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<front>
<journal-meta>
<journal-id journal-id-type="publisher-id">BR</journal-id>
<journal-title-group>
<journal-title>Biomedical Reports</journal-title>
</journal-title-group>
<issn pub-type="ppub">2049-9434</issn>
<issn pub-type="epub">2049-9442</issn>
<publisher>
<publisher-name>D.A. Spandidos</publisher-name>
</publisher>
</journal-meta>
<article-meta>
<article-id pub-id-type="publisher-id">BR-23-6-02073</article-id>
<article-id pub-id-type="doi">10.3892/br.2025.2073</article-id>
<article-categories>
<subj-group subj-group-type="heading">
<subject>Articles</subject>
</subj-group>
</article-categories>
<title-group>
<article-title>Systematic review and meta-analysis of risk prediction models for retinopathy of prematurity in preterm infants</article-title>
</title-group>
<contrib-group>
<contrib contrib-type="author" corresp="yes">
<name><surname>Li</surname><given-names>Li</given-names></name>
<xref rid="af1-BR-23-6-02073" ref-type="aff"/>
<xref rid="c1-BR-23-6-02073" ref-type="corresp"/>
</contrib>
<contrib contrib-type="author">
<name><surname>Gao</surname><given-names>Yanlin</given-names></name>
<xref rid="af1-BR-23-6-02073" ref-type="aff"/>
</contrib>
<contrib contrib-type="author">
<name><surname>Chen</surname><given-names>Wei</given-names></name>
<xref rid="af1-BR-23-6-02073" ref-type="aff"/>
</contrib>
<contrib contrib-type="author">
<name><surname>Han</surname><given-names>Mei</given-names></name>
<xref rid="af1-BR-23-6-02073" ref-type="aff"/>
</contrib>
</contrib-group>
<aff id="af1-BR-23-6-02073">Tianjin Key Laboratory of Ophthalmology and Vision Science, Tianjin Eye Hospital, Tianjin 300020, P.R. China</aff>
<author-notes>
<corresp id="c1-BR-23-6-02073"><italic>Correspondence to:</italic> Dr Li Li, Tianjin Key Laboratory of Ophthalmology and Vision Science, Tianjin Eye Hospital, 4 Gansu Road, Heping, Tianjin 300020, P.R. China <email>liliwf2001@163.com</email></corresp>
</author-notes>
<pub-date pub-type="collection"><month>12</month><year>2025</year></pub-date>
<pub-date pub-type="epub"><day>22</day><month>10</month><year>2025</year></pub-date>
<volume>23</volume>
<issue>6</issue>
<elocation-id>195</elocation-id>
<history>
<date date-type="received">
<day>15</day>
<month>05</month>
<year>2025</year>
</date>
<date date-type="accepted">
<day>04</day>
<month>08</month>
<year>2025</year>
</date>
</history>
<permissions>
<copyright-statement>Copyright: &#x00A9; 2025 Li et al.</copyright-statement>
<copyright-year>2025</copyright-year>
<license license-type="open-access">
<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-nc/4.0/">Creative Commons Attribution License</ext-link>, which permits unrestricted use, distribution, reproduction and adaptation in any medium and for any purpose provided that it is properly attributed. For attribution, the original author(s), title, publication source (PeerJ) and either DOI or URL of the article must be cited, the use is non-commercial and no modifications or adaptations are made.</license-p></license>
</permissions>
<abstract>
<p>Retinopathy of prematurity (ROP) is a proliferative vascular disease affecting preterm infants with incompletely developed retinal vasculature, characterized by abnormal vascular proliferation that can lead to retinal detachment and blindness. Given its impact on neonatal visual health, developing reliable risk prediction models for ROP has become crucial for optimizing clinical screening and intervention strategies. However, existing models exhibit substantial heterogeneity in methodology, validation, and performance, limiting their generalizability across diverse clinical settings. The present study aimed to evaluate and summarize the effectiveness of existing ROP risk prediction models in preterm infants through a systematic review and meta-analysis, with the goal of providing reliable clinical screening tools based on effectiveness metrics. A systematic search was conducted across PubMed, Cochrane Library, Web of Science and Embase databases using a strategy that combined MeSH terms and free-text words to identify literature associated with risk prediction models for ROP in preterm infants. The risk of bias was assessed using the PROBAST tool. Statistical analysis involved data synthesis, heterogeneity testing, subgroup and sensitivity analyses, and publication bias assessment. A total of 492 relevant articles were retrieved; following deduplication and screening, 28 articles involving ROP risk prediction models were included. The included studies were published between 2009 and 2025, with sample sizes ranging from 90 to 22,569 participants, and a total sample size of 72,991. A total of 16 studies did not specify the validation method, five conducted external validation, two performed both internal and external validation, and five performed only internal validation. PROBAST assessment revealed that all included models had a moderate risk of bias, primarily attributed to the retrospective nature of the study design, inconsistent variable measurement and inadequate control of confounding factors. Meta-analysis showed that the pooled area under the receiver operating characteristic curve (AUC) was 0.87 (95&#x0025; CI: 0.34; 0.99), indicating good discriminative ability of the models. However, significant heterogeneity was observed (I&#x00B2;=99.2&#x0025;, P&#x003C;0.05). Subgroup analysis by model type demonstrated significant heterogeneity in both traditional statistical (I&#x00B2;=92.2&#x0025;) and machine learning models (I&#x00B2;=97.3&#x0025;). Subgroup analysis by study region showed no significant heterogeneity in studies from South America (I&#x00B2;=0&#x0025;), while high heterogeneity was found in studies from Asia and North America + Europe (I&#x00B2;=96.6 and 93.6&#x0025;, respectively). This may be associated with cross-regional differences in population characteristics (such as ethnicity and disease spectra) and variations in medical standards. Funnel plot and Peters&#x0027; bias test indicated high reliability of the overall study conclusions, and the results of the sensitivity analysis were stable. However, some studies had small sample sizes and single-center designs, leading to selection bias. Additionally, multiple studies lacked model validation, and samples were limited to specific regions, failing to cover diverse healthcare settings and ethnic groups. In conclusion, current ROP risk prediction models for preterm infants exhibit good clinical application potential, with certain discriminative and predictive abilities, which can provide references for clinical screening. However, the risk of bias and insufficient validation limit their generalization ability. Future studies should expand sample sizes through prospective designs, strengthen external validation and optimize model development to improve prediction accuracy and universality, addressing the identified risks of bias and limited generalizability.</p>
</abstract>
<kwd-group>
<kwd>preterm infant</kwd>
<kwd>retinopathy of prematurity</kwd>
<kwd>prediction model</kwd>
<kwd>systematic review</kwd>
<kwd>meta-analysis</kwd>
</kwd-group>
<funding-group>
<funding-statement><bold>Funding:</bold> The present study was supported by the National Natural Science Foundation of China (grant no. 82160205) and the Tianjin Key Medical Discipline (Specialty) Construction Project (grant no. TJYXZDXK-3-004A-3).</funding-statement>
</funding-group>
</article-meta>
</front>
<body>
<sec sec-type="intro">
<title>Introduction</title>
<p>Retinopathy of prematurity (ROP) is a proliferative vascular disease that occurs in areas of the retina where vascular development is incomplete in preterm infants. It is characterized by abnormal blood vessel proliferation, which can lead to retinal detachment and blindness (<xref rid="b1-BR-23-6-02073" ref-type="bibr">1</xref>). A meta-analysis involving 121,618 preterm infants reported that the global incidence of ROP in preterm infants is 31.9&#x0025;, with the incidence of severe ROP at 7.5&#x0025; (<xref rid="b2-BR-23-6-02073" ref-type="bibr">2</xref>). A cohort study (<xref rid="b3-BR-23-6-02073" ref-type="bibr">3</xref>) conducted in the United States from 2003 to 2019 involving 125,212 cases of ROP showed that the overall incidence of ROP in premature infants increased from 4.4 to 8.1&#x0025;; the incidence in African-American infants rose from 5.8 to 11.6&#x0025; and that in infants from low-income families rose from 4.9 to 9.0&#x0025;; and the increase was the greatest in the southern region (3.7 to 8.3&#x0025;). Therefore, there are certain differences in the incidence of ROP in various regions and populations, and it is necessary to develop risk prediction models for different groups. Clinically, the diagnosis and severity assessment of ROP are based on the International Classification of Retinopathy of Prematurity, 3rd Edition (ICROP3), released in 2021. This classification systematically defines the lesion location, progression extent and risk level of ROP through indicators including lesion zones I-III, disease stages 1-5 and plus disease (severe retinal vascular dilation and tortuosity in the posterior pole), thereby providing a foundation for clinical diagnosis (<xref rid="b4-BR-23-6-02073" ref-type="bibr">4</xref>).</p>
<p>Current research suggests that the pathogenesis of ROP is characterized by a biphasic pattern of retinal vascular development: An initial phase of reduced retinal vascular growth, followed by excessive vessel proliferation into the vitreous body (<xref rid="b5-BR-23-6-02073" ref-type="bibr">5</xref>). Vascular endothelial growth factor (VEGF) serves a critical role in retinal neovascularization. In recent years, therapeutic approaches have shifted from laser therapy to anti-VEGF therapy (<xref rid="b6-BR-23-6-02073" ref-type="bibr">6</xref>). The RAINBOW Extension study confirmed that ranibizumab, when administered to preterm infants with ROP, significantly decreases the risk of high myopia (<xref rid="b7-BR-23-6-02073" ref-type="bibr">7</xref>). However, follow-up studies (<xref rid="b8-BR-23-6-02073" ref-type="bibr">8</xref>,<xref rid="b9-BR-23-6-02073" ref-type="bibr">9</xref>) have indicated that infants receiving anti-VEGF therapy may have a higher risk of adverse neurodevelopmental outcomes. Furthermore, in remote areas, the lack of medical resources and equipment can lead to worsening conditions in preterm infants, resulting in blindness (<xref rid="b10-BR-23-6-02073" ref-type="bibr">10</xref>). Therefore, compared with single biomarkers or imaging examinations, ROP prediction models have value in integrating multi-dimensional clinical data to achieve dynamic risk stratification. Particularly in resource-poor regions, these models may compensate for the insufficiency of fundus screening equipment, enabling the rapid identification of high-risk preterm infants through basic indicators. To obtain more practical evidence for ROP risk prediction, current research (<xref rid="b11-BR-23-6-02073" ref-type="bibr">11</xref>) focuses on early disease risk prediction, conducting large-scale clinical cohort studies, and developing new artificial intelligence/machine learning algorithms to enhance the accuracy and practicality of ROP risk prediction. However, with the development of computer vision and deep learning algorithms, despite the continuous emergence of various prediction models and algorithms, challenges such as overfitting and insufficient data diversity remain. There is significant heterogeneity among studies (<xref rid="b12-BR-23-6-02073" ref-type="bibr">12</xref>,<xref rid="b13-BR-23-6-02073" ref-type="bibr">13</xref>) in terms of sample size, predictors, model construction methods and reported performance metrics, and there are relatively few systematic reviews on the diagnostic performance of these models (<xref rid="b14-BR-23-6-02073" ref-type="bibr">14</xref>,<xref rid="b15-BR-23-6-02073" ref-type="bibr">15</xref>).</p>
<p>Almutairi <italic>et al</italic> (<xref rid="b10-BR-23-6-02073" ref-type="bibr">10</xref>) performed a meta-analysis that focused on the association between platelet count, thrombocytopenia and severe ROP, and explored the potential mechanisms linking a single biomarker to the disease through methods such as Bayesian model averaging. However, this previous study was limited to the causal exploration of a single risk factor, failing to involve the systematic integration and methodological evaluation of existing multifactorial ROP risk prediction models. It also did not assess differences in applicability of various predictive tools in clinical settings, and did not provide a comprehensive understanding and basis for selecting ROP risk screening tools. The present study aimed to overcome the limitations of single-factor association studies by conducting a systematic review and meta-analysis on risk prediction models for ROP in preterm infants. It systematically organizes, synthesizes and evaluates the methodological characteristics and application potential of existing models, thereby providing a design framework for the rational selection and optimization of ROP risk prediction models in clinical practice.</p>
</sec>
<sec sec-type="Materials|methods">
<title>Materials and methods</title>
<sec>
<title/>
<sec>
<title>Study design</title>
<p>The present study adhered to the Transparent Reporting of a Multivariable Prediction Model for Individual Prognosis Or Diagnosis statement (<xref rid="b16-BR-23-6-02073" ref-type="bibr">16</xref>), and followed the critical appraisal and data extraction checklist of Critical Appraisal and Data Extraction for Systematic Reviews of Prediction Modelling Studies (<xref rid="b17-BR-23-6-02073" ref-type="bibr">17</xref>). The study did not involve human experiments or direct collection of clinical data, thus no ethics committee approval was required. The key items of the systematic review were as follows: People, preterm infants; intervention model, development and publication of risk prediction models for ROP in preterm infants; comparator, no competing model; outcome, incidence of ROP in preterm infants (primary) and performance metrics of the prediction model (secondary); timing, from birth of preterm infants until ROP stabilizes or the relevant observation period ends and setting, healthcare settings, including neonatal intensive care units, pediatric wards and specialized ophthalmic clinics in hospitals of various levels.</p>
</sec>
<sec>
<title>Search strategy</title>
<p>A comprehensive literature search was conducted using the PubMed (<ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="http://pubmed.ncbi.nlm.nih.gov/">pubmed.ncbi.nlm.nih.gov/</ext-link>), Cochrane Library (<ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="http://cochranelibrary.com/">cochranelibrary.com/</ext-link>), Web of Science (<ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="https://www.webofscience.com/">https://www.webofscience.com/</ext-link>) and Embase (<ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="https://www.embase.com/">https://www.embase.com/</ext-link>) databases to identify studies associated with ROP in preterm infants. The core search terms used across the four databases are as follows: PubMed: &#x2018;Infant, Premature&#x2019; (MeSH), &#x2018;Infant, Extremely Premature&#x2019; (MeSH), &#x2018;Retinopathy of Prematurity&#x2019; (MeSH), &#x2018;Retinal Diseases&#x2019; (MeSH), &#x2018;Area Under Curve&#x2019; (MeSH); Web of Science: core topic terms including &#x2018;Infant, Premature&#x2019;, &#x2018;Infant, Extremely Premature&#x2019;, &#x2018;Retinopathy of Prematurity&#x2019;, &#x2018;Retinal Diseases&#x2019;, &#x2018;Area Under Curve&#x2019;, &#x2018;AUC&#x2019;; Embase: &#x2018;prematurity&#x2019;/exp, &#x2018;retrolental fibroplasia&#x2019;/exp, &#x2018;retina disease&#x2019;/exp, &#x2018;area under the curve&#x2019;/exp; Cochrane Library: &#x2018;Infant, Premature&#x2019; (explode all trees), &#x2018;Infant, Extremely Premature&#x2019; (explode all trees), &#x2018;Retinal Diseases&#x2019; (explode all trees), &#x2018;Retinopathy of Prematurity&#x2019; (explode all trees), &#x2018;Area Under Curve&#x2019; (explode all trees). A detailed search strategy is provided in <xref rid="SD1-BR-23-6-02073" ref-type="supplementary-material">Table SI</xref>, <xref rid="SD2-BR-23-6-02073" ref-type="supplementary-material">Table SII</xref>, <xref rid="SD3-BR-23-6-02073" ref-type="supplementary-material">Table SIII</xref> and <xref rid="SD4-BR-23-6-02073" ref-type="supplementary-material">Table SIV</xref>. To minimize discrepancies from database updates, searches were conducted from database inception until April 18, 2025, with all data collection completed by this date.</p>
</sec>
<sec>
<title>Inclusion and exclusion criteria</title>
<p>The inclusion criteria were as follows: i) Cross-sectional, cohort, retrospective or prospective studies; ii) Diagnosis of ROP according to ICROP3(<xref rid="b4-BR-23-6-02073" ref-type="bibr">4</xref>), based on the affected area (zone I, II or III), disease stage (stage 1-5) and retinal vascular abnormalities &#x005B;pre-plus disease (mild retinal vascular dilation and tortuosity confined to the posterior pole, not meeting the severity threshold for plus disease) or plus disease (severe retinal vascular dilation and tortuosity involving the posterior pole, typically affecting at least two quadrants, as defined by ICROP3 to indicate advanced disease severity)&#x005D; to determine disease severity; iii) studies focusing on the development, validation or evaluation of ROP prediction models in preterm infants; iv) study subjects including preterm infants with a birth weight of &#x2265;500 g or gestational age of &#x003C;37 weeks; v) prediction model including &#x2265;2 predictors; vi) models associated with the occurrence, screening or risk prediction of ROP, including traditional statistical models (such as logistic regression) and machine learning algorithms (such as decision trees and neural networks); vii) study providing statistical indicators related to the model, such as the area under the receiver operating characteristic curve (AUC) and viii) English literature. The exclusion criteria were as follows: i) Systematic reviews, meta-analyses or other types of review articles; ii) studies that did not provide quantitative results for the prediction model, or where key data were unavailable or there was a substantial amount of missing data; iii) studies involving children with severe congenital malformation, complex systemic disease or other ocular disease; iv) studies lacking a control group or with unclear control group definitions; v) unclear sample definitions or a large number of non-preterm infants and vii) conference abstracts, editorials or studies on radiomics.</p>
</sec>
<sec>
<title>Literature screening</title>
<p>The literature screening was conducted using the EndNote reference management tool (version 21, <ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="http://endnote.com/">endnote.com/</ext-link>). Two authors independently screened the titles and abstracts of the studies, excluding those that did not meet the inclusion criteria. Full texts of the remaining studies were reviewed for further screening. In case of disagreements, a third researcher (was consulted to resolve the discrepancies and reach a consensus.</p>
</sec>
<sec>
<title>Data extraction</title>
<p>The following information was collected from the included studies: First author, publication year, region, study design, sample size, predictive variables, model type, validation methods and model evaluation metrics. All data were independently extracted by two researchers and cross-checked for accuracy.</p>
</sec>
<sec>
<title>Assessment of literature quality</title>
<p>The risk of bias in the predictive models was assessed using the Prediction Model Risk Of Bias Assessment Tool (PROBAST) (<xref rid="b18-BR-23-6-02073" ref-type="bibr">18</xref>). A total of two authors independently conducted the evaluation and cross-validated the results; in case of discrepancies, a third author was consulted for final assessment. PROBAST is designed for evaluating the risk of bias and applicability of prediction model studies. It has been used in systematic reviews (<xref rid="b19-BR-23-6-02073" ref-type="bibr">19</xref>,<xref rid="b20-BR-23-6-02073" ref-type="bibr">20</xref>) and is suitable for the development, validation, and updating of diagnostic or prognostic prediction models (<xref rid="b21-BR-23-6-02073" ref-type="bibr">21</xref>). The core framework of PROBAST includes four primary domains and 20 items, aiming to systematically assess potential biases introduced during the research design, implementation and analysis phases to ensure the reliability and clinical applicability of the prediction models. The evaluation considers whether the outcome definitions align with clinical needs. If the outcome definitions in the domain match clinical concerns and provide valuable information for clinical decision-making, the applicability is classified as &#x2018;low risk&#x2019;. If the outcome definitions are disconnected from clinical needs and do not effectively guide clinical practice, the applicability is considered &#x2018;high risk&#x2019;. If the alignment of the outcome definitions with clinical needs is unclear, the applicability is rated as &#x2018;unclear&#x2019;.</p>
</sec>
<sec>
<title>Subgroup analyses</title>
<p>To explore potential sources of heterogeneity in the performance of ROP risk prediction models, predefined subgroup analyses were planned and conducted based on model type and geographic region.</p>
<p>For subgroup analysis by model type, studies were stratified into two distinct subgroups according to the modeling approaches employed. The first subgroup included studies utilizing traditional statistical models, with logistic regression being the primary method. The second subgroup comprised studies that adopted machine learning models, which encompassed various techniques such as neural networks, support vector machines, long short-term memory, and deep learning models.</p>
<p>For subgroup analysis by geographic region, studies were stratified into three regional subgroups based on the geographical locations of the study populations. The first subgroup included studies conducted in South America. The second subgroup consisted of studies performed in Asia. The third subgroup combined studies from North America and Europe, as these regions share similarities in healthcare systems and population characteristics, justifying their integration for comparative analysis.</p>
</sec>
<sec>
<title>Statistical analysis</title>
<p>Statistical analysis was performed using R version 4.4.2 (R Foundation for Statistical Computing, 2024; <ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="http://cran.r-project.org/bin/windows/base/old/4.4.2/">cran.r-project.org/bin/windows/base/old/4.4.2/</ext-link>), utilizing the &#x2018;meta (<ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="https://cran.r-project.org/package=meta">https://cran.r-project.org/package=meta</ext-link>)&#x2019; and &#x2018;metafor (<ext-link xmlns:xlink="http://www.w3.org/1999/xlink" ext-link-type="uri" xlink:href="https://cran.r-project.org/package=metafor">https://cran.r-project.org/package=metafor</ext-link>)&#x2019; packages to perform data pooling, heterogeneity testing, subgroup and sensitivity analyses and publication bias assessment. The AUC and its 95&#x0025; confidence intervals (CIs) were extracted from studies as the primary measure of predictive performance. Cochran&#x0027;s Q test and I&#x00B2; statistic were used to assess heterogeneity between studies. A random-effects model was used to pool the data, addressing the heterogeneity across studies. To assess potential publication bias, funnel plots were constructed. According to the Cochrane Handbook (<xref rid="b22-BR-23-6-02073" ref-type="bibr">22</xref>), when the number of included studies is &#x2265;10, publication bias risk assessment should not rely on Egger&#x0027;s or Begg&#x0027;s test. Instead, Peters&#x0027; test (<xref rid="b23-BR-23-6-02073" ref-type="bibr">23</xref>) was used to assess the symmetry of the funnel plot. Sensitivity analysis was performed using the Leave-One-Out method to evaluate the impact of each individual study on the overall pooled effect size. P&#x003C;0.05 was considered to indicate a statistically significant difference.</p>
</sec>
</sec>
</sec>
<sec sec-type="Results">
<title>Results</title>
<sec>
<title/>
<sec>
<title>Literature screening results</title>
<p>The present study conducted literature screening in accordance with the PRISMA 2020 guidelines (<xref rid="b24-BR-23-6-02073" ref-type="bibr">24</xref>). A total of 492 studies were retrieved through systematic searching; 163 duplicates were removed. Subsequently, seven meta-analyses, eight reviews, four studies including animal experiments and 64 conference records, guidelines and letters were excluded. Additionally, 105 studies that did not meet the inclusion criteria after title and abstract screening were excluded. Moreover, 20 studies for which full texts could not be obtained were excluded, along with eight studies without outcome indicators and 85 that only focused on risk factor research. Finally, a total of 28 studies were included (<xref rid="b25-BR-23-6-02073 b26-BR-23-6-02073 b27-BR-23-6-02073 b28-BR-23-6-02073 b29-BR-23-6-02073 b30-BR-23-6-02073 b31-BR-23-6-02073 b32-BR-23-6-02073 b33-BR-23-6-02073 b34-BR-23-6-02073 b35-BR-23-6-02073 b36-BR-23-6-02073 b37-BR-23-6-02073 b38-BR-23-6-02073 b39-BR-23-6-02073 b40-BR-23-6-02073 b41-BR-23-6-02073 b42-BR-23-6-02073 b43-BR-23-6-02073 b44-BR-23-6-02073 b45-BR-23-6-02073 b46-BR-23-6-02073 b47-BR-23-6-02073 b48-BR-23-6-02073 b49-BR-23-6-02073 b50-BR-23-6-02073 b51-BR-23-6-02073 b52-BR-23-6-02073" ref-type="bibr">25-52</xref>) (<xref rid="f1-BR-23-6-02073" ref-type="fig">Fig. 1</xref>).</p>
</sec>
<sec>
<title>Characteristics of the included studies</title>
<p>The studies were published between 2009 and 2025. A total of 14 studies (<xref rid="b32-BR-23-6-02073" ref-type="bibr">32</xref>,<xref rid="b34-BR-23-6-02073" ref-type="bibr">34</xref>,<xref rid="b36-BR-23-6-02073" ref-type="bibr">36</xref>,<xref rid="b40-BR-23-6-02073" ref-type="bibr">40</xref>,<xref rid="b41-BR-23-6-02073" ref-type="bibr">41</xref>,<xref rid="b45-BR-23-6-02073" ref-type="bibr">45</xref>,<xref rid="b47-BR-23-6-02073 b48-BR-23-6-02073 b49-BR-23-6-02073" ref-type="bibr">47-49</xref>,<xref rid="b51-BR-23-6-02073" ref-type="bibr">51</xref>,<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>) were conducted in East Asia, eight (<xref rid="b28-BR-23-6-02073" ref-type="bibr">28</xref>,<xref rid="b29-BR-23-6-02073" ref-type="bibr">29</xref>,<xref rid="b31-BR-23-6-02073" ref-type="bibr">31</xref>,<xref rid="b33-BR-23-6-02073" ref-type="bibr">33</xref>,<xref rid="b37-BR-23-6-02073" ref-type="bibr">37</xref>,<xref rid="b38-BR-23-6-02073" ref-type="bibr">38</xref>,<xref rid="b46-BR-23-6-02073" ref-type="bibr">46</xref>,<xref rid="b50-BR-23-6-02073" ref-type="bibr">50</xref>) in North America, two each in Europe (<xref rid="b30-BR-23-6-02073" ref-type="bibr">30</xref>,<xref rid="b39-BR-23-6-02073" ref-type="bibr">39</xref>) and South America (<xref rid="b25-BR-23-6-02073" ref-type="bibr">25</xref>,<xref rid="b26-BR-23-6-02073" ref-type="bibr">26</xref>), and one each in West (<xref rid="b31-BR-23-6-02073" ref-type="bibr">31</xref>) and Southeast Asia (<xref rid="b27-BR-23-6-02073" ref-type="bibr">27</xref>). A total of 11 studies (<xref rid="b28-BR-23-6-02073" ref-type="bibr">28</xref>,<xref rid="b30-BR-23-6-02073" ref-type="bibr">30</xref>,<xref rid="b33-BR-23-6-02073" ref-type="bibr">33</xref>,<xref rid="b36-BR-23-6-02073" ref-type="bibr">36</xref>,<xref rid="b38-BR-23-6-02073" ref-type="bibr">38</xref>,<xref rid="b40-BR-23-6-02073" ref-type="bibr">40</xref>,<xref rid="b41-BR-23-6-02073" ref-type="bibr">41</xref>,<xref rid="b46-BR-23-6-02073 b47-BR-23-6-02073 b48-BR-23-6-02073" ref-type="bibr">46-48</xref>,<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>) were multicenter studies. The sample size ranged from 90 to 22,569 cases, with an overall sample size of 72,991 cases (<xref rid="SD5-BR-23-6-02073" ref-type="supplementary-material">Table SV</xref>). A total of 28 items were included in the ROP risk prediction model (<xref rid="SD6-BR-23-6-02073" ref-type="supplementary-material">Table SVI</xref>).</p>
</sec>
<sec>
<title>Model validation</title>
<p>A total of 16 studies (<xref rid="b25-BR-23-6-02073 b26-BR-23-6-02073 b27-BR-23-6-02073" ref-type="bibr">25-27</xref>,<xref rid="b29-BR-23-6-02073" ref-type="bibr">29</xref>,<xref rid="b31-BR-23-6-02073 b32-BR-23-6-02073 b33-BR-23-6-02073 b34-BR-23-6-02073 b35-BR-23-6-02073" ref-type="bibr">31-35</xref>,<xref rid="b39-BR-23-6-02073" ref-type="bibr">39</xref>,<xref rid="b43-BR-23-6-02073" ref-type="bibr">43</xref>,<xref rid="b45-BR-23-6-02073" ref-type="bibr">45</xref>,<xref rid="b49-BR-23-6-02073 b50-BR-23-6-02073 b51-BR-23-6-02073" ref-type="bibr">49-51</xref>) did not mention the specific validation methods, five (<xref rid="b28-BR-23-6-02073" ref-type="bibr">28</xref>,<xref rid="b30-BR-23-6-02073" ref-type="bibr">30</xref>,<xref rid="b41-BR-23-6-02073" ref-type="bibr">41</xref>,<xref rid="b42-BR-23-6-02073" ref-type="bibr">42</xref>,<xref rid="b48-BR-23-6-02073" ref-type="bibr">48</xref>) conducted external validation, two (<xref rid="b40-BR-23-6-02073" ref-type="bibr">40</xref>,<xref rid="b47-BR-23-6-02073" ref-type="bibr">47</xref>) performed both internal and external validation and five (<xref rid="b36-BR-23-6-02073" ref-type="bibr">36</xref>,<xref rid="b38-BR-23-6-02073" ref-type="bibr">38</xref>,<xref rid="b44-BR-23-6-02073" ref-type="bibr">44</xref>,<xref rid="b46-BR-23-6-02073" ref-type="bibr">46</xref>,<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>) performed internal validation. This lack of rigorous validation limits the generalizability and clinical applicability of existing ROP risk prediction models.</p>
</sec>
<sec>
<title>Literature quality assessment</title>
<p>According to the PROBAST assessment tool, all the models have an unclear risk of bias (<xref rid="f2-BR-23-6-02073" ref-type="fig">Figs. 2</xref> and <xref rid="f3-BR-23-6-02073" ref-type="fig">3</xref>). This was primarily due to the susceptibility of retrospective studies to information bias, limited sample selection affecting representativeness, inconsistent variable definitions and measurement methods, insufficient control of confounding factors and small sample sizes that may lead to model instability. In the future model development process, more rigorous research designs and standardized variable measurement methods need to be adopted.</p>
</sec>
<sec>
<title>Meta-analysis of risk prediction models</title>
<p>Due to missing model evaluation data, only 22 studies (<xref rid="b25-BR-23-6-02073 b26-BR-23-6-02073 b27-BR-23-6-02073 b28-BR-23-6-02073 b29-BR-23-6-02073" ref-type="bibr">25-29</xref>,<xref rid="b32-BR-23-6-02073 b33-BR-23-6-02073 b34-BR-23-6-02073" ref-type="bibr">32-34</xref>,<xref rid="b36-BR-23-6-02073 b37-BR-23-6-02073 b38-BR-23-6-02073 b39-BR-23-6-02073 b40-BR-23-6-02073 b41-BR-23-6-02073 b42-BR-23-6-02073 b43-BR-23-6-02073 b44-BR-23-6-02073" ref-type="bibr">36-44</xref>,<xref rid="b47-BR-23-6-02073 b48-BR-23-6-02073 b49-BR-23-6-02073 b50-BR-23-6-02073 b51-BR-23-6-02073 b52-BR-23-6-02073" ref-type="bibr">47-52</xref>) were included in the analysis. The pooled effect size was AUC=0.87 (95&#x0025; CI: 0.34; 0.99), indicating good discriminative ability of the models. However, significant heterogeneity was observed among the studies (I&#x00B2;=99.2&#x0025;, P&#x003C;0.05; <xref rid="f4-BR-23-6-02073" ref-type="fig">Fig. 4</xref>).</p>
<p>Studies were stratified by modeling approach into subgroup A &#x005B;traditional statistical models (logistic regression&#x005D; (<xref rid="b25-BR-23-6-02073 b26-BR-23-6-02073 b27-BR-23-6-02073 b28-BR-23-6-02073 b29-BR-23-6-02073" ref-type="bibr">25-29</xref>,<xref rid="b32-BR-23-6-02073 b33-BR-23-6-02073 b34-BR-23-6-02073" ref-type="bibr">32-34</xref>,<xref rid="b37-BR-23-6-02073 b38-BR-23-6-02073 b39-BR-23-6-02073" ref-type="bibr">37-39</xref>,<xref rid="b41-BR-23-6-02073 b42-BR-23-6-02073 b43-BR-23-6-02073" ref-type="bibr">41-43</xref>,<xref rid="b45-BR-23-6-02073" ref-type="bibr">45</xref>,<xref rid="b47-BR-23-6-02073" ref-type="bibr">47</xref>,<xref rid="b50-BR-23-6-02073" ref-type="bibr">50</xref>,<xref rid="b51-BR-23-6-02073" ref-type="bibr">51</xref>) and B &#x005B;machine learning models (neural networks, support vector machines, long short-term memory, deep learning models&#x005D; (<xref rid="b36-BR-23-6-02073" ref-type="bibr">36</xref>,<xref rid="b40-BR-23-6-02073" ref-type="bibr">40</xref>,<xref rid="b48-BR-23-6-02073" ref-type="bibr">48</xref>,<xref rid="b49-BR-23-6-02073" ref-type="bibr">49</xref>,<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>). There was significant heterogeneity within both subgroups (P&#x003C;0.05), with I&#x00B2;=92.2&#x0025; in subgroup A and I&#x00B2;=97.3&#x0025; in subgroup B. These findings indicated that the differences between studies, whether using traditional statistical models or machine learning models were greater than what can be explained by random error, reflecting substantial methodological or study characteristic variations (<xref rid="f5-BR-23-6-02073" ref-type="fig">Fig. 5</xref>).</p>
<p>Subgroup analyses were also performed by study region. The South America subgroup (<xref rid="b25-BR-23-6-02073" ref-type="bibr">25</xref>,<xref rid="b26-BR-23-6-02073" ref-type="bibr">26</xref>) showed I&#x00B2;=0&#x0025; with P=0.898, indicating highly consistent results and no statistically significant heterogeneity. By contrast, the Asia (I&#x00B2;=96.6&#x0025;) (<xref rid="b27-BR-23-6-02073" ref-type="bibr">27</xref>,<xref rid="b32-BR-23-6-02073" ref-type="bibr">32</xref>,<xref rid="b36-BR-23-6-02073" ref-type="bibr">36</xref>,<xref rid="b40-BR-23-6-02073 b41-BR-23-6-02073 b42-BR-23-6-02073 b43-BR-23-6-02073" ref-type="bibr">40-43</xref>,<xref rid="b45-BR-23-6-02073" ref-type="bibr">45</xref>,<xref rid="b47-BR-23-6-02073 b48-BR-23-6-02073 b49-BR-23-6-02073" ref-type="bibr">47-49</xref>,<xref rid="b51-BR-23-6-02073" ref-type="bibr">51</xref>,<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>) and North America + Europe subgroup (I&#x00B2;=93.6&#x0025;) (<xref rid="b28-BR-23-6-02073" ref-type="bibr">28</xref>,<xref rid="b33-BR-23-6-02073" ref-type="bibr">33</xref>,<xref rid="b37-BR-23-6-02073 b38-BR-23-6-02073 b39-BR-23-6-02073" ref-type="bibr">37-39</xref>,<xref rid="b50-BR-23-6-02073" ref-type="bibr">50</xref>) both exhibited very high heterogeneity with P&#x003C;0.05, suggesting statistically significant differences in study results within these regional subgroups (<xref rid="f6-BR-23-6-02073" ref-type="fig">Fig. 6</xref>).</p>
<p>Based on the symmetry of the funnel plot around the pooled effect size (AUC=0.87), there was no obvious study bias (<xref rid="f7-BR-23-6-02073" ref-type="fig">Fig. 7</xref>). Peters&#x0027; bias test in showed t=-0.55, P=0.590, indicating no evidence of significant bias. This indicated that the findings of the included studies were not distorted by selective publication, and the overall evidence chain is highly reliable. From the results of bias assessments, the overall conclusions of the study are highly credible. The symmetry of the funnel plot and potential bias issues demonstrated minimal influence on the results. Sensitivity analysis showed that excluding any single study did not substantially alter the results, confirming stability (<xref rid="f8-BR-23-6-02073" ref-type="fig">Fig. 8</xref>).</p>
<p>Of the 28 studies, seven reported external validation; among these, three did not provide 95&#x0025; CI values for the external validation AUC. Pooling results from the remaining four studies (<xref rid="b40-BR-23-6-02073" ref-type="bibr">40</xref>,<xref rid="b41-BR-23-6-02073" ref-type="bibr">41</xref>,<xref rid="b47-BR-23-6-02073" ref-type="bibr">47</xref>,<xref rid="b50-BR-23-6-02073" ref-type="bibr">50</xref>) yielded an external validation AUC of 0.90 (0.76; 0.96; <xref rid="f9-BR-23-6-02073" ref-type="fig">Fig. 9</xref>). The symmetry of the funnel plot, non-significant Peters&#x0027; bias test and stable sensitivity analysis confirm that the overall findings are not distorted by publication bias and are robust to individual study exclusion, supporting the reliability of the meta-analysis conclusions.</p>
</sec>
</sec>
</sec>
<sec sec-type="Discussion">
<title>Discussion</title>
<p>Effective screening combined with timely intervention can notably decrease the blindness rate of ROP (<xref rid="b12-BR-23-6-02073" ref-type="bibr">12</xref>). Novel imaging technologies and internet connectivity have transformed the ROP screening model, with artificial intelligence-supported ROP screening becoming a research hotspot (<xref rid="b53-BR-23-6-02073" ref-type="bibr">53</xref>,<xref rid="b54-BR-23-6-02073" ref-type="bibr">54</xref>). However, existing predictive models have limitations and are not well-suited for areas with quality poor neonatal care (<xref rid="b55-BR-23-6-02073" ref-type="bibr">55</xref>,<xref rid="b56-BR-23-6-02073" ref-type="bibr">56</xref>). The present study conducted a meta-analysis to evaluate the performance of current ROP prediction models and improve ROP risk prediction models.</p>
<p>The present study included 28 ROP risk prediction models, among which six studies did not provide the 95&#x0025; CI values for the AUC. Pooling results from the remaining 22 studies, the AUC of ROP prediction models was 0.87 (0.34; 0.99), indicating that the overall performance of ROP risk prediction models is favorable, with good discriminative ability. However, there was high heterogeneity between the models. When the models were sub-grouped into traditional statistical and machine learning models, high heterogeneity remained within each subgroup. The causes of heterogeneity were considered to be differences in covariate selection, sample characteristics and outcome definitions and a lack of unified standards for data preprocessing and validation protocols. Regional subgroup analysis showed that studies from South America had no significant heterogeneity, while those from Asia, North America and Europe exhibited high heterogeneity. It was hypothesized that studies in South America showed consistent results due to the uniformity of population characteristics and medical standards within the region; by contrast, the high heterogeneity in Asia, North America and Europe may be attributed to notable differences in cross-regional population characteristics and medical systems. Nevertheless, funnel plot symmetry and Peters&#x0027; bias test indicated no significant publication bias, and sensitivity analysis showed stable results, supporting the reliability of the conclusions. Future studies should reduce heterogeneity by unifying methodological standards and conducting multicenter research.</p>
<p>The risk of bias for all the models was unclear. Badriah <italic>et al</italic> (<xref rid="b27-BR-23-6-02073" ref-type="bibr">27</xref>) and Park <italic>et al</italic> (<xref rid="b32-BR-23-6-02073" ref-type="bibr">32</xref>) adopted retrospective designs, relying on medical record reviews for data collection. This may introduce information bias due to incomplete record-keeping or subjective data assignment. The study by Park <italic>et al</italic> (<xref rid="b32-BR-23-6-02073" ref-type="bibr">32</xref>) was a single-center study, with sample selection limited to a specific medical setting, which may decrease the generalizability of the results.</p>
<p>In terms of variable measurement, there were differences in the definitions and measurement methods of key predictors across studies. Filho <italic>et al</italic> (<xref rid="b25-BR-23-6-02073" ref-type="bibr">25</xref>) used &#x2018;weight gain proportion at 6 weeks after birth&#x2019; as an indicator, while Cerda <italic>et al</italic> (<xref rid="b31-BR-23-6-02073" ref-type="bibr">31</xref>) employed changes in z-scores based on the Fenton growth curve. Such inconsistent standards limited data comparability. While most studies (<xref rid="b25-BR-23-6-02073 b26-BR-23-6-02073 b27-BR-23-6-02073 b28-BR-23-6-02073 b29-BR-23-6-02073 b30-BR-23-6-02073 b31-BR-23-6-02073 b32-BR-23-6-02073 b33-BR-23-6-02073 b34-BR-23-6-02073 b35-BR-23-6-02073 b36-BR-23-6-02073 b37-BR-23-6-02073 b38-BR-23-6-02073 b39-BR-23-6-02073 b40-BR-23-6-02073 b41-BR-23-6-02073 b42-BR-23-6-02073 b43-BR-23-6-02073 b44-BR-23-6-02073 b45-BR-23-6-02073 b46-BR-23-6-02073 b47-BR-23-6-02073 b48-BR-23-6-02073 b49-BR-23-6-02073 b50-BR-23-6-02073 b51-BR-23-6-02073 b52-BR-23-6-02073" ref-type="bibr">25-52</xref>) referenced international classification criteria, Blue <italic>et al</italic> (<xref rid="b38-BR-23-6-02073" ref-type="bibr">38</xref>) and Chen <italic>et al</italic> (<xref rid="b44-BR-23-6-02073" ref-type="bibr">44</xref>) did not explicitly mention international ROP severity assessment criteria in their relevant evaluations. In addition, Filho <italic>et al</italic> (<xref rid="b26-BR-23-6-02073" ref-type="bibr">26</xref>) and Gerull <italic>et al</italic> (<xref rid="b30-BR-23-6-02073" ref-type="bibr">30</xref>) did not explicitly describe the implementation of assessor blinding, which may introduce subjective bias, however, the core staging criteria remained consistent.</p>
<p>The multicenter study by Ying <italic>et al</italic> (<xref rid="b33-BR-23-6-02073" ref-type="bibr">33</xref>) covered 29 hospitals in North America. Differences in medical care practices between institutions may have interfered with the identification of ROP risk factors, but the study adjusted for key variables such as gestational age and birth weight through multivariate regression, decreasing confounding effects to a certain extent. Park <italic>et al</italic> (<xref rid="b32-BR-23-6-02073" ref-type="bibr">32</xref>), Hari <italic>et al</italic> (<xref rid="b50-BR-23-6-02073" ref-type="bibr">50</xref>), and Shi <italic>et al</italic> (<xref rid="b51-BR-23-6-02073" ref-type="bibr">51</xref>) had relatively small sample sizes, which may pose a risk of model instability. However, owing to the explicit and rigorous definition of outcome events, the risk of overfitting (where a model or analytical approach exhibits excessive adaptation to the original dataset while lacking generalizability to new data-was kept at a controllable level. While specific biases were present across multiple dimensions of the study, they did not substantially compromise the overall validity of the findings. Consequently, the overall risk of bias was evaluated as unclear, indicating that although biases exist, they are not severe enough to invalidate the core conclusions of the study.</p>
<p>In predictor selection, the included studies did not report the effectiveness of predictors in practical applications or clearly specify whether the predictive ability of predictors was independently evaluated under blinded conditions. In addition, there were notable differences in terms of predictor selection and their determination methods. Some studies (<xref rid="b45-BR-23-6-02073" ref-type="bibr">45</xref>,<xref rid="b46-BR-23-6-02073" ref-type="bibr">46</xref>) failed to fully consider potential interactions between predictors. Multiple included studies consistently identified oxygen therapy as a key risk factor for ROP; however, the studies did not conduct in-depth exploration of interaction effects between factors such as different oxygen therapy modalities and fluctuations in oxygen concentration. Kubota <italic>et al</italic> (<xref rid="b45-BR-23-6-02073" ref-type="bibr">45</xref>) focused on analyzing the association between oxygen saturation (SpO<sub>2</sub>) fluctuations and ROP risk by calculating the total difference in SpO<sub>2</sub> values over the total effective time. On the other hand, Lin <italic>et al</italic> (<xref rid="b46-BR-23-6-02073" ref-type="bibr">46</xref>) mainly focused on relevant indicators of fraction of inspired oxygen (FiO<sub>2</sub>), including the average FiO<sub>2</sub> and the coefficient of variation of FiO<sub>2</sub>, aggregating daily data to smooth short-term fluctuations and decrease noise. Unlike other studies (<xref rid="b26-BR-23-6-02073" ref-type="bibr">26</xref>,<xref rid="b27-BR-23-6-02073" ref-type="bibr">27</xref>,<xref rid="b30-BR-23-6-02073" ref-type="bibr">30</xref>,<xref rid="b37-BR-23-6-02073" ref-type="bibr">37</xref>,<xref rid="b40-BR-23-6-02073" ref-type="bibr">40</xref>,<xref rid="b50-BR-23-6-02073" ref-type="bibr">50</xref>) that may focus only on oxygen concentration or oxygen duration at a fixed point in time, this previous study emphasized the impact of the trend in FiO<sub>2</sub> changes over time on ROP. In practical applications, there may be differences in the frequency and method of FiO<sub>2</sub> monitoring and recording between different medical institutions.</p>
<p>Future studies should adopt prospective designs and increase sample sizes. This would allow for more precise control of influencing factors during data collection, enable tracking and observation of changes in the target population, provide more representative study samples, and avoid information and selection biases inherent in retrospective studies. Regularization methods should be used to limit model degrees of freedom and prevent overfitting. When constructing prediction models, potential confounding factors should be controlled.</p>
<p>Of 28 studies, 16 did not mention model validation, while five conducted internal validation. The internal validation sample sizes in the studies by Lin <italic>et al</italic> (<xref rid="b46-BR-23-6-02073" ref-type="bibr">46</xref>) and Takeda <italic>et al</italic> (<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>) were relatively small, which may not fully capture the various characteristics and associations in the data. While the models performed well on the training sets, they may not perform as well in real-world applications. In the study by Chen <italic>et al</italic> (<xref rid="b44-BR-23-6-02073" ref-type="bibr">44</xref>), five-fold cross-validation was performed on data from 22,569 patients, improving the training effect of the model and enhancing its stability and reliability. However, the occurrence and development of ROP may be influenced by factors such as medical conditions and environmental factors in different regions. Therefore, it is essential to include data from different regions and medical centers for external validation to ensure the general applicability of the model. The present study combined the external validation results from four studies (<xref rid="b40-BR-23-6-02073" ref-type="bibr">40</xref>,<xref rid="b41-BR-23-6-02073" ref-type="bibr">41</xref>,<xref rid="b47-BR-23-6-02073" ref-type="bibr">47</xref>,<xref rid="b48-BR-23-6-02073" ref-type="bibr">48</xref>) with an external validation model AUC of 0.90 (0.76; 0.96), showing good external validation performance. However, in clinical applications, the practical value of the model should be verified by incorporating other evaluation indicators.</p>
<p>Additionally, in the statistical analysis, certain studies (<xref rid="b25-BR-23-6-02073" ref-type="bibr">25</xref>,<xref rid="b26-BR-23-6-02073" ref-type="bibr">26</xref>) had issues with improper handling of missing data and insufficient assessment of collinearity. In the study by Takeda <italic>et al</italic> (<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>), five machine learning methods (decision trees, random forests, gradient boosting trees, neural networks and naive Bayes) were used to construct the models. Random forests and naive Bayes models performed well. Non-imaging machine learning models demonstrated high performance in predicting ROP occurrence, providing a feasible predictive approach for hospitals that lack access to retinal images or pediatric retinal cameras. However, this previous study acknowledged the small sample size and issues with variable collinearity. In the future, combining LASSO regression with embedded feature selection techniques may help control for collinearity between variables, select a stable and effective set of features and improve the robustness of the models.</p>
<p>Of 28 studies, 24 reported (<xref rid="b25-BR-23-6-02073 b26-BR-23-6-02073 b27-BR-23-6-02073" ref-type="bibr">25-27</xref>,<xref rid="b29-BR-23-6-02073 b30-BR-23-6-02073 b31-BR-23-6-02073 b32-BR-23-6-02073 b33-BR-23-6-02073 b34-BR-23-6-02073 b35-BR-23-6-02073" ref-type="bibr">29-35</xref>,<xref rid="b37-BR-23-6-02073" ref-type="bibr">37</xref>,<xref rid="b39-BR-23-6-02073" ref-type="bibr">39</xref>,<xref rid="b40-BR-23-6-02073 b41-BR-23-6-02073 b42-BR-23-6-02073 b43-BR-23-6-02073 b44-BR-23-6-02073 b45-BR-23-6-02073 b46-BR-23-6-02073 b47-BR-23-6-02073 b48-BR-23-6-02073" ref-type="bibr">40-48</xref>,<xref rid="b50-BR-23-6-02073 b51-BR-23-6-02073 b52-BR-23-6-02073" ref-type="bibr">50-52</xref>) that low birth weight in preterm infants is a risk factor for the occurrence of ROP. Yildirim <italic>et al</italic> (<xref rid="b57-BR-23-6-02073" ref-type="bibr">57</xref>) found that, compared with preterm infants without ROP, the average weight gain in the third week after birth was significantly lower in infants with ROP; Preterm infants with low birth weight have underdeveloped retinal vascular systems, and their blood vessels are structurally and functionally fragile, making it difficult to cope with abnormal vascular proliferation, fibrosis and other pathological changes, thereby increasing the risk of ROP (<xref rid="b58-BR-23-6-02073" ref-type="bibr">58</xref>).</p>
<p>Additionally, eight studies (<xref rid="b33-BR-23-6-02073" ref-type="bibr">33</xref>,<xref rid="b34-BR-23-6-02073" ref-type="bibr">34</xref>,<xref rid="b37-BR-23-6-02073" ref-type="bibr">37</xref>,<xref rid="b42-BR-23-6-02073" ref-type="bibr">42</xref>,<xref rid="b47-BR-23-6-02073" ref-type="bibr">47</xref>,<xref rid="b48-BR-23-6-02073" ref-type="bibr">48</xref>,<xref rid="b49-BR-23-6-02073" ref-type="bibr">49</xref>,<xref rid="b52-BR-23-6-02073" ref-type="bibr">52</xref>) used the Apgar score to establish prediction models. The Apgar score primarily evaluates neonatal health status based on heart rate, respiration, muscle tone, reflexes and skin color. A low Apgar score often indicates that the newborn experienced asphyxia or hypoxia at birth, which affects the normal development of the retinal blood vessels and increases the risk of ROP (<xref rid="b59-BR-23-6-02073" ref-type="bibr">59</xref>).</p>
<p>Multiple pregnancies are also a risk factor for ROP. In multiple pregnancies, the blood supply from the placenta is distributed unevenly, leading to insufficient fetal nutrition, and restricted growth and development, which often results in low birth weight (<xref rid="b60-BR-23-6-02073" ref-type="bibr">60</xref>)</p>
<p>Furthermore, studies (<xref rid="b23-BR-23-6-02073" ref-type="bibr">23</xref>,<xref rid="b27-BR-23-6-02073" ref-type="bibr">27</xref>) have shown that Caucasian infants have a higher risk of developing ROP compared with other ethnicities. This is because Caucasian individuals have less pigmentation, making the retinas more sensitive to oxygen and light damage. Under oxygen therapy or high-oxygen exposure conditions, the retina is more prone to vascular development disorders (<xref rid="b61-BR-23-6-02073" ref-type="bibr">61</xref>). However, a 2006-2017 study (<xref rid="b62-BR-23-6-02073" ref-type="bibr">62</xref>) of 41 North American hospitals found African-American infants had lower birth weight and gestational ages than white and Asian infants; African-American and Asian infants had significantly lower daily weight gain than Caucasian infants 31-40 days after birth and after adjusting for birth weight and gestational age, African-American infants had a lower incidence of severe ROP than Caucasian and Asian infants. There were no differences in the incidence or timing of severe ROP between different ethnicities; this mechanism requires further exploration.</p>
<p>Although the aforementioned factors have been confirmed to be associated with ROP in most studies, certain research (<xref rid="b27-BR-23-6-02073" ref-type="bibr">27</xref>,<xref rid="b32-BR-23-6-02073" ref-type="bibr">32</xref>,<xref rid="b34-BR-23-6-02073" ref-type="bibr">34</xref>,<xref rid="b42-BR-23-6-02073" ref-type="bibr">42</xref>,<xref rid="b43-BR-23-6-02073" ref-type="bibr">43</xref>,<xref rid="b46-BR-23-6-02073" ref-type="bibr">46</xref>,<xref rid="b49-BR-23-6-02073" ref-type="bibr">49</xref>,<xref rid="b50-BR-23-6-02073 b51-BR-23-6-02073 b52-BR-23-6-02073" ref-type="bibr">50-52</xref>) still has the limitation of having a relatively small sample size. Additionally, there are notable differences in medical standards, preterm infant care and environmental factors across regions, and the level of care provided to infants, including nutritional support and oxygen therapy management, varies (<xref rid="b27-BR-23-6-02073" ref-type="bibr">27</xref>,<xref rid="b33-BR-23-6-02073" ref-type="bibr">33</xref>,<xref rid="b35-BR-23-6-02073" ref-type="bibr">35</xref>).</p>
<p>It is recommended that pregnant patients at risk of preterm birth receive prenatal corticosteroids: these medications accelerate fetal lung maturation, reducing the incidence and severity of respiratory distress syndrome in preterm infants (<xref rid="b63-BR-23-6-02073" ref-type="bibr">63</xref>). Additionally, unnecessary postnatal ventilation and oxygen therapy for neonates should be avoided, as excessive oxygen exposure directly disrupts retinal vascular development. Neonates should also receive high-quality care and providing targeted management of comorbidities like bronchopulmonary dysplasia.</p>
<p>The present study had certain limitations: the systematic review was not pre-registered on the PROSPERO platform, which decreases the traceability of the research design and implementation process, and may affect methodological transparency and the validation of the standardization of the research protocol.</p>
<p>Future studies should consider combining fundus images with clinical data and use deep learning methods such as convolutional and recurrent neural networks, or ensemble learning algorithms such as random forest, gradient boosting machine and XGBoost to construct ROP prediction models (<xref rid="b58-BR-23-6-02073" ref-type="bibr">58</xref>,<xref rid="b64-BR-23-6-02073" ref-type="bibr">64</xref>). Such an approach could potentially handle large volumes of complex non-linear relationships and enable automated feature extraction, which might provide a more accurate basis for early screening-though this remains to be validated in future research.</p>
<p>In summary, existing ROP prediction models have potential in discriminative ability and may provide references for preliminary clinical screening. However, their application is limited by insufficient external validation and inadequate sample representativeness, and their generalization ability needs to be improved. Future model development should prioritize multicenter, large-sample prospective designs, control confounding factors, and systematically incorporate data from populations with different medical resource backgrounds and ethnic groups to enhance the generalizability of results. Meanwhile, it is necessary to strengthen external validation processes, explore multimodal fusion of fundus images and clinical indicators, introduce deep learning or ensemble learning methods to handle complex data associations and explore potential biomarkers associated with ROP, thereby providing more reliable tools for early accurate screening and intervention for neonatal ROP.</p>
</sec>
<sec sec-type="supplementary-material">
<title>Supplementary Material</title>
<supplementary-material id="SD1-BR-23-6-02073" content-type="local-data">
<caption>
<title>PubMed database search strategy.</title>
</caption>
<media mimetype="application" mime-subtype="pdf" xlink:href="Supplementary_Data.pdf"/>
</supplementary-material>
<supplementary-material id="SD2-BR-23-6-02073" content-type="local-data">
<caption>
<title>Web of Science database search strategy.</title>
</caption>
<media mimetype="application" mime-subtype="pdf" xlink:href="Supplementary_Data.pdf"/>
</supplementary-material>
<supplementary-material id="SD3-BR-23-6-02073" content-type="local-data">
<caption>
<title>Embase database search strategy.</title>
</caption>
<media mimetype="application" mime-subtype="pdf" xlink:href="Supplementary_Data.pdf"/>
</supplementary-material>
<supplementary-material id="SD4-BR-23-6-02073" content-type="local-data">
<caption>
<title>Cochrane Library database search strategy.</title>
</caption>
<media mimetype="application" mime-subtype="pdf" xlink:href="Supplementary_Data.pdf"/>
</supplementary-material>
<supplementary-material id="SD5-BR-23-6-02073" content-type="local-data">
<caption>
<title>Study characteristics.</title>
</caption>
<media mimetype="application" mime-subtype="pdf" xlink:href="Supplementary_Data.pdf"/>
</supplementary-material>
<supplementary-material id="SD6-BR-23-6-02073" content-type="local-data">
<caption>
<title>Prediction model characteristics.</title>
</caption>
<media mimetype="application" mime-subtype="pdf" xlink:href="Supplementary_Data.pdf"/>
</supplementary-material>
</sec>
</body>
<back>
<ack>
<title>Acknowledgements</title>
<p>Not applicable.</p>
</ack>
<sec sec-type="data-availability">
<title>Availability of data and materials</title>
<p>The data generated in the present study may be requested from the corresponding author.</p>
</sec>
<sec>
<title>Authors&#x0027; contributions</title>
<p>LL and YG confirm the authenticity of all the raw data. LL and YG designed and performed the experiments and wrote the manuscript. WC interpreted data. MH conceived the study. All authors have read and approved the final manuscript.</p>
</sec>
<sec>
<title>Ethics approval and consent to participate</title>
<p>Not applicable.</p>
</sec>
<sec>
<title>Patient consent for publication</title>
<p>Not applicable.</p>
</sec>
<sec sec-type="COI-statement">
<title>Competing interests</title>
<p>The authors declare that they have no competing interests.</p>
</sec>
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<floats-group>
<fig id="f1-BR-23-6-02073" position="float">
<label>Figure 1</label>
<caption><p>Flowchart of literature screening. Initial retrieval from PubMed, Cochrane Library, Web of Science and Embase yielded 492 records. After removing 163 duplicates, 329 records remained. Following the exclusion of 83 ineligible records (meta-analyses, reviews, animal studies, conference abstracts), 246 full texts were assessed. Further exclusions (n=218) included studies without prediction models. Ultimately, 28 studies were included, encompassing 28 retinopathy of prematurity risk prediction models with a total sample size of 72,991 infants.</p></caption>
<graphic xlink:href="br-23-06-02073-g00.tif"/>
</fig>
<fig id="f2-BR-23-6-02073" position="float">
<label>Figure 2</label>
<caption><p>Publication bias of the included studies.</p></caption>
<graphic xlink:href="br-23-06-02073-g01.tif"/>
</fig>
<fig id="f3-BR-23-6-02073" position="float">
<label>Figure 3</label>
<caption><p>Specific assessment results of PROBAST. Risk of bias evaluation for 28 included studies using the PROBAST tool. Each study was assessed across 20 items in four domains (participants, predictors, outcomes, analysis), with an overall unclear risk of bias. PROBAST, Prediction Model Risk Of Bias Assessment Tool.</p></caption>
<graphic xlink:href="br-23-06-02073-g02.tif"/>
</fig>
<fig id="f4-BR-23-6-02073" position="float">
<label>Figure 4</label>
<caption><p>Forest plot of retinopathy of prematurity risk prediction model for premature infants. Individual and pooled (0.87, 95&#x0025; CI: 0.34; 0.99) AUC values with 95&#x0025; CIs for 22 risk prediction models. Heterogeneity is marked by I&#x00B2;=99.2&#x0025; (P&#x003C;0.05). AUC, area under the receiver operating characteristic curve; CI, confidence interval.</p></caption>
<graphic xlink:href="br-23-06-02073-g03.tif"/>
</fig>
<fig id="f5-BR-23-6-02073" position="float">
<label>Figure 5</label>
<caption><p>Subgroup analysis of types of retinopathy of prematurity risk prediction model for premature infants. (A) Traditional statistical (n=17) and (B) machine learning models (n=5). Each subgroup includes individual study AUCs with 95&#x0025; CIs and pooled effect sizes, with I&#x00B2; values of 92.2 and 97.3&#x0025; respectively. AUC, area under the receiver operating characteristic curve; CI, confidence interval.</p></caption>
<graphic xlink:href="br-23-06-02073-g04.tif"/>
</fig>
<fig id="f6-BR-23-6-02073" position="float">
<label>Figure 6</label>
<caption><p>Regional subgroup analysis of retinopathy of prematurity risk in preterm infants. Forest plots of the subgroup meta-analyses of 22 models by geographic region: South America (n=2), Asia (n=15) and North America + Europe (n=6). Each region includes individual study AUCs with 95&#x0025; CIs and pooled effect sizes, with I&#x00B2; values of 0.0, 96.6 and 93.6&#x0025;, respectively. AUC, area under the receiver operating characteristic curve; CI, confidence interval.</p></caption>
<graphic xlink:href="br-23-06-02073-g05.tif"/>
</fig>
<fig id="f7-BR-23-6-02073" position="float">
<label>Figure 7</label>
<caption><p>Funnel plot of the retinopathy of prematurity risk prediction model for premature infants. Distribution of 22 studies, with each point representing AUC and precision (1/standard error). The vertical line indicates the pooled AUC (0.87). AUC, area under the receiver operating characteristic curve.</p></caption>
<graphic xlink:href="br-23-06-02073-g06.tif"/>
</fig>
<fig id="f8-BR-23-6-02073" position="float">
<label>Figure 8</label>
<caption><p>Sensitivity analysis of the combined retinopathy of prematurity risk prediction model for premature infants. Pooled area under the receiver operating characteristic curve after iteratively excluding each study is shown.</p></caption>
<graphic xlink:href="br-23-06-02073-g07.tif"/>
</fig>
<fig id="f9-BR-23-6-02073" position="float">
<label>Figure 9</label>
<caption><p>Forest plot of the external validation of four retinopathy of prematurity risk prediction models for premature infants. The diamond indicates the pooled external validation area under the receiver operating characteristic curve (0.90, 95&#x0025; CI: 0.76; 0.96). CI, confidence interval.</p></caption>
<graphic xlink:href="br-23-06-02073-g08.tif"/>
</fig>
</floats-group>
</article>
