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<front>
<journal-meta>
<journal-id journal-id-type="publisher-id">Front. Pharmacol.</journal-id>
<journal-title-group>
<journal-title>Frontiers in Pharmacology</journal-title>
<abbrev-journal-title abbrev-type="pubmed">Front. Pharmacol.</abbrev-journal-title>
</journal-title-group>
<issn pub-type="epub">1663-9812</issn>
<publisher>
<publisher-name>Frontiers Media S.A.</publisher-name>
</publisher>
</journal-meta>
<article-meta>
<article-id pub-id-type="publisher-id">1756578</article-id>
<article-id pub-id-type="doi">10.3389/fphar.2026.1756578</article-id>
<article-version article-version-type="Version of Record" vocab="NISO-RP-8-2008"/>
<article-categories>
<subj-group subj-group-type="heading">
<subject>Original Research</subject>
</subj-group>
</article-categories>
<title-group>
<article-title>Beyond codeine &#x2013; the evidence landscape of conventional, natural, and emerging antitussive therapies: a systematic review and meta-analysis</article-title>
<alt-title alt-title-type="left-running-head">Marko and Pawliczak</alt-title>
<alt-title alt-title-type="right-running-head">
<ext-link ext-link-type="uri" xlink:href="https://doi.org/10.3389/fphar.2026.1756578">10.3389/fphar.2026.1756578</ext-link>
</alt-title>
</title-group>
<contrib-group>
<contrib contrib-type="author">
<name>
<surname>Marko</surname>
<given-names>Monika</given-names>
</name>
<xref ref-type="aff" rid="aff1"/>
<xref ref-type="author-notes" rid="fn001">
<sup>&#x2020;</sup>
</xref>
<uri xlink:href="https://loop.frontiersin.org/people/3110375"/>
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<contrib contrib-type="author" corresp="yes">
<name>
<surname>Pawliczak</surname>
<given-names>Rafa&#x142;</given-names>
</name>
<xref ref-type="aff" rid="aff1"/>
<xref ref-type="corresp" rid="c001">&#x2a;</xref>
<xref ref-type="author-notes" rid="fn001">
<sup>&#x2020;</sup>
</xref>
<uri xlink:href="https://loop.frontiersin.org/people/2364096"/>
<role vocab="credit" vocab-identifier="https://credit.niso.org/" vocab-term="Data curation" vocab-term-identifier="https://credit.niso.org/contributor-roles/data-curation/">Data curation</role>
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<aff id="aff1">
<institution>Department of Immunopathology, Faculty of Medicine, Division of Biomedical Science, Medical University of Lodz</institution>, <city>Lodz</city>, <country country="PL">Poland</country>
</aff>
<author-notes>
<corresp id="c001">
<label>&#x2a;</label>Correspondence: Rafa&#x142; Pawliczak, <email xlink:href="mailto:rafal.pawliczak@csk.umed.lodz.pl">rafal.pawliczak@csk.umed.lodz.pl</email>
</corresp>
<fn fn-type="other" id="fn001">
<label>
<sup>&#x2020;</sup>
</label>
<p>ORCID: Monika Marko, <ext-link ext-link-type="uri" xlink:href="https://orcid.org/0000-0003-3596-6625">orcid.org/0000-0003-3596-6625</ext-link>; Rafa&#x142; Pawliczak, <ext-link ext-link-type="uri" xlink:href="https://orcid.org/0000-0001-6784-453X">orcid.org/0000-0001-6784-453X</ext-link>
</p>
</fn>
</author-notes>
<pub-date publication-format="electronic" date-type="pub" iso-8601-date="2026-03-02">
<day>02</day>
<month>03</month>
<year>2026</year>
</pub-date>
<pub-date publication-format="electronic" date-type="collection">
<year>2026</year>
</pub-date>
<volume>17</volume>
<elocation-id>1756578</elocation-id>
<history>
<date date-type="received">
<day>28</day>
<month>11</month>
<year>2025</year>
</date>
<date date-type="rev-recd">
<day>16</day>
<month>01</month>
<year>2026</year>
</date>
<date date-type="accepted">
<day>28</day>
<month>01</month>
<year>2026</year>
</date>
</history>
<permissions>
<copyright-statement>Copyright &#xa9; 2026 Marko and Pawliczak.</copyright-statement>
<copyright-year>2026</copyright-year>
<copyright-holder>Marko and Pawliczak</copyright-holder>
<license>
<ali:license_ref start_date="2026-03-02">https://creativecommons.org/licenses/by/4.0/</ali:license_ref>
<license-p>This is an open-access article distributed under the terms of the <ext-link ext-link-type="uri" xlink:href="https://creativecommons.org/licenses/by/4.0/">Creative Commons Attribution License (CC BY)</ext-link>. The use, distribution or reproduction in other forums is permitted, provided the original author(s) and the copyright owner(s) are credited and that the original publication in this journal is cited, in accordance with accepted academic practice. No use, distribution or reproduction is permitted which does not comply with these terms.</license-p>
</license>
</permissions>
<abstract>
<sec>
<title>Background</title>
<p>For decades, cough treatment has relied on centrally acting agents like codeine despite inconsistent efficacy. Advances in cough neurobiology enabled targeted therapies. Natural remedies remain widely used, though evidence for their effectiveness and safety is limited. This study aimed to compare evidence on the efficacy and safety of conventional, natural, and novel antitussives.</p>
</sec>
<sec>
<title>Methods</title>
<p>A systematic review and meta-analysis of randomized clinical trials assessed cough frequency, Visual Analogue Scale (VAS), Leicester Cough Questionnaire (LCQ) and adverse events versus placebo.</p>
</sec>
<sec>
<title>Results</title>
<p>Subgroup meta-analysis showed no significant differences between P2X3 antagonists, indicating a consistent class effect. All subgroups reduced chronic cough frequency [standardized mean difference (SMD) &#x3d; &#x2212;0.50, 95% confidence interval (CI) (&#x2212;0.67&#x2013;0.34), P &#x3d; 0.0001], suggesting that the observed effect is a class-related response rather than a compound-specific effect.</p>
</sec>
<sec>
<title>Conclusion</title>
<p>Conventional and natural antitussives show inconsistent efficacy. P2X3 receptor antagonists appear most promising, marking a shift beyond codeine toward targeted chronic cough therapies.</p>
</sec>
<sec>
<title>Clinical Trial Registration</title>
<p>The meta-analysis was performed according to the protocol described in PROSPERO, identifier CRD420251172660.</p>
</sec>
</abstract>
<kwd-group>
<kwd>antitussive</kwd>
<kwd>codeine alternatives</kwd>
<kwd>cough suppression</kwd>
<kwd>natural therapies</kwd>
<kwd>P2X3</kwd>
</kwd-group>
<funding-group>
<award-group id="gs1">
<funding-source id="sp1">
<institution-wrap>
<institution>Uniwersytet Medyczny w Lodzi</institution>
<institution-id institution-id-type="doi" vocab="open-funder-registry" vocab-identifier="10.13039/open_funder_registry">10.13039/501100005888</institution-id>
</institution-wrap>
</funding-source>
</award-group>
<funding-statement>The author(s) declared that financial support was received for this work and/or its publication. This work was supported by the Medical University of Lodz (grant number 503/0-149-03/503-01-001).</funding-statement>
</funding-group>
<counts>
<fig-count count="7"/>
<table-count count="3"/>
<equation-count count="0"/>
<ref-count count="54"/>
<page-count count="19"/>
</counts>
<custom-meta-group>
<custom-meta>
<meta-name>section-at-acceptance</meta-name>
<meta-value>Respiratory Pharmacology</meta-value>
</custom-meta>
</custom-meta-group>
</article-meta>
</front>
<body>
<sec sec-type="intro" id="s1">
<label>1</label>
<title>Introduction</title>
<p>Cough is a vital protective reflex whose primary function is to generate high-velocity airflow, thereby clearing the airways and maintaining respiratory function (<xref ref-type="bibr" rid="B29">Morice et al., 2020</xref>; <xref ref-type="bibr" rid="B23">Lee et al., 2021</xref>). When this response becomes excessive or uncontrolled, however, it may evolve into a chronic condition that markedly affects quality of life and increases the healthcare burden (<xref ref-type="bibr" rid="B18">Jakusova and Brozmanova, 2023</xref>; <xref ref-type="bibr" rid="B49">Weinberger and Hurvitz, 2020</xref>). Children are considered to have a chronic cough when symptoms persist for more than 4&#xa0;weeks, whereas in adults the threshold is 8&#xa0;weeks (<xref ref-type="bibr" rid="B49">Weinberger and Hurvitz, 2020</xref>). The leading causes of chronic cough include asthma, chronic obstructive pulmonary disease (COPD), pulmonary fibrosis, eosinophilic bronchitis, chronic bacterial bronchitis (<xref ref-type="bibr" rid="B51">Weinberger et al., 2025</xref>), as well as upper airway cough syndrome and gastroesophageal reflux disease (GERD).</p>
<p>Increasing attention has been given to cough hypersensitivity syndrome (CHS), which is now recognized as a significant clinical entity accounting for a substantial proportion of patients with chronic cough in whom no clear underlying cause can be identified (<xref ref-type="bibr" rid="B21">Khan et al., 2024</xref>; <xref ref-type="bibr" rid="B9">Chung et al., 2016</xref>). This condition is characterized by an exaggerated cough response to otherwise innocuous stimuli (thermal, mechanical, or chemical), resulting from enhanced excitability and plasticity of airway sensory nerves, particularly involving vagal afferent pathways (<xref ref-type="bibr" rid="B21">Khan et al., 2024</xref>). Importantly, evidence suggests that, in addition to maladaptive neural plasticity, other pathophysiological mechanisms underlying cough hypersensitivity have not been sufficiently characterized (<xref ref-type="bibr" rid="B46">Song and Morice, 2017</xref>).</p>
<p>Other contributing factors comprise the use of antihypertensive agents such as angiotensin-converting enzyme (ACE) inhibitors, smoking, habit cough, and systemic disorders (<xref ref-type="bibr" rid="B29">Morice et al., 2020</xref>; <xref ref-type="bibr" rid="B18">Jakusova and Brozmanova, 2023</xref>). A so-called habit cough, more frequently observed in children and adolescents, is considered a functional disorder characterized by repetitive coughing without an identifiable organic cause, often influenced by behavioral or psychogenic factors (<xref ref-type="bibr" rid="B50">Weinberger et al., 2023</xref>). Identification of the etiologies of chronic cough is essential for effective management. In adults, the most common etiologies include cough-variant asthma (CVA), upper airway cough syndrome (UACS), and eosinophilic bronchitis (EB). In contrast, the etiologies of chronic cough in children differ, with protracted bronchitis (PB) predominating and asthma or CVA representing frequent etiologies in school-aged children. However, data on pediatric etiologies remain limited due to the restricted feasibility of diagnostic investigations (<xref ref-type="bibr" rid="B54">Yu et al., 2019</xref>).</p>
<p>Cough is one of the most common symptoms encountered in clinical practice, and despite significant progress in understanding its mechanisms, treating it remains a challenge for clinicians (<xref ref-type="bibr" rid="B18">Jakusova and Brozmanova, 2023</xref>; <xref ref-type="bibr" rid="B40">Rouadi et al., 2025</xref>).</p>
<p>For decades, the management of cough has relied on centrally acting agents, including codeine (<xref ref-type="bibr" rid="B42">Smith et al., 2006</xref>), dextromethorphan (<xref ref-type="bibr" rid="B28">Meeves et al., 2023</xref>), butamirate (<xref ref-type="bibr" rid="B12">Faruqi et al., 2014</xref>; <xref ref-type="bibr" rid="B8">Charpin and Weibel, 1990</xref>), and levodropropizine (<xref ref-type="bibr" rid="B24">Lee et al., 2022</xref>; <xref ref-type="bibr" rid="B25">Mannini et al., 2017</xref>), despite their limited and inconsistent clinical efficacy. Recent advances in the neurobiology of cough have led to the development of mechanism-based therapies, such as P2X3 receptor antagonists, that directly target peripheral cough pathways (<xref ref-type="bibr" rid="B40">Rouadi et al., 2025</xref>). This paradigm shift from symptom suppression to pathway-specific modulation marks a pivotal moment in antitussive research.</p>
<p>Alongside these agents, a wide range of natural or herbal remedies continues to be promoted for cough relief, reflecting patient preference for &#x201c;natural&#x201d; options (<xref ref-type="bibr" rid="B31">Murgia et al., 2021</xref>). It is estimated that nearly four billion people worldwide still rely primarily on herbal medicines for their healthcare needs (<xref ref-type="bibr" rid="B47">Wardani et al., 2023</xref>).</p>
<p>Natural cough medicines, often perceived as safer, offer an alternative to conventional over the counter (OTC) cough medications. It should also be emphasized that the market for so-called &#x201c;natural&#x201d; cough medicines is rapidly expanding, offering a wide range of preparations with diverse compositions and claimed mechanisms of action (<xref ref-type="bibr" rid="B31">Murgia et al., 2021</xref>). Moreover, because medicinal plants contain a variety of bioactive molecules that can simultaneously exert expectorant and antitussive effects, the classification of herbal cough remedies is difficult (<xref ref-type="bibr" rid="B37">Pourova et al., 2023</xref>).</p>
<p>An important aspect is the difficult-to-assess chemical composition of plant extracts, which can vary significantly depending on cultivation, harvesting, storage, and processing conditions. As a result, products sold under the same name may differ in composition and pharmacological activity (<xref ref-type="bibr" rid="B31">Murgia et al., 2021</xref>). Due to growing interest in natural cough remedies and the lack of consistent, high-quality scientific evidence, a critical assessment of the current state of knowledge is necessary.</p>
<p>Our study aimed to go beyond codeine and examine the current scientific evidence on the effectiveness and safety of conventional, natural, and novel antitussive therapies for the treatment of chronic cough. Therefore, we conducted a systematic review and meta-analysis to assess and compare the effectiveness and safety of antitussives. By integrating data from randomized clinical trials (RCTs), we aimed to provide an updated and comprehensive evidence synthesis to aid clinical decision-making in cough management.</p>
</sec>
<sec sec-type="methods" id="s2">
<label>2</label>
<title>Methods</title>
<sec id="s2-1">
<label>2.1</label>
<title>Search strategy</title>
<p>This systematic review and meta-analysis was conducted in line with the Preferred Reporting Items for Systematic Reviews and Meta-Analyses (PRISMA) guidelines (<xref ref-type="bibr" rid="B34">Page et al., 2021</xref>). The study protocol was described in PROSPERO (CRD420251172660).</p>
<p>A comprehensive search was carried out across PubMed, the Cochrane Central Register of Controlled Trials (CENTRAL), Embase, and <ext-link ext-link-type="uri" xlink:href="http://ClinicalTrials.gov">ClinicalTrials.gov</ext-link> up to October 2025. In addition, gray literature sources&#x2013;such as conference abstracts, official reports, preprints, datasets, white papers, and patents were explored via Google Scholar. The complete search strategy is provided in <xref ref-type="table" rid="T1">Table 1</xref>. To ensure completeness, updated searches were performed prior to the final synthesis.</p>
<table-wrap id="T1" position="float">
<label>TABLE 1</label>
<caption>
<p>Search strategy.</p>
</caption>
<table>
<thead valign="top">
<tr>
<th align="center">Database</th>
<th align="center">Search strategy<xref ref-type="table-fn" rid="Tfn1">
<sup>a</sup>
</xref>
</th>
</tr>
</thead>
<tbody valign="top">
<tr>
<td align="left">PubMed</td>
<td align="left">((antitussive agents) OR (antitussive drugs) OR (cough treatment) AND ((efficacy)) AND ((safety) OR (adverse events) OR (side effects))<break/>Filters applied: Randomized controlled trial, Clinical trial</td>
</tr>
<tr>
<td align="left">Cochrane Central Register of Controlled Trials (CENTER)</td>
<td align="left">Antitussive agents OR antitussive drugs OR cough treatment AND efficacy AND safety<break/>Filters applied: title abstract keyword, in Trials</td>
</tr>
<tr>
<td align="left">ClinicalTrials.gov</td>
<td align="left">(antitussive agents OR antitussive drugs OR cough treatment) AND (efficacy) AND (safety OR adverse events OR side effects)<break/>Filters applied: &#x201c;Expert search&#x201d;</td>
</tr>
<tr>
<td align="left">Embase</td>
<td align="left">(&#x201c;antitussive agents&#x201d;/exp OR &#x201c;antitussive agents&#x201d; OR &#x201c;antitussive drugs&#x201d; OR &#x201c;cough treatment&#x201d; OR &#x201c;efficacy&#x201d;/exp OR &#x201c;efficacy&#x201d; OR &#x201c;safety&#x201d;/exp OR &#x201c;safety&#x201d; OR &#x201c;adverse events&#x201d;/exp OR &#x201c;adverse events&#x201d; OR &#x201c;side effects&#x201d;) AND ([controlled clinical trial]/lim OR [randomized controlled trial]/lim) AND &#x201c;coughing&#x201d;/dm AND (&#x201c;clinical trial&#x201d;/de OR &#x201c;controlled clinical trial&#x201d;/de OR &#x201c;controlled study&#x201d;/de OR &#x201c;double blind procedure&#x201d;/de OR &#x201c;human&#x201d;/de OR &#x201c;intervention study&#x201d;/de OR &#x201c;open study&#x201d;/de OR &#x201c;randomized controlled trial&#x201d;/de OR &#x201c;retrospective study&#x201d;/de) AND (&#x201c;article&#x201d;/it OR &#x201c;clinical trial&#x201d;/it)</td>
</tr>
<tr>
<td align="left">Google Scholar</td>
<td align="left">((antitussive agents) OR (antitussive drugs) OR (cough treatment) AND ((efficacy)) AND ((safety) OR (adverse events) OR (side effects))</td>
</tr>
</tbody>
</table>
<table-wrap-foot>
<fn id="Tfn1">
<label>
<sup>a</sup>
</label>
<p>The searches were re-run before the final analysis to identify further studies and possibly include them.</p>
</fn>
</table-wrap-foot>
</table-wrap>
<p>The research question and selection criteria were formulated using the Population, Intervention, Comparison, Outcome, and Study design (PICOS) structure. The inclusion criteria were population: patients with cough, intervention: antitussive drugs, comparison: placebo, outcomes: cough count, change in cough frequency, Visual Analogue Scale (VAS), Leicester Cough Questionnaire (LCQ) and adverse events (AEs), and study design: randomized clinical trials (RCTs), non-randomized clinical trials, real-life trials, observational trials, open-label trials, and prospective trials.</p>
<p>The following exclusion criteria were formulated: review article, systematic reviews, meta-analysis, case series, case report, articles with insufficient information and data, articles published in languages other than English, original articles where specific data and outcomes could not be extracted, original articles that do not include outcomes of interest and retracted articles.</p>
</sec>
<sec id="s2-2">
<label>2.2</label>
<title>Study selection and data extraction</title>
<p>The study selection process was conducted independently by two reviewers in parallel. Titles and abstracts identified through database searches were first screened for relevance, and duplicate records were excluded. Full texts of potentially eligible studies were then assessed in detail to determine whether they met the predefined inclusion criteria. To minimize selection bias, eligibility was judged independently by both reviewers, and any discrepancies were resolved through discussion until consensus was achieved.</p>
<p>Data extraction was performed independently using standardized forms. Extracted information included study identifiers (title, authors, institutional affiliation, and registration number), study design, duration, year of publication, intervention details, sample size, participant age, underlying condition, and reported outcomes. The two sets of extracted data were subsequently compared for accuracy and consistency.</p>
<p>All included studies were further assessed for missing or unclear data. Where required, efforts were made to clarify information or standardize reporting. In accordance with Cochrane guidelines (<xref ref-type="bibr" rid="B17">Higgins et al., 2024</xref>), results expressed as confidence intervals (CIs) or standard errors of the mean (SEM) were converted to means and standard deviation (SD) to ensure comparability across studies.</p>
</sec>
<sec id="s2-3">
<label>2.3</label>
<title>Assessment of the risk of bias and methodological quality</title>
<p>Risk of bias was assessed independently by two reviewers using the Cochrane Risk of Bias tool in Review Manager 5.4. Seven domains were evaluated (sequence generation, allocation concealment, blinding, incomplete data, selective reporting, and other bias), with studies rated as low, unclear, or high risk. Potential conflicts of interest were also considered in relation to funding sources. Disagreements were resolved by consensus, and an attrition rate above 10% was regarded as potentially influencing study validity.</p>
</sec>
<sec id="s2-4">
<label>2.4</label>
<title>Statistical methods</title>
<p>All extracted data were analyzed using Review Manager (RevMan) version 5.4. Continuous outcomes were expressed as standardized mean difference (SMD) with 95% confidence intervals (CI), and dichotomous outcomes as risk ratios (RR) with CI. Given the expected heterogeneity, pooled analyses were performed using the Mantel&#x2013;Haenszel random-effects model. Heterogeneity was assessed with Cochran&#x2019;s Q test and the I<sup>2</sup> statistic, with P &#x3c; 0.05 considered significant. Results were presented as forest plots, and SMDs were interpreted according to Cohen&#x2019;s thresholds (0.2 small, 0.5 moderate, &#x2265;0.8 large).</p>
</sec>
<sec id="s2-5">
<label>2.5</label>
<title>Additional analyses</title>
<p>The certainty of evidence for the outcomes included in the quantitative synthesis was appraised using the Grading of Recommendations Assessment, Development, and Evaluation (GRADE) approach (<xref ref-type="bibr" rid="B41">Sch&#xfc;nemann et al., 2023</xref>; <xref ref-type="bibr" rid="B16">Guyatt et al., 2013</xref>). This assessment considered potential limitations related to risk of bias, inconsistency, indirectness, imprecision, and publication bias. Evidence quality was classified as high, moderate, low, or very low, following the standard GRADE framework, and findings were summarized in a Summary of Findings (SoF) table (<xref ref-type="bibr" rid="B16">Guyatt et al., 2013</xref>). The potential for publication bias was further examined through visual inspection of funnel plots.</p>
</sec>
</sec>
<sec sec-type="results" id="s3">
<label>3</label>
<title>Results</title>
<sec id="s3-1">
<label>3.1</label>
<title>Included studies</title>
<p>
<xref ref-type="fig" rid="F1">Figure 1</xref> (<xref ref-type="bibr" rid="B34">Page et al., 2021</xref>) illustrates the study selection process. <xref ref-type="table" rid="T2">Table 2</xref> summarizes the characteristics of the studies included in the meta-analysis (<xref ref-type="bibr" rid="B10">Dicpinigaitis et al., 2023</xref>; <xref ref-type="bibr" rid="B1">Abdulqawi et al., 2015</xref>; <xref ref-type="bibr" rid="B43">Smith et al., 2020a</xref>; <xref ref-type="bibr" rid="B44">Smith et al., 2020b</xref>; <xref ref-type="bibr" rid="B45">Smith et al., 2025</xref>; <xref ref-type="bibr" rid="B4">Birring et al., 2024</xref>; <xref ref-type="bibr" rid="B27">McGarvey et al., 2023</xref>; <xref ref-type="bibr" rid="B32">Niimi et al., 2022</xref>; <xref ref-type="bibr" rid="B30">Morice et al., 2021</xref>) and a systematic review (<xref ref-type="bibr" rid="B42">Smith et al., 2006</xref>; <xref ref-type="bibr" rid="B28">Meeves et al., 2023</xref>; <xref ref-type="bibr" rid="B25">Mannini et al., 2017</xref>; <xref ref-type="bibr" rid="B6">Canciani et al., 2014</xref>; <xref ref-type="bibr" rid="B7">Carnevali et al., 2021</xref>; <xref ref-type="bibr" rid="B15">Ghaemi et al., 2020</xref>; <xref ref-type="bibr" rid="B35">Pan et al., 2025</xref>; <xref ref-type="bibr" rid="B36">Paul et al., 2014</xref>; <xref ref-type="bibr" rid="B38">Qasemzadeh et al., 2015</xref>; <xref ref-type="bibr" rid="B20">Kemmerich et al., 2006</xref>; <xref ref-type="bibr" rid="B19">Kemmerich, 2007</xref>; <xref ref-type="bibr" rid="B33">N&#xfa;&#xf1;ez et al., 2024</xref>; <xref ref-type="bibr" rid="B48">Watson et al., 2008</xref>; <xref ref-type="bibr" rid="B52">Willcox et al., 2021</xref>; <xref ref-type="bibr" rid="B22">Lee et al., 2000</xref>; <xref ref-type="bibr" rid="B11">Eccles et al., 1992</xref>; <xref ref-type="bibr" rid="B14">Freestone et al., 1996</xref>; <xref ref-type="bibr" rid="B3">Bhattacharya et al., 2013</xref>; <xref ref-type="bibr" rid="B5">Bruschi et al., 2003</xref>; <xref ref-type="bibr" rid="B26">McGarvey et al., 2022</xref>; <xref ref-type="bibr" rid="B2">Barth et al., 2015</xref>). Following study selection, quantitative synthesis was feasible exclusively for chronic cough, as no eligible studies investigating acute cough met the predefined inclusion criteria.</p>
<fig id="F1" position="float">
<label>FIGURE 1</label>
<caption>
<p>Flowchart of the screening procedure. PICOS: Population, Intervention, Comparison, Outcome and Study design.</p>
</caption>
<graphic xlink:href="fphar-17-1756578-g001.tif">
<alt-text content-type="machine-generated">PRISMA flow diagram outlining systematic review process: 16,774 records identified across four databases, 6,433 removed, 10,341 screened with 5,037 excluded, 5,304 reports sought, 5,150 not retrieved, 154 assessed for eligibility, 123 excluded for not meeting PICOS, resulting in 21 qualitative and 10 quantitative studies included.</alt-text>
</graphic>
</fig>
<table-wrap id="T2" position="float">
<label>TABLE 2</label>
<caption>
<p>Characteristics of studies included in a systematic review and meta-analysis.</p>
</caption>
<table>
<thead valign="top">
<tr>
<th colspan="5" align="center">Studies included in a meta-analysis</th>
</tr>
<tr>
<th align="center">Study (author, year)/Design</th>
<th align="center">Duration</th>
<th align="center">Intervention</th>
<th align="center">Participants N, age, condition</th>
<th align="center">Main outcomes and measures</th>
</tr>
</thead>
<tbody valign="top">
<tr>
<td align="left">(<xref ref-type="bibr" rid="B10">Dicpinigaitis et al., 2023</xref>)<break/>PAGANINI: a randomized, double-blind, parallel-group, placebo-con- trolled, dose-finding</td>
<td align="left">12 weeks</td>
<td align="left">Twice daily:<break/>Eliapixant<break/>25&#xa0;mg<break/>75&#xa0;mg<break/>150&#xa0;mg placebo</td>
<td align="left">N &#x3d; 310, &#x2265;18 refractory chronic cough (RCC)</td>
<td align="left">PO: Change from baseline in 24-h cough count after 12&#xa0;weeks of intervention<break/>SO: &#x2265;30% reduction in 24-h cough count at 12&#xa0;weeks<break/>Change in 24-h cough count at 2, 4, 8&#xa0;weeks<break/>PO: Change in awake coughs/hour at 2, 4, 8, 12&#xa0;weeks<break/>Change in cough severity (VAS) at 12&#xa0;weeks; &#x2265;30-unit VAS reduction<break/>Change in cough-related QoL (LCQ) at 12&#xa0;weeks; &#x2265;1.3-point LCQ increase<break/>Treatment-emergent AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B1">Abdulqawi et al., 2015</xref>)<break/>a randomized, double-blind, placebo-controlled phase 2 study</td>
<td align="left">8&#xa0;weeks (two 2-week treatment periods &#x2b; 2-week washout &#x2b; 2-week follow-up)</td>
<td align="left">Twice daily:<break/>AF-219<break/>600&#xa0;mg placebo</td>
<td align="left">N &#x3d; 24<break/>Mean age: 54.5&#xa0;years (24&#x2013;70) refractory chronic cough (RCC)</td>
<td align="left">PO: Daytime cough frequency, night-time and 24-h cough frequency assessed<break/>SO: Changes in cough severity VAS (day/night), urge-to-cough VAS, and CQLQ scores; global rating of change (15-point scale) for cough severity and frequency<break/>Treatment-emergent AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B43">Smith et al., 2020a</xref>) I and II<break/>Two randomized, double-blind, placebo-controlled, two-period crossover, dose-escalation studies</td>
<td align="left">&#x223c;5&#x2013;8&#xa0;weeks (two 16-day treatment periods &#x2b; washout)</td>
<td align="left">Gefapixant BID 7.5&#x2013;200&#xa0;mg; 4-day escalation placebo</td>
<td align="left">N &#x3d; 59 mean age 63&#xa0;years (47&#x2013;76)<break/>refractory chronic cough (RCC)</td>
<td align="left">PO: Awake cough freq. (VitaloJAK)<break/>SO: VAS, cough diary, LCQ<break/>AEs; physical examination; vital signs; ECG; blood and urine analyses</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B44">Smith et al., 2020b</xref>) III<break/>a randomized, double-blind, controlled, parallel-group, phase 2b trial</td>
<td align="left">12-week</td>
<td align="left">Gefapixant BID 7.5&#x2013;50&#xa0;mg placebo</td>
<td align="left">N &#x3d; 253<break/>Age range: 18-80 refractory chronic cough (RCC)<break/>or unexplained chronic cough</td>
<td align="left">PO: Change from baseline in awake objective cough frequency after 12&#xa0;weeks (day 84)<break/>SO: Change in awake/24-h/sleep cough freq. (4&#x2013;12 w, FU 14&#xa0;weeks); VAS; LCQ; responder rates (&#x2265;30/50/70%); PGIC, CGIC.<break/>Vital signs, laboratory assessments, and AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B45">Smith et al., 2025</xref>)<break/>SOOTHE: a phase 2b, randomized, placebo-controlled trial</td>
<td align="left">4 weeks</td>
<td align="left">camlipixant<break/>12.5, 50, or 200&#xa0;mg twice daily or placebo for 4 weeks</td>
<td align="left">N &#x3d; 310<break/>Age range: 18-80 refractory chronic cough (RCC)</td>
<td align="left">PO: Change in 24-h cough frequency (Day 28, VitaloJAK)<break/>SO: Change in 24-h (Day 15), awake/night frequency (Days 15, 28); responders (&#x3e;30/50/70%); CS-VAS; LCQ (Days 15, 29)<break/>AEs, TEAEs, abnormal exam/ECG/vital signs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B44">Smith et al., 2020b</xref>)<break/>A randomized placebo- controlled study</td>
<td align="left">&#x223c;3 weeks total (two 1-day periods, 48-h washout, 2-weeks follow-up)</td>
<td align="left">single dose gefapixant<break/>100&#xa0;mg or placebo</td>
<td align="left">N &#x3d; 24<break/>Age range: 18&#x2013;80 chronic cough</td>
<td align="left">PO: Cough challenge thresholds C2 (&#x2265;2 coughs) and C5 (&#x2265;5 coughs) for each challenge agent, averaged across 1-, 3-, and 5-h post-exposure<break/>SO: VAS (cough severity, urge-to-cough), 24-h cough freq. (ambulatory), HARQ total score (0&#x2013;70)<break/>Serious AEs, physical examinations, vital signs, 12-lead ECGs, and clinical laboratory tests</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B4">Birring et al., 2024</xref>)<break/>a phase 3b, randomized, multicentre, double-blind, placebo-controlled trial</td>
<td align="left">&#x2248;16&#xa0;weeks total (2-week run-in &#x2b;12-week treatment &#x2b; 2-week follow-up)</td>
<td align="left">Gefapixant<break/>45&#xa0;mg twice daily or placebo</td>
<td align="left">N &#x3d; 375<break/>Mean age: 56.4&#xa0;years (SD 11.4)<break/>chronic cough and cough-induced stress urinary incontinence</td>
<td align="left">PO: Percentage change from baseline in 7-day average of daily CSUI episodes at week 12 (recorded in incontinence diary)<break/>SO: Change from baseline in CSD, total daily incontinence episodes, cough severity VAS, I-QOL, work productivity and activity impairment, and percentage of participants improved on the PGIC scale<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B27">McGarvey et al., 2023</xref>)<break/>phase 3b, double-blind, placebo-controlled, parallel group, multicenter study</td>
<td align="left">&#x2248;16&#xa0;weeks total (2-week screening &#x2b;12-week treatment &#x2b; 2-week follow-up)</td>
<td align="left">gefapixant<break/>45&#xa0;mg BID or placebo</td>
<td align="left">N &#x3d; 415<break/>&#x2265;18&#xa0;years of age<break/>mean age 52.5&#xa0;years<break/>recent-onset refractory chronic cough (RCC) or unexplained chronic cough (UCC)</td>
<td align="left">PO: change from baseline at week 12 in LCQ total score<break/>SO: The change from baseline in Cough Severity VAS score at week 12 and the CSD<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B32">Niimi et al., 2022</xref>)<break/>a phase 2a, randomized, double-blind, placebo-controlled, crossover, multicentre study</td>
<td align="left">Approximately 6&#x2013;7&#xa0;weeks (2 weeks of treatment, 2&#x2013;3-week washout period, followed by another 2&#xa0;weeks of treatment in the crossover phase)</td>
<td align="left">oral sivopixant<break/>150&#xa0;mg or placebo once daily for 2 weeks</td>
<td align="left">N &#x3d; 31<break/>Age range: 20&#x2013;75&#xa0;years refractory chronic cough (RCC)</td>
<td align="left">PO: Ratio of daytime coughs per hour after 2&#xa0;weeks vs. baseline<break/>SO: Ratios of coughs per hour (24&#xa0;h, nighttime, awake, asleep) vs. baseline<break/>Change in J-LCQ and % achieving MID (&#x2265;1.3 points)<break/>Change in cough severity (VAS)<break/>Change in EQ-5D-5L and EQ-VAS<break/>AEs and blood pressure, pulse rate, ECG and clinical laboratory tests</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B30">Morice et al., 2021</xref>)<break/>a randomized, placebo-controlled, crossover phase 2a study</td>
<td align="left">&#x223c;9&#x2013;10&#xa0;weeks (two 3-week periods &#x2b; 3&#x2013;4&#xa0;weeks washout)</td>
<td align="left">Period A: placebo 2&#xa0;weeks: eliapixant 10&#xa0;mg BID 1 week; Period B: eliapixant 50/200/750&#xa0;mg BID (1 week each)</td>
<td align="left">N &#x3d; 40<break/>&#x3e;18&#xa0;years<break/>refractory chronic cough (RCC)</td>
<td align="left">PO: Change in cough frequency per hour (24-h objective monitoring, VitaloJAK) at baseline (day 1) and end of each treatment week (days 7, 14, 21); awake and asleep cough frequencies also assessed<break/>SO: Patient-reported cough severity (VAS, 100&#xa0;mm) and cough-related quality of life (LCQ)<break/>Frequency and severity of AEs</td>
</tr>
<tr>
<td colspan="5" align="center">Studies included in a systematic review</td>
</tr>
<tr>
<td align="left">Study ID</td>
<td align="left">Duration</td>
<td align="left">Intervention</td>
<td align="left">Participants<break/>N, age, condition</td>
<td align="left">Main outcomes and measures</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B22">Lee et al., 2000</xref>) a double-blind, stratifed, rando- mized and parallel group design study</td>
<td align="left">Single-day sessions (3&#xa0;h follow-up)</td>
<td align="left">Dextromethorphan 30&#xa0;mg<break/>Placebo</td>
<td align="left">N &#x3d; 44<break/>Age range: 18-60 cough associated with acute upper respiratory tract infection</td>
<td align="left">Not specifically reported</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B11">Eccles et al., 1992</xref>) a randomized, stratified, double- blind, parallel group, placebo-controlled study</td>
<td align="left">3-h laboratory assessment &#x2b; 4-day home phase</td>
<td align="left">Codeine 30 mg/10&#xa0;mL q.d.s. (total 120&#xa0;mg/day) placebo syrup</td>
<td align="left">N &#x3d; 91<break/>Mean age: 23&#xa0;years, (18-71) cough associated with acute upper respiratory tract infection</td>
<td align="left">Not specifically reported</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B42">Smith et al., 2006</xref>) double-blind, randomized, placebo- controlled study</td>
<td align="left">2 single-day periods, 1&#xa0;week apart</td>
<td align="left">Codeine phosphate 60&#xa0;mg or matched placebo</td>
<td align="left">N &#x3d; 21<break/>Mean age: 67.7&#xa0;years cough in chronic obstructive pulmonary disease</td>
<td align="left">PO: Time spent coughing (cough seconds, cs) during 10-h daytime and overnight recordings (objective cough frequency)<break/>SO: Not specifically reported</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B14">Freestone et al., 1996</xref>) a double-blind, stratified, placebo-controlled, parallel-group, clinical trial</td>
<td align="left">2&#xa0;days</td>
<td align="left">50&#xa0;mg codeine or matched placebo in capsule form</td>
<td align="left">N &#x3d; 83<break/>Mean age: 23.5&#xa0;years cough associated with common cold or acute URTI</td>
<td align="left">cough sound-pressure levels (CSPLs) measured on a sound meter; subjective scores of coughs seventy; and cough frequency recorded by means of a microphone connected to an ink-pen recorder</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B3">Bhattacharya et al., 2013</xref>) randomized double-blinded placebo-controlled trial</td>
<td align="left">dextromethorphan<break/>5&#xa0;mg promethazine 0.5&#xa0;mg/kg<break/>placebo</td>
<td align="left">3&#xa0;days</td>
<td align="left">N &#x3d; 120 median age:<break/>5.5&#xa0;years nocturnal cough during URTI</td>
<td align="left">Symptom scores<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B28">Meeves et al., 2023</xref>) multiple&#x2010;dose, double&#x2010;blind, placebo&#x2010;controlled, randomized, pilot clinical study</td>
<td align="left">4&#xa0;days</td>
<td align="left">Dextromethorphan<break/>15&#xa0;mg/10&#xa0;mL or placebo</td>
<td align="left">N &#x3d; 131<break/>Age range: 6&#x2013;11&#xa0;years<break/>acute cough due to the common cold</td>
<td align="left">PO: Total cough count during the first 24&#xa0;h of treatment<break/>SO: Cough rate (counts/h) during daytime, nighttime, and individual dosing intervals<break/>Total time with cough events over 24&#xa0;h<break/>Change from baseline for cough severity, frequency, and impact on sleep (5-point scales)<break/>Change in Child Global Question<break/>Subject/parent satisfaction with treatment<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B5">Bruschi et al., 2003</xref>) a double-blind, randomized, cross-over trial</td>
<td align="left">Approximately 7&#x2013;13&#xa0;days (two treatment sessions of 10 consecutive doses each, separated by a 3&#x2013;7-day washout period)</td>
<td align="left">Levodropropizine 60&#xa0;mg (20 drops) or matching placebo, administered orally three times daily (t.i.d.) for 10 consecutive doses</td>
<td align="left">N &#x3d; 26<break/>Age range: 18&#x2013;45&#xa0;years healthy volunteers and patients with chronic respiratory impairment associated with chronic obstructive pulmonary disease</td>
<td align="left">Bronchodilator reversibility by FEV<sub>1</sub> change after salbutamol 200&#xa0;&#x3bc;g<break/>Spirometry and arterial blood gases measured at baseline and post-inhalation<break/>Respiratory parameters recorded at rest<break/>Ventilatory response to hypercapnia assessed with 0%&#x2013;7% CO<sub>2</sub>
<break/>AEs and general tolerability evaluation by physical examination, vital signs (blood pressure, heart rate), ECG</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B25">Mannini et al., 2017</xref>)<break/>Randomized clinical trial</td>
<td align="left">Approximately 6&#x2013;9&#xa0;days (three treatment sessions separated by 48&#x2013;72-h washout periods)</td>
<td align="left">60&#xa0;mg Levodropropizine, or 15&#xa0;mg Dihydrocodeine or matching placebo</td>
<td align="left">N &#x3d; 24<break/>Age range: 39&#x2013;70&#xa0;years<break/>Chronic cough</td>
<td align="left">Ventilatory response to CO<sub>2</sub> rebreathing</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B26">McGarvey et al., 2022</xref>) two double-blind<break/>randomized, parallel-group, placebo-controlled, phase 3 trials (COUGH-1 and COUGH-2)</td>
<td align="left">12&#xa0;weeks (COUGH-1) and 24&#xa0;weeks (COUGH-2)</td>
<td align="left">gefapixant 15&#xa0;mg twice per day, or gefapixant 45&#xa0;mg twice per day or placebo</td>
<td align="left">COUGH-1<break/>N &#x3d; 732<break/>COUGH-2<break/>N &#x3d; 1,314<break/>Mean age 59.0&#xa0;years (12.6) in COUGH-1<break/>Mean age 58.1&#xa0;years (12.1) in COUGH-2<break/>refractory chronic cough or unexplained chronic cough</td>
<td align="left">PO: Change from baseline in 24-h cough frequency (weeks 12/24)<break/>Secondary:<break/>Change in awake cough frequency<break/>&#x2265;30% reduction in 24-h cough frequency<break/>&#x2265;1.3-point LCQ improvement<break/>Reductions in Cough Severity Diary and VAS scores<break/>Exploratory: 50% and 70% cough-frequency responders<break/>AEs, vital signs, physical examination, and laboratory tests</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B2">Barth et al., 2015</xref>) a comparative, randomized, double-blind, placebo-controlled study</td>
<td align="left">5&#xa0;days</td>
<td align="left">
<italic>Justicia adhatoda, Echinacea purpurea</italic> and <italic>Eleutherococcus senticosus extracts</italic> -KJ (30&#xa0;mL/day<break/>Bromhexine<break/>1.6&#xa0;mg/mL and Placebo</td>
<td align="left">N &#x3d; 177<break/>KJ<break/>Mean age &#xb1;SD:<break/>34.8 &#xb1; 11.39<break/>Bromhexine<break/>Mean age &#xb1;SD:<break/>32.1 &#xb1; 10.38<break/>Placebo<break/>Mean age &#xb1;SD:<break/>31.9 &#xb1; 11.57<break/>patients with acute upper respiratory tract infection</td>
<td align="left">PO: efficacy of treatment (Cough Relief Index), cough frequency<break/>SO: Hematological and immunological parameters<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B6">Canciani et al., 2014</xref>) a randomized, multicenter, double blind, placebo-controlled clinical trial</td>
<td align="left">8&#xa0;days</td>
<td align="left">Grintuss<break/>4 doses a day, 5&#xa0;mL each, and placebo</td>
<td align="left">N &#x3d; 102<break/>Age range: 3&#x2013;5&#xa0;years<break/>cough persisting more than 7&#xa0;days</td>
<td align="left">PO: The changes in the day- and night-time cough score<break/>SO: Not specifically reported<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B7">Carnevali et al., 2021</xref>) a randomized, double blind<break/>placebo-controlled clinical trial</td>
<td align="left">8&#xa0;days</td>
<td align="left">KalobaTUSS<break/>4 doses daily in 5&#xa0;mL per dose<break/>and placebo</td>
<td align="left">N &#x3d; 106<break/>Mean age: (months)<break/>53.0 &#xb1; 12.0<break/>acute cough</td>
<td align="left">PO: The change in the night-time cough score before treatment and nocturnal scores obtained after the first, fourth and eighth nights of treatment, and the change in the diurnal time cough score before treatment and scores obtained after the first, fourth and eighth days of treatment<break/>SO: The secondary outcome was the safety of the syrup when administered to children with acute cough for 8&#xa0;days, which was evaluated by recording potential adverse reactions to treatment<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B15">Ghaemi et al., 2020</xref>)<break/>A randomized, double-blinded, placebo- controlled clinical trial</td>
<td align="left">15&#xa0;months</td>
<td align="left">Licorice pastilles<break/>one pastille of 300&#xa0;mg (licorice, acacia, and tragacanth) or a placebo three times daily for 2&#xa0;weeks</td>
<td align="left">N &#x3d; 70<break/>Age range:18-70<break/>chronic cough</td>
<td align="left">PO: a decrease in the daily cough scores during the 2-week treatment period<break/>SO: the assessment of the quality-of-life measure of chronic cough ac- cording to the LCQ scores<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B35">Pan et al., 2025</xref>)<break/>A multicenter, randomized, double-blinded, placebo-controlled trial</td>
<td align="left">28-day follow-up<break/>14-day treatment</td>
<td align="left">Suhuang Zhike capsules<break/>1.35&#xa0;g of SHZK granules or placebo</td>
<td align="left">N &#x3d; 132<break/>Age range: 18-60<break/>Asthma</td>
<td align="left">PO: Change in ACT scores on day 42 relative to baseline, reflecting asthma control status<break/>SO: Changes in cough symptom scores on days 7, 14, and 42 relatives to the baseline. Changes in VAS scores of coughs, wheezing, chest tightness, and shortness of breath on days 7, 14, and 42 relatives to the baseline<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B36">Paul et al., 2014</xref>)<break/>Randomized clinical trial</td>
<td align="left">13&#xa0;months</td>
<td align="left">Agave nectar<break/>3&#xa0;mL (age 2&#x2013;5&#xa0;months); 4&#xa0;mL (age 6&#x2013;23&#xa0;months); 5&#xa0;mL (age 24&#x2013;47 months) or placebo</td>
<td align="left">N &#x3d; 120<break/>The mean age:<break/>22.9 (14.0) months<break/>nonspecific acute cough</td>
<td align="left">The outcome of between-night change<break/>Cough frequency, cough severity, cough bothersomeness, congestion severity, rhinorrhea severity, and cough effect on child and parent sleep<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B38">Qasemzadeh et al., 2015</xref>) double-blind, randomized controlled clinical trial</td>
<td align="left">7&#xa0;months</td>
<td align="left">
<italic>Viola odorata</italic> Flower Syrup<break/>And placebo administered for 5&#xa0;days; 2.5&#xa0;cc three times daily for children aged 2&#x2013;5&#xa0;years, and 5 cc three times daily for children &#x2265;5&#xa0;years. Each 100 cc of violet syrup contained 12&#xa0;g of dried <italic>Viola</italic> flower</td>
<td align="left">N &#x3d; 182<break/>Age range: 2&#x2013;12&#xa0;years old<break/>Asthma</td>
<td align="left">Evaluation in terms of the duration until cough suppression was achieved<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B20">Kemmerich et al., 2006</xref>) a double-blind, placebo- controlled, multicentre Phase IV study</td>
<td align="left">5&#xa0;months</td>
<td align="left">Thyme-ivy syrup 5.4&#xa0;mL three times daily for 11&#xa0;days (15&#xa0;g thyme &#x2b;1.5&#xa0;g ivy extract/100&#xa0;g); placebo identical in appearance and flavour</td>
<td align="left">N &#x3d; 363<break/>Thyme-ivy combination<break/>Mean age &#xb1;SD:<break/>43.4 &#xb1; 17.7<break/>Placebo<break/>Mean age &#xb1;SD:<break/>41.5 &#xb1; 17.3<break/>acute bronchitis with productive cough</td>
<td align="left">PO: Change in mean frequency of daytime coughing fits (Days 7&#x2013;9 vs. Day 1)<break/>SO: Reduction in coughing fits (AUC), time to 50% reduction, proportion without coughing fits on Day 9, relative reduction at Day 9, investigator-assessed response, change in BSS, mucus expectoration, sleep disturbance, and general wellbeing (all assessed by diary or rating scales)<break/>AEs, vital signs, patient&#x2019;s and investigator&#x2019;s global judgement of tolerability at study end</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B19">Kemmerich, 2007</xref>) a double-blind, placebo- controlled, multicentre Phase IV study</td>
<td align="left">5 months</td>
<td align="left">Thyme&#x2013;primrose tablets<break/>160&#xa0;mg thyme &#x2b;60&#xa0;mg primrose extract/tablet or placebo</td>
<td align="left">N &#x3d; 362<break/>Thyme-primrose combination<break/>Mean age &#xb1;SD:<break/>41.9 &#xb1; 14.9<break/>Placebo<break/>Mean age &#xb1;SD:<break/>43.5 &#xb1; 16.4<break/>acute bronchitis with productive cough</td>
<td align="left">PO: Change in mean frequency of daytime coughing fits (Days 7&#x2013;9 vs. Day 1)<break/>SO: Reduction in coughing fits (AUC), time to 50% reduction, cough-free rate (Day 9), relative reduction at Day 9, investigator-assessed response, BSS change, mucus expectoration, sleep disturbance, and general wellbeing<break/>AEs, vital signs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B33">N&#xfa;&#xf1;ez et al., 2024</xref>)<break/>A pilot, randomized, double-blind, placebo- controlled, multicenter clinical trial</td>
<td align="left">14-day study: 7-day treatment, and 7-day safety follow-up</td>
<td align="left">Sediflu syrup 10&#xa0;mL BID for 7&#xa0;days</td>
<td align="left">N &#x3d; 56<break/>Mean age &#xb1;SD:<break/>8.65 &#xb1; a 2.14<break/>dry and/or productive cough</td>
<td align="left">PO: Change in day- and night-time CCS.<break/>SO: Tolerability (Paul&#x2019;s Night Cough Questionnaire)<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B48">Watson et al., 2008</xref>) randomized, placebo-controlled, double-blind trial</td>
<td align="left">4&#xa0;weeks</td>
<td align="left">purple passion fruit (PFP) peel extract<break/>(150&#xa0;mg/d) or placebo pills</td>
<td align="left">N &#x3d; 43<break/>PFP<break/>Mean age &#xb1;SD:<break/>36.4 &#xb1; 15.7<break/>Placebo<break/>Mean age &#xb1;SD:<break/>35.8 &#xb1; 11.5<break/>Asthma</td>
<td align="left">Asthma symptoms and spirometry (FVC, FEV<sub>1</sub>) at baseline and weekly<break/>AEs</td>
</tr>
<tr>
<td align="left">(<xref ref-type="bibr" rid="B52">Willcox et al., 2021</xref>)<break/>Feasibility double-blind randomized placebo-controlled clinical trial</td>
<td align="left">9&#xa0;months</td>
<td align="left">Pelargonium sidoides extract (EPs&#xae;7630, Kaloba&#xae;)<break/>Oral solution: 10&#xa0;g (&#x2248;9.75&#xa0;mL) contains 8.0&#xa0;g extract; Film-coated tablet: 20&#xa0;mg dry extract (1:8&#x2013;10)</td>
<td align="left">N &#x3d; 132 average age: 56&#x2013;59&#xa0;years<break/>acute cough due to lower respiratory tract infection</td>
<td align="left">Feasibility (recruitment, diary return/completion, antibiotic use, symptom duration/resolution, medication compliance), clinical (symptom duration, resolution at Day 7), and health-economic (EQ-5D-5L, NHS resource use, costs)<break/>AEs</td>
</tr>
</tbody>
</table>
<table-wrap-foot>
<fn>
<p>CSUI: cough associated stress urinary incontinence, ECG: electrocardiogram, EQ-5D-5L: EuroQol 5 Dimensions, 5 Levels, FEV<sub>1</sub>: Forced Expiratory Volume in 1&#xa0;s, FU: follow-up, FVC: forced vital capacity, HARQ: hull airway reflux questionnaire, J-LCQ: japanese version of the leicester cough questionnaire, LCQ: leicester cough questionnaire, MID: minimal important difference, NHS: national health service, PGIC: patient global impression of change, PO&#x201d; primary endpoint, PROs: Patient-Reported Outcomes, PFP: purple passion fruit, q.d.s.: four times daily, SO: secondary endpoint, t.i.d.: three times daily, UCC: unexplained chronic cough, VAS: visual analogue scale.</p>
</fn>
</table-wrap-foot>
</table-wrap>
<p>No additional records were identified through the gray literature search (Google Scholar), and no duplicates were detected. The updated search yielded no further eligible studies for inclusion in the systematic review or meta-analysis.</p>
<p>The pooled risk of bias assessment (<xref ref-type="fig" rid="F2">Figures 2</xref>, <xref ref-type="fig" rid="F3">3</xref>) confirmed that most studies were of low risk. Qualitative evaluation did not suggest substantial publication bias. Given the limited number of studies (n &#x3c; 10), funnel plots were used for illustrative purposes only, as recommended by Cochrane guidelines (<xref ref-type="bibr" rid="B17">Higgins et al., 2024</xref>). Visual inspection of the plots (<xref ref-type="sec" rid="s13">Supplementary Figures S1&#x2013;S4</xref>) showed no marked asymmetry, though the small sample precludes definitive conclusions.</p>
<fig id="F2" position="float">
<label>FIGURE 2</label>
<caption>
<p>Risk of bias summary. Review authors&#x2019; judgements about each risk of bias item for each included study.</p>
</caption>
<graphic xlink:href="fphar-17-1756578-g002.tif">
<alt-text content-type="machine-generated">Horizontal stacked bar chart displaying risk of bias assessments across seven study domains, with green indicating low risk and yellow indicating unclear risk; no high risk (red) is shown. Domains assessed include random sequence generation, allocation concealment, blinding of participants and personnel, blinding of outcome assessment, incomplete outcome data, selective reporting, and other bias, with most domains indicating a predominance of low risk of bias and varying proportions of unclear risk. Legend categorizes color codes for low, unclear, and high risk of bias.</alt-text>
</graphic>
</fig>
<fig id="F3" position="float">
<label>FIGURE 3</label>
<caption>
<p>Risk of bias graph. Review authors&#x2019; judgements about each risk of bias item presented as percentages across studies.</p>
</caption>
<graphic xlink:href="fphar-17-1756578-g003.tif">
<alt-text content-type="machine-generated">Risk of bias summary table for ten studies, with each row representing a study and columns for seven bias domains. Green circles with plus signs indicate low risk, yellow circles with question marks indicate unclear risk. Most studies show predominantly low risk of bias, with occasional unclear risk mainly in the domains of sequence generation, allocation concealment, and blinding.</alt-text>
</graphic>
</fig>
</sec>
<sec id="s3-2">
<label>3.2</label>
<title>P2X3: cough count (24&#xa0;h frequency, chronic cough)</title>
<p>Five studies (<xref ref-type="bibr" rid="B10">Dicpinigaitis et al., 2023</xref>; <xref ref-type="bibr" rid="B1">Abdulqawi et al., 2015</xref>; <xref ref-type="bibr" rid="B43">Smith et al., 2020a</xref>; <xref ref-type="bibr" rid="B44">Smith et al., 2020b</xref>; <xref ref-type="bibr" rid="B45">Smith et al., 2025</xref>) were included in the subgroup meta-analysis of 24-h cough frequency after P2X3 antagonist administration versus placebo. Due to varying dosages and study stages, data were analyzed in three subgroups: eliapixant, gefapixant, and camlipixant. The pooled analysis (814 experimental vs. 834 placebo participants) showed a significant reduction in cough frequency [SMD &#x3d; &#x2212;0.50, 95% CI (&#x2013;0.67, &#x2212;0.34), P &#x3c; 0.00001; I<sup>2</sup> &#x3d; 61%]. No significant subgroup differences were observed (P &#x3d; 0.11; I<sup>2</sup> &#x3d; 54.5%), with eliapixant demonstrating the greatest effect [SMD &#x3d; &#x2212;0.79, 95% CI (&#x2013;1.08, &#x2212;0.49), P &#x3c; 0.00001; I<sup>2</sup> &#x3d; 56%]. Results are presented in <xref ref-type="fig" rid="F4">Figure 4</xref>.</p>
<fig id="F4" position="float">
<label>FIGURE 4</label>
<caption>
<p>Standardized mean difference in 24-h cough frequency following P2X3 antagonist treatment in patients with chronic cough compared with placebo.</p>
</caption>
<graphic xlink:href="fphar-17-1756578-g004.tif">
<alt-text content-type="machine-generated">Meta-analysis forest plot comparing three drug subgroups&#x2014;Eliapixant, Gefapixant, and Camlipixant&#x2014;versus placebo on standard mean difference. Each study&#x27;s mean, standard deviation, group sizes, effect size, confidence intervals, and weights are shown. Summary diamonds for subgroups and total favor experimental groups, with all overall confidence intervals to the left of zero. Heterogeneity statistics are reported for each subgroup and overall.</alt-text>
</graphic>
</fig>
</sec>
<sec id="s3-3">
<label>3.3</label>
<title>Gefapixant: visual analogue scale (chronic cough)</title>
<p>Four studies (<xref ref-type="bibr" rid="B10">Dicpinigaitis et al., 2023</xref>; <xref ref-type="bibr" rid="B1">Abdulqawi et al., 2015</xref>; <xref ref-type="bibr" rid="B43">Smith et al., 2020a</xref>; <xref ref-type="bibr" rid="B44">Smith et al., 2020b</xref>) were included in the meta-analysis of Visual Analogue Scale (VAS) scores after gefapixant versus placebo. Data from 461 experimental and 465 placebo participants were analyzed, with some studies divided by dosage or observation period. The pooled analysis showed a significantly lower VAS score in the gefapixant group [SMD &#x3d; &#x2212;0.52, 95% CI (&#x2013;0.68, &#x2212;0.35), P &#x3c; 0.00001; I<sup>2</sup> &#x3d; 30%]. Results are presented in <xref ref-type="fig" rid="F5">Figure 5</xref>.</p>
<fig id="F5" position="float">
<label>FIGURE 5</label>
<caption>
<p>Standardized mean difference in Visual Analogue Scale (VAS) scores following gefapixant treatment in patients with chronic cough compared with placebo.</p>
</caption>
<graphic xlink:href="fphar-17-1756578-g005.tif">
<alt-text content-type="machine-generated">Forest plot and table summarizing standardized mean differences and confidence intervals for gefapixant versus placebo across several studies on cough outcomes, showing consistent benefit for gefapixant with a pooled effect size of -0.52 and moderate heterogeneity.</alt-text>
</graphic>
</fig>
</sec>
<sec id="s3-4">
<label>3.4</label>
<title>Gefapixant: leicester cough questionnaire (chronic cough)</title>
<p>Two studies (<xref ref-type="bibr" rid="B43">Smith et al., 2020a</xref>; <xref ref-type="bibr" rid="B44">Smith et al., 2020b</xref>) were included in the meta-analysis of Leicester Cough Questionnaire (LCQ) scores after gefapixant versus placebo. Data from 233 experimental and 240 placebo participants were analyzed, with study parts divided by dosage or design. The pooled analysis showed a significantly higher LCQ score in the gefapixant group [SMD &#x3d; 0.41, 95% CI (0.22, 0.60), P &#x3c; 0.0001; I<sup>2</sup> &#x3d; 10%]. Results are shown in <xref ref-type="fig" rid="F6">Figure 6</xref>.</p>
<fig id="F6" position="float">
<label>FIGURE 6</label>
<caption>
<p>Standardized mean difference in Leicester Cough Questionnaire (LCQ) scores following gefapixant treatment in patients with chronic cough compared with placebo.</p>
</caption>
<graphic xlink:href="fphar-17-1756578-g006.tif">
<alt-text content-type="machine-generated">Forest plot displaying standard mean differences between gefapixant and placebo groups from five studies, with all studies and the subtotal point estimates favoring the experimental group. Subtotal standard mean difference is 0.41 with confidence interval 0.22 to 0.60 and low heterogeneity.</alt-text>
</graphic>
</fig>
</sec>
<sec id="s3-5">
<label>3.5</label>
<title>P2X3: adverse events (chronic cough)</title>
<p>Eight studies (<xref ref-type="bibr" rid="B10">Dicpinigaitis et al., 2023</xref>; <xref ref-type="bibr" rid="B43">Smith et al., 2020a</xref>; <xref ref-type="bibr" rid="B44">Smith et al., 2020b</xref>; <xref ref-type="bibr" rid="B45">Smith et al., 2025</xref>; <xref ref-type="bibr" rid="B4">Birring et al., 2024</xref>; <xref ref-type="bibr" rid="B27">McGarvey et al., 2023</xref>; <xref ref-type="bibr" rid="B32">Niimi et al., 2022</xref>; <xref ref-type="bibr" rid="B30">Morice et al., 2021</xref>) were included in the meta-analysis of adverse events (AEs) after P2X3 antagonist administration versus placebo. Data from 1998 experimental and 2010 placebo participants were analyzed across four subgroups (gefapixant, eliapixant, sivopixant, camlipixant). The pooled analysis showed a higher incidence of AEs in the experimental group [RR &#x3d; 1.23, 95% CI (1.09, 1.38), P &#x3d; 0.0006; I<sup>2</sup> &#x3d; 75%], with significant subgroup differences (P &#x3d; 0.00004; I<sup>2</sup> &#x3d; 83.5%), indicating that AEs frequency varied by the type of P2X3. Results are presented in <xref ref-type="fig" rid="F7">Figure 7</xref>.</p>
<fig id="F7" position="float">
<label>FIGURE 7</label>
<caption>
<p>Risk ratio of adverse events (AEs) following P2X3 antagonist treatment in patients with chronic cough compared with placebo.</p>
</caption>
<graphic xlink:href="fphar-17-1756578-g007.tif">
<alt-text content-type="machine-generated">Forest plot summarizing risk ratios with ninety-five percent confidence intervals for four antitussive drugs versus placebo across multiple studies. Gepants show a statistically significant benefit, while eliapixant and camlipixant do not. Sivopixant demonstrates potential efficacy. Overall pooled analysis favors the experimental drugs.</alt-text>
</graphic>
</fig>
</sec>
<sec id="s3-6">
<label>3.6</label>
<title>Results of additional analyses</title>
<p>The certainty of evidence for all analyzed outcomes was evaluated according to the GRADE methodology (<xref ref-type="bibr" rid="B16">Guyatt et al., 2013</xref>). The summary of findings and corresponding GRADE ratings are presented in <xref ref-type="table" rid="T3">Table 3</xref>.</p>
<table-wrap id="T3" position="float">
<label>TABLE 3</label>
<caption>
<p>Summary of findings (SoF) of meta-analysis using working group grades of evidence (GRADE).</p>
</caption>
<table>
<thead valign="top">
<tr>
<th colspan="6" align="center">Continuous data</th>
</tr>
</thead>
<tbody valign="top">
<tr>
<td align="center">Patients, interventions, comparators</td>
<td colspan="2" align="center">Number of participants/studies</td>
<td align="center">Intervention vs. comparator standardized mean difference (95% CI)</td>
<td align="center">Comparator</td>
<td align="center">Certainty of the evidence (GRADE)</td>
</tr>
<tr>
<td align="center">Eliapixant vs. placebo</td>
<td colspan="2" align="center">209 vs. 222/1 study (divided into three)</td>
<td align="center">&#x2212;0.79 [&#x2212;1.08, &#x2212;0.49]<break/>Lower cough count in the experimental group. a moderate-to-large effect size, likely reflecting a meaningful clinical improvement<xref ref-type="table-fn" rid="Tfn2">
<sup>a</sup>
</xref>
</td>
<td align="center">The mean cough count (24&#xa0;h frequency)</td>
<td align="center">High<break/>&#x2295;&#x2295;&#x2295;&#x2295;</td>
</tr>
<tr>
<td align="center">Gefapixant vs. placebo</td>
<td colspan="2" align="center">419 vs. 423/4 studies (3 studies divided into several parts)</td>
<td align="center">&#x2212;0.43 [&#x2212;0.65, &#x2212;0.21]<break/>Lower cough count in the experimental group<break/>A small-to-moderate effect size, suggesting a modest but potentially meaningful clinical improvement<xref ref-type="table-fn" rid="Tfn2">
<sup>a</sup>
</xref>
</td>
<td align="center">The mean cough count (24&#xa0;h frequency)</td>
<td align="center">Moderate<break/>&#x2295;&#x2295;&#x2295;&#x25CB;</td>
</tr>
<tr>
<td align="center">Camlipixant vs. placebo</td>
<td colspan="2" align="center">186 vs. 189/1 study (divided into three)</td>
<td align="center">&#x2212;0.43 [&#x2212;0.64, &#x2212;0.23]<break/>Lower cough count in the experimental group<break/>A small-to-moderate effect size, indicating a modest but potentially meaningful clinical improvement<xref ref-type="table-fn" rid="Tfn2">
<sup>a</sup>
</xref>
</td>
<td align="center">The mean cough count (24&#xa0;h frequency)</td>
<td align="center">Moderate<break/>&#x2295;&#x2295;&#x2295;&#x25CB;</td>
</tr>
<tr>
<td align="center">Gefapixant vs. placebo</td>
<td colspan="2" align="center">461 vs. 465/4 studies (3 of them divided into several parts)</td>
<td align="center">&#x2212;0.52 [&#x2212;0.68, &#x2212;0.35]<break/>Lower VAS in the experimental group<break/>A moderate effect size, suggesting a clear and clinically relevant improvement<xref ref-type="table-fn" rid="Tfn2">
<sup>a</sup>
</xref>
</td>
<td align="center">The mean VAS</td>
<td align="center">High<break/>&#x2295;&#x2295;&#x2295;&#x2295;</td>
</tr>
<tr>
<td align="center">Gefapixant vs. placebo</td>
<td colspan="2" align="center">233 vs. 240/3 studies (1 of them divided into several parts)</td>
<td align="center">0.41 [0.22, 0.60]<break/>Higher LCQ in the experimental group<break/>A small-to-moderate effect size, suggesting a modest but noticeable clinical difference<xref ref-type="table-fn" rid="Tfn2">
<sup>a</sup>
</xref>
</td>
<td align="center">The mean LCQ</td>
<td align="center">High<break/>&#x2295;&#x2295;&#x2295;&#x2295;</td>
</tr>
<tr>
<td colspan="6" align="center">Dichotomous data</td>
</tr>
<tr>
<td rowspan="2" align="left">Outcomes</td>
<td colspan="2" align="center">Absolute Effect (95% CI)</td>
<td rowspan="2" align="center">Relative effect (95% CI)</td>
<td rowspan="2" align="center">Number of studies</td>
<td rowspan="2" align="center">Certainty of the evidence (GRADE)</td>
</tr>
<tr>
<td align="center">Risk with placebo</td>
<td align="center">Risk with experimental</td>
</tr>
<tr>
<td rowspan="2" align="left">Occurrence of adverts events<break/>Gefapixant vs. placebo</td>
<td align="center">648 per 1,000</td>
<td align="center">914 (785-1,000) per 1,000</td>
<td rowspan="2" align="center">RR 1.41 [1.21, 1.64]</td>
<td rowspan="2" align="center">4 studies (3 of them divided into several parts)</td>
<td rowspan="2" align="center">Low<break/>&#x2295;&#x2295;&#x25CB;&#x25CB;</td>
</tr>
<tr>
<td colspan="2" align="center">Absolute difference per 1,000:<break/>&#x2b;266 (&#x2b;137 do &#x2b;352)<break/>The relative risk of 1.41 (1.21&#x2013;1.64) indicates a significant 41% increase in risk</td>
</tr>
<tr>
<td rowspan="2" align="center">Occurrence of adverts events<break/>Eliapixant vs. placebo</td>
<td align="center">221 per 1,000</td>
<td align="center">217 (190&#x2013;245) per 1,000</td>
<td rowspan="2" align="center">RR 0.98 [0.86, 1.11]<xref ref-type="table-fn" rid="Tfn3">
<sup>b</sup>
</xref>
</td>
<td rowspan="2" align="center">3 studies divided into several parts</td>
<td rowspan="2" align="center">Low<break/>&#x2295;&#x2295;&#x25CB;&#x25CB;</td>
</tr>
<tr>
<td colspan="2" align="center">Absolute difference per 1,000:<break/>&#x2212;4 (&#x2212;31 to &#x2b;24)<break/>The relative risk of 0.98 (0.86&#x2013;1.11) suggests a small (2%) reduction in risk, but the result is not statistically significant</td>
</tr>
<tr>
<td rowspan="2" align="center">Occurrence of adverts events<break/>Sivipixant vs. placebo</td>
<td align="center">64 per 1,000</td>
<td align="center">113 (86&#x2013;147) per 1,000</td>
<td rowspan="2" align="center">RR 1.76 [1.35, 2.30]</td>
<td rowspan="2" align="center">2 studies (1 of them divided into several parts)</td>
<td rowspan="2" align="center">Moderate<break/>&#x2295;&#x2295;&#x2295;&#x25CB;</td>
</tr>
<tr>
<td colspan="2" align="center">Absolute difference per 1,000:<break/>&#x2b;49 (&#x2b;22 to &#x2b;83)<break/>The relative risk of 1.76 (1.35&#x2013;2.30) indicates a statistically significant 76% increase in risk</td>
</tr>
<tr>
<td rowspan="2" align="center">Occurrence of adverts events<break/>Camlipixant vs. placebo</td>
<td align="center">66 per 1,000</td>
<td align="center">56 (42&#x2013;75) per 1,000</td>
<td rowspan="2" align="center">RR 0.85 [0.63, 1.14]<xref ref-type="table-fn" rid="Tfn3">
<sup>b</sup>
</xref>
</td>
<td rowspan="2" align="center">1 study divided into several parts</td>
<td rowspan="2" align="center">Low<break/>&#x2295;&#x2295;&#x25CB;&#x25CB;</td>
</tr>
<tr>
<td colspan="2" align="center">Absolute difference per 1,000:<break/>&#x2212;10 (&#x2212;24 to &#x2b;9)<break/>The relative risk of 0.85 (0.63&#x2013;1.14) suggests a 15% relative reduction in risk<break/>But the result is not statistically significant</td>
</tr>
</tbody>
</table>
<table-wrap-foot>
<fn>
<p>95% CI: 95% Confidence interval; GRADE: working group grades of evidence, LCQ: leicester cough questionnaire, RR: risk ratio, VAS: visual analogue scale.</p>
</fn>
<fn>
<p>Explanations:</p>
</fn>
<fn id="Tfn2">
<label>
<sup>a</sup>
</label>
<p>According to Cohen&#x2019;s convention.</p>
</fn>
<fn id="Tfn3">
<label>
<sup>b</sup>
</label>
<p>Statistically insignificant outcome.</p>
</fn>
</table-wrap-foot>
</table-wrap>
</sec>
</sec>
<sec sec-type="discussion" id="s4">
<label>4</label>
<title>Discussion</title>
<p>This systematic review and meta-analysis included centrally, and peripherally acting medications commonly used to treat cough. The analysis aimed to assess their efficacy and safety based on the results of available RCTs. It should be emphasized that this study did not present quantitative data for codeine, butamirate, dextromethorphan, and levodropropizine. Only qualitative analysis was possible for these antitussives (<xref ref-type="table" rid="T2">Table 2</xref>). The inability to conduct a meta-analysis of the data from the included studies confirms previous observations that the available studies are characterized by significant heterogeneity. Furthermore, their conclusions are inconsistent. Consequently, it is impossible to draw clear conclusions about the efficacy of these medications in treating cough.</p>
<p>As shown in <xref ref-type="table" rid="T2">Table 2</xref>, the observed heterogeneity results from significant differences across studies, including drug doses used, therapy duration, methods of efficacy assessment, and heterogeneity in the patient population (age, cough etiology, and comorbidities). These factors contributed to the discrepancy in results and limited the comparability of data in this meta-analysis.</p>
<p>
<xref ref-type="bibr" rid="B11">Eccles et al. (1992)</xref> in a study using a 30&#xa0;mg codeine syrup, no significant differences in cough frequency or subjective cough severity were observed between the codeine and placebo groups, either in the laboratory or during home monitoring. These results suggest that cough mechanisms during viral infections may be poorly responsive to opioid antitussives, underscoring the need to explore alternative agents with distinct mechanisms of action.</p>
<p>Moreover, a study (<xref ref-type="bibr" rid="B42">Smith et al., 2006</xref>) in patients with stable COPD demonstrated that codeine, although considered a standard antitussive, did not significantly affect cough frequency or subjective cough severity compared with placebo. Despite a slight decrease in cough time after codeine administration compared to baseline, this difference was not statistically significant compared to the control group. These results suggest that cough mechanisms in COPD may be resistant to the effects of opioid antitussives, questioning the validity of using codeine as a reference point in studies of new antitussive agents.</p>
<p>Similarly, a clinical trial in children (<xref ref-type="bibr" rid="B3">Bhattacharya et al., 2013</xref>) with upper respiratory tract infection (URTI) found that neither dextromethorphan nor promethazine was more effective than placebo at reducing nocturnal cough or improving sleep quality. Analogously, a study of adults with URTI (<xref ref-type="bibr" rid="B22">Lee et al., 2000</xref>) showed no significant advantage over placebo in relieving cough.</p>
<p>These results emphasize that the routine use of antitussives in children and adults with acute upper respiratory tract infection is unjustified, and the effectiveness of both opioid and non-opioid antitussives remains limited. The antitussive effect of dextromethorphan in acute URTI is marginal at best, casting doubt on its routine use in treating viral cough.</p>
<p>Contrary results were obtained in a recent clinical trial in children aged 6&#x2013;11&#xa0;years with cough associated with colds (<xref ref-type="bibr" rid="B28">Meeves et al., 2023</xref>) Multiple doses of dextromethorphan hydrobromide resulted in statistically significant, although modest, reductions in cough frequency and severity compared with placebo. This effect was most pronounced during the day, but there were no differences between groups in nocturnal cough frequency or sleep quality. These results suggest that dextromethorphan may have some antitussive efficacy in children, particularly for daytime cough, although its effect remains limited. Furthermore, the study highlights the importance of using objective, validated cough assessment tools in the pediatric population to increase the sensitivity of analyses of antitussive efficacy.</p>
<p>Other observations were reported in a study evaluating the efficacy of codeine and levodropropizine in patients with chronic cough (<xref ref-type="bibr" rid="B24">Lee et al., 2022</xref>). Codeine was significantly more effective than levodropropizine in reducing cough severity, as confirmed by changes in the VAS, Cough Severity Scale (CSS), and LCQ. Adverse events such as drowsiness, constipation, and headache were more frequently observed in the codeine-treated group, although these did not lead to a higher number of treatment discontinuations. These results indicate that codeine may be more effective in relieving chronic cough, but its use is associated with the risk of side effects typical of opioid medications. In contrast, levodropropizine, despite being slightly less effective, has a more favorable safety profile, making it a potentially better choice for long-term therapy.</p>
<p>The present review also identified several studies evaluating natural antitussive agents that could not be included in the quantitative synthesis due to substantial heterogeneity in study design, methodology, outcome measures, endpoints, and study populations.</p>
<p>Similarly, studies assessing natural or plant-based preparations demonstrated encouraging yet inconsistent results. Barth et al. showed that a combination of aqueous ethanolic extracts of <italic>Justicia adhatoda</italic> L. leaf, <italic>Echinacea purpurea</italic> (L.) Moench root and Eleutherococcus senticosus Harms root have an antitussive effect in patients aged 18&#x2013;65&#xa0;years with non-complicated URTI (<xref ref-type="bibr" rid="B2">Barth et al., 2015</xref>). What is more, another study (<xref ref-type="bibr" rid="B6">Canciani et al., 2014</xref>) confirmed that the use of Grintuss&#xae; syrup containing resins, polysaccharides, saponins, flavonoids and sugars derived from <italic>Grindelia robusta, Plantago lanceolata, Helichrysum italicum</italic> and honey leads to an improvement in cough symptoms in children, especially nocturnal cough, after just 4&#xa0;days of use. Carnevall et al. also demonstrated that KalobaTUSS&#xae; syrup (acacia honey in combination with <italic>Malva sylvestris, Inula helenium, Plantago major, and Helichrysum stoechas</italic> extracts) reduced the severity and duration of daytime and nighttime cough in children with acute cough. However, it should be noted that these two studies focused on entirely different ingredients, so there is considerable risk in interpreting the results comprehensively (<xref ref-type="bibr" rid="B7">Carnevali et al., 2021</xref>). Another new substance was investigated in a study conducted in Iran (<xref ref-type="bibr" rid="B15">Ghaemi et al., 2020</xref>), which showed that lozenges containing licorice root extract (<italic>Glycyrrhiza glabra L</italic>.) effectively relieved symptoms of chronic cough of unknown etiology. After 2&#xa0;weeks of treatment and at a four-week follow-up, a significant reduction in cough severity was observed compared to placebo, while quality of life, as assessed by the LCQ, improved.</p>
<p>It is also worth mentioning a study combining conventional asthma therapy with a traditional Chinese medicine preparation (<xref ref-type="bibr" rid="B35">Pan et al., 2025</xref>). This study demonstrated that Suhuang Zhike capsules can be an effective and safe adjunct to therapy in patients with mild to moderate asthma whose symptoms were inadequately controlled despite inhaled corticosteroids (ICS) and long-acting beta<sub>2</sub>-agonists (LABA) therapy. Although no significant improvement in Asthma Control Test (ACT) scores was observed in the overall population, a subgroup analysis of patients on stable treatment prior to enrollment demonstrated significant clinical improvement and reduced cough severity.</p>
<p>Another study (<xref ref-type="bibr" rid="B33">N&#xfa;&#xf1;ez et al., 2024</xref>) showed that Sedifl&#xf9; syrup, containing active plant ingredients, effectively relieved cough during both the day and the night in children with upper respiratory tract infections. Significant improvement in cough severity was observed after just 2&#xa0;days of treatment, and this effect persisted and intensified in subsequent days.</p>
<p>It should be emphasized, however, that the studies discussed in this paper differed significantly in terms of design, population, intervention type, and endpoints, which prevented their direct comparison in a meta-analysis. Some studies included preparations with mechanical or protective effects (Grintuss&#xae;, KalobaTUSS&#xae;, Sedifl&#xf9;), while others involved herbal products with potential anti-inflammatory or immunomodulatory effects (licorice, Suhuang Zhike, Xiehuangjiejing). The patient populations also varied, from children with acute infectious cough to patients with chronic cough or asthma, as did the intervention duration and methods for assessing efficacy (symptom scales, LCQ, VAS). Despite favorable clinical outcomes and a good safety profile, these results should be interpreted with caution because they come from studies of varying methodological quality and often a limited number of participants.</p>
<p>While several trials reported modest symptomatic relief, particularly in cough frequency and sleep quality, methodological weaknesses and lack of standardized outcomes considerably limit the strength and generalizability of these findings. Together, these observations underscore the urgent need for more rigorous, harmonized clinical trials with standardized outcome measures, adequate sample sizes, and improved study designs to assess better the comparative efficacy of both pharmacological and natural antitussive therapies.</p>
<p>The meta-analysis revealed that among the available RTCs on antitussive medications, those on P2X3 receptor antagonists demonstrated the greatest methodological consistency, particularly in the outcome measures used. Therefore, statistical analyses could be performed primarily for this group of medications, yielding reliable, comparable results on their efficacy and safety. Other interventions, due to the heterogeneity of cough assessment methods and the limited number of studies, could not be included in the quantitative analysis. This represents a significant limitation but also highlights the methodological advances in research on P2X3 antagonists.</p>
<p>The subgroup analysis revealed no statistically significant differences between P2X3 antagonists, indicating a consistent treatment effect across compounds. All subgroups demonstrated a reduction in cough frequency, suggesting that the observed effect is a class-related response rather than compound-specific.</p>
<p>After gefapixant administration, we also observed a statistically significant lower VAS score and a higher LCQ score, with a moderate, potentially clinically relevant effect and high certainty of evidence compared to placebo. In addition, after gefapixant administration, we observed that the intervention increased the risk of AEs by 41% compared with the placebo group, with low certainty of evidence. Also, sivopixant increased the risk of AEs by approximately 76% compared to the placebo group with moderate certainty of evidence. In contrast, eliapixant and camlipixant administration resulted in reductions of AEs of 2% and 15%, respectively, with low certainty of evidence. Furthermore, we noted that the type of P2X3 receptor has a significant impact on AEs frequency.</p>
<p>The GRADE assessment showed varying levels of evidence certainty across outcomes. Low heterogeneity, consistent effects, and narrow confidence intervals characterized high-certainty results. Moderate and low certainty were mainly due to heterogeneity, wide intervals, or a limited number of studies. Despite these differences, the overall results consistently indicated a beneficial effect of the intervention, supporting its clinical relevance.</p>
<p>The obtained results are consistent with previous meta-analyses and systematic reviews (<xref ref-type="bibr" rid="B39">Ramadan et al., 2023</xref>; <xref ref-type="bibr" rid="B53">Yamamoto et al., 2024</xref>), which also indicated the high efficacy of P2X3 receptor antagonists in reducing cough frequency in patients with refractory chronic cough.</p>
<p>From a clinical perspective, recent findings, together with our results, support the potential role of P2X3 antagonists as a targeted therapeutic option primarily for patients with refractory or unexplained chronic cough. By directly modulating cough hypersensitivity at the level of peripheral sensory pathways, these agents offer a mechanism-based, symptom-oriented approach rather than a replacement for etiological treatment, which remains the cornerstone of chronic cough management. Based on available clinical evidence, P2X3 antagonists may be best positioned as add-on or later-line therapies for patients whose symptoms persist despite optimized standard care. This treatment strategy aligns with emerging views that modulation of sensory neural pathways represents a promising adjunct approach in the management of chronic cough.</p>
<p>Safety and tolerability are central to the clinical implementation of P2X3 antagonists, particularly given their intended use in long-term treatment of chronic cough. In clinical studies with gefapixant, a high incidence of taste-related adverse effects has been reported, attributed to inhibition of the heteromeric P2X2/3 receptor (<xref ref-type="bibr" rid="B53">Yamamoto et al., 2024</xref>; <xref ref-type="bibr" rid="B13">Francke et al., 2025</xref>). Consequently, the development of more selective P2X3 antagonists has been pursued to improve tolerability while maintaining efficacy (<xref ref-type="bibr" rid="B13">Francke et al., 2025</xref>). <xref ref-type="bibr" rid="B30">Morice et al. (2021)</xref> showed that taste-related adverse events following eliapixant administration were less frequent at therapeutic doses than with the less selective P2X3 antagonist gefapixant. Although generally reversible upon discontinuation of treatment, taste-related adverse effects may negatively affect treatment adherence, especially during prolonged therapy. Significantly, the development of next-generation P2X3 antagonists with increased receptor selectivity has been associated with a lower incidence and severity of taste disturbances, suggesting a more favorable tolerability profile and supporting the feasibility of chronic administration. On the other hand, <xref ref-type="bibr" rid="B30">Morice et al. (2021)</xref> hypothesized that filapixant would be associated with a lower incidence of taste-related adverse effects compared with the non-selective P2X3/P2X2/3 antagonist gefapixant and the less selective P2X3 antagonist eliapixant. However, the results of their study were unexpected. Although filapixant was generally well tolerated, the frequency of taste-related adverse events was higher than anticipated. Therefore, further studies are required to evaluate sustained tolerability, optimal dosing strategies that balance efficacy and adverse effects, and to identify patient subgroups most likely to benefit from therapy with minimal impact on quality of life. Such data will be essential for defining the role of P2X3 antagonists within future chronic cough management algorithms and for informing clinical decision-making in routine practice.</p>
</sec>
<sec id="s5">
<label>5</label>
<title>Limitations</title>
<p>This meta-analysis included only pharmacological agents classified as antitussive drugs, acting directly on the cough reflex through central or peripheral mechanisms. Medications that may indirectly reduce cough by treating underlying airway inflammation or hyperresponsiveness, such as inhaled corticosteroids, leukotriene receptor antagonists, or bronchodilators, were not included. Therefore, the results primarily reflect the efficacy of classical antitussive therapy rather than broader pharmacological strategies targeting disease-specific mechanisms. This may limit the generalizability of the findings to patients whose cough is secondary to inflammatory or allergic airway disorders, such as asthma or eosinophilic bronchitis.</p>
<p>The available evidence may be influenced by publication bias, as studies with positive outcomes are more likely to be published, potentially overestimating the therapeutic efficacy of novel antitussive agents. Second, substantial heterogeneity exists across studies in terms of outcome measures, including differences in cough frequency assessment, patient-reported endpoints, and study duration, which limits direct comparability and quantitative synthesis of results. Finally, while P2X3 receptor antagonists are supported by the most robust clinical data to date, the number of high-quality, randomized trials evaluating alternative mechanistic targets remains limited. This imbalance limits broader conclusions about the relative efficacy of non-P2X3 therapies and underscores the need for well-designed trials across diverse antitussive strategies.</p>
<p>Although the literature search included both acute and chronic cough, only studies focusing on chronic cough met the inclusion criteria for quantitative synthesis. As a result, the meta-analysis and forest plots reflect evidence exclusively related to chronic cough. The absence of eligible studies on acute cough highlights a gap in the current literature and limits the generalizability of the findings to chronic cough populations only. Consequently, conclusions regarding the efficacy of P2X3 antagonists should not be extrapolated to acute cough.</p>
<p>Another limitation of this work is the inclusion of only English-language publications, which may have introduced a language-related selection bias. As a result, relevant studies published in other languages, particularly those originating from regions with extensive research on traditional medicine, such as China, may not have been captured. Numerous studies have investigated traditional herbal remedies with potential antitussive effects, however, many were excluded due to language restrictions and classification difficulties. Consequently, the exclusion of non-English studies and traditional herbal formulations may limit the completeness of the evidence base and should be considered when interpreting the findings of this review.</p>
</sec>
<sec id="s6">
<label>6</label>
<title>Conslusions</title>
<p>Our study confirms that despite the long history of use of codeine and other antitussives, both centrally (butamirate, dextromethorphan) and peripherally (levodropropizine), evidence for their effectiveness remains limited, and the available data are scattered and inconsistent. In recent years, there has been growing interest in natural preparations as alternatives to traditional antitussives. However, their efficacy and safety remain inconsistent, highlighting the need for further, high-quality clinical trials. P2X3 receptor antagonists deserve particular attention, as they have shown potential to reduce cough frequency and severity in available studies. In addition, all P2X3 antagonists reduced cough frequency, with no significant differences between compounds. Accordingly, P2X3 represents a promising direction for the development of new therapies. In this context, the concept of &#x201c;beyond codeine&#x201d; takes on particular significance&#x2013;it encompasses not only the search for more effective and safer synthetic drugs but also the development of therapies targeting new, peripheral molecular targets, such as P2X3 receptors.</p>
</sec>
</body>
<back>
<sec sec-type="data-availability" id="s7">
<title>Data availability statement</title>
<p>The original contributions presented in the study are included in the article/<xref ref-type="sec" rid="s13">Supplementary Material</xref>, further inquiries can be directed to the corresponding author.</p>
</sec>
<sec sec-type="author-contributions" id="s8">
<title>Author contributions</title>
<p>MM: Conceptualization, Data curation, Formal Analysis, Investigation, Methodology, Writing &#x2013; original draft, Writing &#x2013; review and editing. RP: Data curation, Investigation, Project administration, Writing &#x2013; review and editing.</p>
</sec>
<sec sec-type="COI-statement" id="s10">
<title>Conflict of interest</title>
<p>The author(s) declared that this work was conducted in the absence of any commercial or financial relationships that could be construed as a potential conflict of interest.</p>
</sec>
<sec sec-type="ai-statement" id="s11">
<title>Generative AI statement</title>
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<title>Publisher&#x2019;s note</title>
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</sec>
<sec sec-type="supplementary-material" id="s13">
<title>Supplementary material</title>
<p>The Supplementary Material for this article can be found online at: <ext-link ext-link-type="uri" xlink:href="https://www.frontiersin.org/articles/10.3389/fphar.2026.1756578/full#supplementary-material">https://www.frontiersin.org/articles/10.3389/fphar.2026.1756578/full&#x23;supplementary-material</ext-link>
</p>
<supplementary-material xlink:href="Supplementaryfile1.docx" id="SM1" mimetype="application/docx" xmlns:xlink="http://www.w3.org/1999/xlink"/>
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<bold>Edited by:</bold> <ext-link ext-link-type="uri" xlink:href="https://loop.frontiersin.org/people/15918/overview">Donald C. Bolser</ext-link>, University of Florida, United States</p>
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<ext-link ext-link-type="uri" xlink:href="https://loop.frontiersin.org/people/3317976/overview">Syed A. Rizvi</ext-link>, Larkin University, United States</p>
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