A prototype variable corresponding to the proportion of ischemia for the comparison between robotic and open partial nephrectomy: a meta-analysis accompanied by sensitivity analysis

The primary objective of this study involves the formulation of a novel variable, derived from initial data related to ischemia duration and operative time in partial nephrectomies. The aim was to determine the proportion of ischemia for the comparison between robotic and open approaches in terms of their relative ischemic requirements. The literature search was conducted from August 2022 to June 2023, primarily encompassing non-randomized comparative studies in the English language. Ultimately, a total of 62 studies involving data from 26,072 patients were included. Following appropriate transformation of the original data under the assumption of normal distribution, the proportion of ischemia (I) was formulated for each study and comparison arm, using estimator functions. Subsequent analysis of the generated data was performed for both the original variables and the I outcome. Statistical significance was only observed regarding the surgical duration, with a mean difference of 19.74 min (CI95% = [11.56; 27.92]) in favor of robotic access. The mean difference in I was estimated on the entire dataset as well as carefully selected subgroups based on publication year, patient matching, the number of referral centers, and risk of bias class. Additionally, meta-regression analysis and four-level sensitivity analysis were conducted. In none of these investigations did statistically significant differences emerge between the two surgical approaches. These findings lead us to hypothesize that the proportion of ischemia in partial nephrectomies may represent an inherent characteristic of the procedure, typically manifesting as baseline ischemia (12–13% of operative time), with fluctuations depending on the chosen strategy or the complexity of the specific intervention. There is no difference in the proportion of ischemia between robotic and open partial nephrectomies. In overall, ischemia time appears to be primarily determined by the overall duration of the procedure and the effectiveness in achieving adequate hemostasis.


Background
Partial nephrectomy (PN) represents a nephron-sparing surgery (NSS) technique for the treatment of localized kidney tumors, primarily aiming at kidney function preservation compared to radical nephrectomy (RN) [1].Various approaches, including open (OPN), laparoscopic (LPN), and robot-assisted partial nephrectomy (RAPN), are utilized.In particular, RAPN offers comparable perioperative outcomes to LPN but with improved precision in tumor excision.The R.E.N.A.L. nephrometry score is used to categorize kidney masses based on size, location, and depth, although there is limited data for highly complex tumors [1].Guidelines from the American Urological Association (AUA) recommend PN for localized T1a-b renal tumors, and there has been an increased utilization of NSS in recent years, mainly due to the rise in robotic technology availability [2].Ongoing research is exploring outcomes for robotic, open, and laparoscopic PN [2].NSS is commonly employed for renal masses, with OPN preferred in cases involving a solitary kidney due to its field visualization and access advantages.RPN is gaining popularity and has demonstrated safety and effectiveness, even for complex tumors in solitary kidneys [3].Renal cell carcinoma (RCC) is a life-threatening condition, and NSS is the currently most preferred approach.OPN has traditionally been the standard approach for treating RCC.However, the adoption of minimally invasive techniques like LPN has been limited due to the complexity of the procedure.In contrast, RAPN has emerged as a viable alternative, offering improved surgical capabilities and ergonomic benefits [4].Several studies have shown that RAPN provides superior surgical precision compared to OPN and LPN, but the varied methodologies and outcome measures used, unavoidably limit broader conclusions [5][6][7].
In this study, our objective was to compare RAPN and OPN in terms of surgical precision, specifically in the context of intraoperative applied ischemia.The international literature consistently highlights the detrimental effects of prolonged ischemia on postoperative kidney function recovery [8].Conversely, ischemia is crucial to achieve adequate hemostasis and optimize the visualization of the surgical field, ultimately enhancing the precision of surgical maneuvers [9].The contribution of minimally invasive techniques to prolonging ischemia duration in PN compared to open surgery has been frequently discussed, although this position does not universally represent the body of relevant literature.Given the conflicting impact of ischemia duration on renal function and surgical precision, we considered the proportion of ischemia, defined as the ratio of ischemia time (IT) to operative time (OT), as a parameter that could provide a more objective basis for comparing the two surgical approaches in terms of their relative demands for intraoperative ischemia.Consequently, we conducted a meta-analysis using available data from the literature to obtain an overall estimation of the comparative effect within the maximum feasible set of studies.

Main concept
We've previously elucidated the relationship between ischemia time (IT), renal function preservation, and hemostasis.In our analysis, we considered the impact of IT normalized to the procedure's total duration.We argue that the proportion of ischemia better reflects surgical precision, supported by international literature showing that RAPN typically has a longer operative time (OT) compared to OPN [10,11].Assuming IT and OT are collinear, indicating a non-zero correlation coefficient, we chose to compare RAPN and OPN precision using the ratio of these variables, denoted as "I".The newly introduced outcome, expressed as a dimensionless measure, essentially signifies the proportion of ischemia, effectively indicating the ischemic requirements associated with each approach.More specifically, it was considered to have a negative impact on surgical precision, aligning with literature advocating for improved postoperative outcomes by minimizing ischemia duration within a specified procedure timeframe [12].In summary, our hypothesis proposes that when comparing RAPN and OPN, greater surgical precision can be offered by the approach that minimizes I.

Literature search and study selection
Between August 2022 and June 2023, a comprehensive literature search was conducted to identify relevant studies comparing RPN or RAPN with OPN based on their titles.Inclusion in the analysis was contingent upon the availability of simultaneous comparative data for the original variables: IT (ischemia time) and OT (operative time).These variables were combined as a quotient to derive the proportion of intraoperatively applied ischemia, the primary outcome of interest.The literature search encompassed multiple databases, including "Medline," "Scopus," "ScienceDirect," "CENTRAL," and "Google Scholar".Monthly alerts were set within these databases throughout the search period to ensure adequate coverage.The study protocol was meticulously formulated in advance and is accessible on the Prospero website (https:// www.crd.york.ac.uk/ prosp ero) [13], identified as CRD42022354959.In accordance with the original study protocol, two distinct interventions were implemented.Firstly, the protocol's title was succinctly condensed.And secondly, the investigation was expanded to encompass a broader range of databases to conduct a more thorough examination of the available literature.
The preselected search strategy (SS) played a pivotal role in determining the study selection criteria.The original SS can be accessed online at the following URL: https:// www.crd.york.ac.uk/ PROSP EROFI LES/ 354959_ STRAT EGY_ 20220 821.pdf.In summary, this SS utilized keywords such as "robotic", "robot-assisted", "open", and "partial nephrectomy" in various combinations.To manage the extensive amount of data generated during the initial exploration of potential studies for the RPN/RAPN versus OPN comparison, these filters were applied exclusively to study titles.After applying the SS sequentially to each database, distinct sets of studies were identified and imported into the Sysrev electronic platform (https:// sysrev.com) [14] in ".ris" format.The inclusion criteria were then applied, focusing on studies conducted exclusively in English, non-duplicated studies with accessible fulltext, and comparative studies providing sufficient data for both arms of the comparison, enabling the calculation of "ischemia minutes per operative minute".Noncomparative studies, those lacking statistically assessable data, or studies reporting findings solely for one arm of the comparison were excluded.The application of these inclusion criteria to individual studies primarily occurred within the Sysrev online platform.The entire project is accessible online at the URL: https:// sysrev.com/p/ 119881.Furthermore, an additional criterion was introduced post-initial evaluation, focusing on the exclusion of studies based on the outcome of interest.Within the Sysrev platform, each study underwent an initial assessment considering a set of binary qualitative variables, followed by the assignment of specific labels according to its field of interest.A PRISMA flowchart illustrating the processes of study exclusion or inclusion is available in the Sect.3.

Evidence acquisition and quality assessment
The classification of studies obtained from the databases commenced within the Sysrev environment.This classification process involved three levels.Initially, studies were assessed using basic binary parameters based on their methodological profile, and they were then labeled according to their specific field of interest.At the third level, a list of variables was compiled for each study, focusing on relevant statistical data needed for comparative purposes between RAPN and OPN.A member of the authoring team ([SA]), oversaw this three-level process, which included study classification, labeling, and outcome identification.Subsequently, two reviewers ([DA] and [IK]) tabulated studies that met the eligibility criteria, creating the corresponding file in ".csv" format.It's important to note that missing data affected a total of 1093 patients, with 472 in the experimental arm (RPN/ RAPN) and 621 in the control arm (OPN).Addressing these missing data was crucial in constructing the patient populations for comparison in each case.
Following data acquisition, the extraction of the necessary statistical parameters for each variable under comparison was conducted manually, without the use of automation tools.Alongside numerical data, metadata related to specific study features were also recorded.These included the study's author, publication year, patient matching implementation, number of referral centers involved, study duration, risk of bias, confounding issues, and other pertinent information.Upon completion of data and metadata tabulation from each individual study, three reviewers ([DA], [IK], and [KT]) performed an overall evaluation and applied two qualitative classification scales.Firstly, the Newcastle-Ottawa Scale (NOS) was employed for an overview grading, followed by the more detailed ROBINS-I tool for nonrandomized comparative studies [15,16].This dual-scale approach was chosen for two primary reasons.Firstly, it allowed for the comprehensive assessment of different critical aspects since each scale addresses distinct factors.And secondly, it aimed to achieve a thorough evaluation of the study quality while minimizing the risk of underestimating bias.

Outcomes
The primary aim of this study was to estimate the proportion of ischemia (I), a measure derived through statistical estimations, as explained below.Additionally, the analysis involved two secondary outcomes: ischemia time (IT) and operative time (OT), both measured in minutes (min).These parameters are well-documented in the international literature, particularly in the context of RAPN versus OPN comparison.To achieve these objectives, a substantial number of studies meeting the inclusion criteria were collected, allowing for the exploration of inherent differences between RAPN and OPN within a diverse patient population.Given the extensive volume of data and adherence to the predefined study protocol, no additional variables beyond the mentioned ones were pursued.However, a comprehensive examination of potential deviations in comparability among integrated studies was conducted, with a specific focus on statistically significant differences in baseline characteristics between patient groups being compared.These variations are succinctly presented in the relevant table of included studies, available in the Sect.3.

Statistical analysis
The estimation of the ischemia proportion (I) followed a standardized stepwise process, utilizing the expected value (EV) and standard error (SE) of the original outcomes.The analysis assumed a normal distribution and relied on summary statistics from the IT and OT variables.Each included study and arm under comparison (RPN/RAPN and OPN) were considered in the estimation process, accounting for missing data to form the respective patient populations.The statistical parameters EV and SE of I were derived using estimator functions ( 1) and ( 2), as previously reported by van Kempen and van Vliet in their computational analysis of fluoroscopy data [17].These functions were implemented with the assumption that each study provided a single sample (n = 1) for each arm under comparison, and all calculations were performed accordingly.To facilitate computation, the original variables (IT and OT) needed to be presented in the format "EV-SE," with units in minutes (min).In cases where the initial data were in a nonstandard format, a transformation was applied following the "rule of thumb", assuming a normal distribution [18].This assumption was supported by the extensive database of studies, which allowed the central limit theorem to be valid [19].Additionally, when both cold and warm ischemia were applied, a weighted average between the two approaches was calculated based on the concept of the maximum effect from ischemia.The equations used for these computations are provided in analytical form below: The equations provided above involve the following variables: "x" represents ischemia time (IT), "y" represents operative time (OT), "m" represents the mean, "s" represents the standard deviation (SD), "n" represents the number of samples per arm, "cov" represents the covariance, and "r" represents the Pearson correlation coefficient between IT and OT [20].The use of the correlation coefficient in the calculations is evident in Eq. ( 3) presented earlier.To obtain accurate r values, a Monte Carlo simulation with 1000 repetitions was conducted (1) for each study and each compared arm, based on the EV and SE of the original variables [21].The physiological significance of the correlation coefficient lies in the covariance between IT and OT when assumed to follow a bivariate normal distribution [22].The theoretical range of r values extends from − 1 to + 1.For positive r values (approximating + 1), both IT and OT increase simultaneously, or they show an exact opposite pattern.This suggests scenarios related to the difficulty in performing partial nephrectomy (PN).In technically demanding procedures, both the total duration of the operation and the application of ischemia are expected to be extended to facilitate tumor removal, and vice versa.Conversely, for negative r values (approximating − 1), IT increases while OT is constrained, or IT decreases while OT is prolonged.In PN, the main goal is to limit ischemia duration, and the disproportionate use of ischemia likely reflects a strategic choice by the surgeon to implement hemostasis measures, despite its impact on postoperative renal function recovery.Following the calculations for the proportion of ischemia (I), the resulting data were re-tabulated by three reviewers: [SA], [DA], and [IS].
The estimation of the Pearson correlation coefficient (r) was performed collectively for each arm under comparison (RAPN vs. OPN) across all available studies, utilizing the expected values (EVs) of IT and OT.Subsequently, two coefficients were obtained, one for each arm, and these coefficients underwent statistical inference to estimate both their difference and their deviation from zero.It's important to note that we initially considered the likelihood of collinearity between the original variables, implying that as the duration of the surgery increases, so does the absolute time of ischemia application.Therefore, in case of a statistically significant difference in r between RAPN and OPN, it was predetermined to use these two correlation coefficients to calculate I for each arm, remaining constant as a pair across all available studies.This assumption was considered necessary, as determining r under a bivariate normal distribution through Monte Carlo simulations tends to be more conservative in revealing a substantial correlation between the two variables involved [23].
The generated I variable served as a suitable representation of the level of surgical precision in tissue handling and hemostasis during PN.It was also considered to adequately reflect the impact of intraoperative ischemic measures on postoperative renal function recovery.To estimate the overall effect of the comparison between RAPN and OPN, a meta-analyses methodology was employed, with the mean difference of I (MD I ) serving as the effect size.Given the inclusion of a substantial number of studies, made possible by the increased availability of data for the original variables, a random effects model was adopted, following the Hartung and Knapp modification [24,25].In the forthcoming meta-regression plots, each study was visually represented as a circle with a radius proportional to the accuracy of its reported results, based on the typical rendering standard.Additionally, linear regression models based on the restricted maximum likelihood (REML) estimation were applied [26,27].Heterogeneity within the data was assessed using the statistical parameters I 2 and Cochran's Q [28,29].The statistical analysis was conducted using the R programming language version 4.3.1 [30].This comprehensive approach enabled the systematic and objective evaluation of the precision of surgical maneuvers during RAPN and OPN, based on the proportion of ischemia implemented in each case.
The evaluation for potential publication bias (PB) was conducted through the utilization of appropriate funnel and radial plots.To enhance the robustness of its significance assessment, rigorous application of the Egger's test was carried out.Special attention was given to the impact of small studies, as they represented a substantial portion of the non-randomized studies included in the analysis.To explore additional sources of heterogeneity, subgroup analysis (SGA) was undertaken.This analysis was based on several factors, including the year of publication, the implementation of patient matching protocols, the involvement of multiple referral centers, and the risk of bias (ROB) classification according to the ROBINS-I tool.Furthermore, meta-regression analysis (MRA) was conducted to investigate the change in the comparative effect concerning both the publication year and the quality rating based on the Newcastle-Ottawa Scale (NOS).These parameters were treated as moderators for the respective analysis.MRA was applied to the entire set of studies and also separately for each of the aforementioned subgroups.This comprehensive approach allowed for a thorough examination of potential sources of variation in the overall effect between RAPN and OPN.
A sensitivity analysis (SA) was performed at four distinct levels to enhance the robustness and validity of the findings.At the first level, a subset of studies was isolated by applying a predefined cut-off to the range of the 95% confidence interval (CI 95% ) around the mean difference in I (MD I ) to assess the impact of individual studies on the overall effect size.At the second level, studies characterized by favorable methodological features and low risk of bias were selected.These studies applied patient matching and were classified as having low ROB according to the ROBINS-I tool, to draw more reliable conclusions regarding the comparative effect between RAPN and OPN.At the third level, a subset of studies with a larger patient population than the average of the initial dataset was chosen to address potential small study effects and enhance result reliability.At the fourth level, a sensitivity analysis was conducted by exploring a range of consecutive values of the correlation coefficient (r) between IT and OT, which is crucial in the estimation of I.This analysis involved examining the comparative effect between RAPN and OPN on MD I as the coefficient (r values) varied from − 0.99 to + 0.99, providing insights into the sensitivity of results to different correlation levels.These four levels of sensitivity analysis collectively ensured the reliability and validity of the overall results by accounting for individual study impact and the interconnection between IT and OT, while addressing potential sources of variability.
The present study meticulously adhered to the guidelines provided on the PRISMA website (http:// prisma-state ment.org/ Exten sions/ Proto cols) to ensure compatibility with the PRISMA 2020 Checklist.Results are presented in the format: MD I -CI 95% , with a confidence level of α = 0.05.To promote transparency and reproducibility, all primary and secondary data are available in ".csv" files, and the analytical code is accessible in ".txt" files.These materials are publicly accessible on a Github repository, through the URL: https:// github.com/ sotbi ke/I.git.Each code file's specific purpose and settings for reproducing the results are detailed in corresponding ".txt" files within the repository.Sharing these data and analytical code is intended to encourage open science practices, facilitate scrutiny of the findings, and promote further research in this domain.

Study retrieval
The PRISMA flowchart illustrating the literature search process, is presented in Fig. 1.The initial search yielded 582 studies, and after eliminating duplicates, non-English studies, and those with ineligible titles or abstracts, 178 studies remained for screening.Of these, 24 studies were excluded due to the unavailability of their full text, resulting in 154 studies included for investigation into comparative data on RPN/RAPN versus OPN.Nine of these studies lacked statistically exploitable data and were subsequently excluded from further analysis.Therefore, a total of 145 records underwent a comprehensive eligibility assessment.Among these, six were excluded as meta-analyses or simple systematic reviews, while 50 were excluded for lacking comparative data.Additionally, 26 studies were excluded as they did not contain data on the outcome of interest for the present analysis.It's worth noting that those studies excluded based on the latter criterion were initially considered eligible based on their general content.However, they did not simultaneously include comparative data for both original variables (IT and OT), which was necessary for estimating I. Through the inclusion-exclusion process described above, a total of 62 studies were identified as having suitable data for analysis.Among these, 18 studies focused on the comparison between RPN versus OPN, 43 compared RAPN versus OPN, and one study involved cost analysis.This final study-set provided data for a total of 26,072 patients, with 14,596 in the experimental group (RPN/RAPN) and 11,476 in the control group (OPN).

Study demographics
In this subsection, a comprehensive description of demographic metadata derived from the isolated studies is provided.Regarding the country of origin for both study and patient-level data, the primary sources were from the United States of America, Korea, and Japan.Additional contributions came from Italy and France within the European region.The percentage Fig. 2 Comprehensive pie charts displaying the percentage distributions of studies and patients by their respective countries of origin distribution of acquired data at both levels is visually depicted in the relevant pie charts shown in Fig. 2. For further clarity, corresponding map charts are provided in Additional file 1: Fig. 1.Concerning the time periods of activity covered by the incorporated studies, the majority spanned the decade between 2006 and 2016.Figure 3 illustrates the specific timeframes and durations during which each study was in progress, based on the implementation of patient matching.These data are presented in Additional file 1: Fig. 2, with a focus on the number of referral centers involved and the classification according to the ROBINS-I tool.Importantly, no deviations were found regarding the duration of studies for any of the subgroups under investigation, indicating a uniform distribution in this regard.As for the parameter of publication year, 53.23% of the studies, accounting for 76.34% of the patient data, were published after the year 2018.This specific year was selected as the cutoff point, being the median publication year for all the included studies.Subsequent analysis according to patient matching implementation, revealed that 43.55% of data at the study level and 52.53% at the patient level involved the utilization of such methodology.Consequently, the analyzed data were considered balanced with respect to patient matching.The corresponding pie charts are presented in Fig. 4. Furthermore, in terms of referral centers, approximately 32.26% of the studies, accounting for 65.88% of the included patient data, were associated with a multicenter type of analysis.Lastly, concerning the ROB assessment using the ROBINS-I tool, approximately 31.7% of the incorporated studies, representing 54.46% of the patient data, belonged to   the "ROBINS-I: Low" category.For studies classified as having moderate and serious ROB, the corresponding percentages were 68.3% and 45.54%, respectively.The relevant results are visually presented in Fig. 5.The comprehensive compilation of the included studies is presented in Table 1, detailing their specific characteristics.These features encompass the publication year, patient matching utilization, number of referral centers, timeframe of activity, NOS grading, ROBINS-I class, and any deviations observed concerning baseline characteristics among the compared populations.Upon analysis of the pooled studies, common baseline differences were related to older patients and higher complexity renal masses in the OPN group.However, in general, no significant differences were observed between the compared surgical approaches.Regarding the ROB assessment, the ROBINS-I grading forms for each individual study are included as Additional file 2. For the tabulation and visualization of the results of this assessment, the statistical package "Robvis" in the R programming language was employed [31].Figure 6a presents a summary plot for the entire dataset, graphically depicting the percentages of studies in each risk category, spanning the 7 domains of the ROBINS-I tool.In Fig. 6b, similar summary plots are provided, stratifying the data according to patient matching.From the examination of these specific diagrams, it can be deduced that in overall there were no significant deviations from intended interventions.The most notable risk percentages were observed in the domains of "confounding", "classification of interventions" and "selection bias", each accounting for 40% of the pooled studies, encompassing both moderate and serious ROB.Concerning those studies with patient matching, it becomes apparent that the overall ROB is notably suppressed.Conversely, in studies without the application of a patient matching protocol, bias in all three aforementioned domains is inflated, with their respective percentages now being 75%, 65%, and 60%.A complementary analysis was conducted to account for the subgroups as well.The results demonstrated better performance in terms of ROB, in studies published after 2018 compared to older ones (ROBINS-I: Low: 40% vs. 30%), and in multicenter over single-center studies (ROBINS-I: Low: 50% vs. 30%).The outcomes at the subgroup level align with the expected theoretical differences between the respective groups, affirming the likely appropriate application of the ROBINS-I tool.The summary plots for the subgroups, as well as the traffic light plots showing the grading of each study for each of the 7 domains of the tool, are available as Additional file 1: Fig. 3 and Additional file 1: Figs.4-10, respectively.

Correlation coefficient
In the initial phase of data analysis, the investigation focused on the role of the correlation coefficient (r), and the relevant examination was conducted at two stages.Firstly, it was performed on the pooled data by utilizing the expected value of I (EV I ) in both RPN/RAPN and OPN arms collectively.Subsequently, the analysis was carried out for each arm of every study individually, employing a Monte Carlo simulation for indirect determination.Regarding the first level of estimation, Fig. 7 showcases the scatterplots of IT-OT pairs for each compared group.A visual observation of these diagrams confirms the initially hypothesized correlation between IT and OT.Notably, in the OPN group, the correlation appears to be stronger, with longer ischemia times compared to RAPN for operations lasting more than 200 min.The correlation coefficients derived from the expected values of IT (EV IT ) and OT (EV OT ) from all studies in the RAPN and OPN groups were found to be 0.256 and 0.644, respectively.The difference in correlation coefficients between the two groups was found to be statistically significant (z value = − 2.7353, p value = 0.0062).Additionally, both coefficients were significantly different from zero (RAPN group: t-value = 2.0122, p value = 0.0487; OPN group: t-value = 5.8804, p value < 0.0001).These findings hold physiological significance through statistical inference, as they indicate that in both approaches, the absolute time of intraoperatively applied ischemia increases with the duration of the operation, with a stronger correlation observed in open surgery cases.As per the relevant strategy formulated in the section 2, this specific pair of coefficients for the RAPN and OPN groups will be used to estimate the EV I and SE I in each arm of every included study.
In the subsequent stage, a Monte Carlo simulation with 1000 repetitions was conducted for every study and each arm of the comparison, utilizing the corresponding patient populations [21].The primary objective of this simulation was to generate a bivariate normal distribution for the original variables, aiming to determine the most probable correlation coefficient in each case.Upon completing the calculations, a dataset with coefficients on the order of magnitude of E(-3) (i.e., 10 to the power of − 3) was obtained, which can be practically considered as negligible.These findings indicate a lack of significant correlation between IT and OT, a pattern that is not globally representative, as demonstrated in the previous inference.Consequently, in the following analysis, special emphasis is placed on the estimation of I using the pair of correlation coefficients obtained for the RAPN and OPN groups at the first level of the present investigation, as presented above.This approach enables a more accurate and reliable estimation of the relationship between IT and OT, and its impact on I in each arm of every included study, leading to more robust conclusions.

Exploratory meta-analysis
This subsection involves the presentation of results from the meta-analysis for the original variables (IT, OT), I, and MD I , utilizing a random effects model.In this analysis, the pair of correlation coefficients established above were employed to compare the outcomes of RAPN and OPN.The dataset encompassed a total of 24,507 patients, with 14,124 falling within the experimental group (RPN/ RAPN) and 10,383 within the control group (OPN).Initially, the impact of the two surgical approaches was assessed individually, for each of the IT and OT variables.For IT, in the overall pool of available studies and within the RAPN group, the expected value (EV IT ) stood at 19.95 min, with a corresponding 95% confidence interval (CI 95% ) of [18.61; 21.28].Conversely, within the OPN group, the EV Ι Τ was determined to be 21.05 min, with a CI 95% of [18.89; 23.21].A preliminary inspection of the above findings suggests that there is no statistically significant distinction in the absolute duration of ischemia between RAPN and OPN.With respect to the OT variable in the RAPN group, EV OT was calculated as 181.7 min, with a CI 95% of [172.1; 191.3].In comparison, in the OPN group, EV OT was found to be 161.5 min, with a CI 95% of [151.6; 171.4].This analysis reveals a notable inclination toward a shorter surgical duration in OPN cases; however, this trend does not reach a level of absolute statistical significance.The forest plots of the aforementioned results are provided as Additional file 1: Figs.11-14.
Furthermore, within the context of preceding analyses, an examination of the mean differences in IT and OT was conducted.Concerning the former, the mean difference in IT (MD IT ) was calculated as − 1.11 min, with CI 95% = [− 2.92; − 0.70].In terms of the latter, the mean difference in OT (MD OT ) was determined to be 19.74 min, with CI 95% = [11.56; 27.92].The above comparison between RAPN and OPN underscores the absence of substantial deviation in the absolute duration of ischemia.However, it is evident that the robotic approach entails an approximately 20-min lengthier process.Given this observation and mindful of the correlation between the original variables, the inquiry now pertains to whether the additional 20 min of surgical time in the context of RAPN engender a significant alteration in the proportion of ischemia, a parameter deemed inherent in each surgical approach.The pertinent outcomes are delineated Fig. 7 Scatter plots depicting the IT-OT pairs for the two compared surgical approaches (RAPN-OPN) in partial nephrectomy.Each diagram is accompanied by the corresponding correlation, represented by a dashed line.It is noted that the plots were constructed using the expected values for each variable from each arm of every included study in the Additional file 1: Figs.15-16, presented as forest plots.Finally, the results acquired for the I variable were subjected to a similar analytical methodology.Accordingly, as for the expected value of I (EV I ) within the RAPN group, it stood at 0.121, with CI 95% = [0.111;0.130].On the contrary, within the OPN group, the corresponding EV I was determined to be 0.131, with CI 95% = [0.121;0.141].These findings offer valuable insights into the disparity observed in MD I , warranting further exploration.Essentially, they imply a lack of statistical significance between the robotic and open approaches in relation to the ischemia proportion required for the seamless conduct of the PN procedure.The corresponding results are visually depicted as forest plots, accessible through Additional file 1: Figs.17-18.

Meta-analysis, subgroup analysis and meta-regression analysis
In this section, the meta-analysis (MA) conducted for MD I using the previously implemented random effects model with the Hartung and Knapp adjustment is presented.The comprehensive examination of the comparison between RAPN and OPN on the I variable, based on the aggregated studies, yielded an overall mean difference of: MD I = − 0.0105, accompanied by a CI 95% of [− 0.0212; 0.0002].This outcome highlights a trend of insignificance regarding the superiority of RAPN over OPN in terms of the proportion of intraoperatively applied ischemia.The visualization of this finding can be observed through the forest plot presented in Fig. 8.However, it is imperative to acknowledge the high degree of heterogeneity observed (Cochran's Q = 2522.67,Higgins I 2 = 97.6%,CI 95% = [97.3%;97.9%]).This heterogeneity level can be ascribed to several underlying factors.Primarily, the inclusion of numerous studies is expected to introduce anticipated disparities.Furthermore, the utilization of estimator functions results in condensed standard errors (SE) compared to population standard deviations (SD), consequently amplifying inter-study variation (τ 2 ).Lastly, the incorporation of non-randomized comparative analyses, coupled with a substantial proportion of small studies marked by low accuracy in reported results, contributes significantly to the observed heterogeneity.
In overall, the above suggest that a significant proportion of the observed variability can be attributed to genuine differences in effect sizes rather than just random error, as inter-study variation is estimated at: τ 2 = 0.0017, with CI 95% = [0.0012;0.0025].Figure 9a illustrates the funnel plot designed to evaluate the presence of publication bias (PB), while incorporating a regression curve to model small study effects.The corresponding graph demonstrates a notable degree of symmetry around the overall estimate of the effect across all encompassed studies.Additional file 1: Fig. 19 depicts the same funnel plot, augmented with contours indicating statistical significance.Additionally, an evaluation was undertaken using the Egger's test to gauge the significance of asymmetry.The resulting magnitude of bias (MB) was computed as − 0.2385, accompanied by an SE of 1.5575.Employing linear regression yielded a t value of − 0.15, and the associated p-value stood at 0.8788.This outcome underscores the absence of a statistically significant PB.In summary, the amalgamation of results and their collective interpretation, suggest a lack of compelling evidence for asymmetry within the funnel plot analysis.This outcome indicates that the observed estimates of effect size remain relatively unaffected by potential factors such as PB or other systematic sources of distortion.Further scrutiny was applied to investigate the potential impact of small study effects.The respective test does not provide strong substantiation to infer that publication bias or other related biases from small studies considerably sway the outcomes of the meta-analysis.This is further supported by the Q-Q′ value of 0.99, and a corresponding p value of 0.3209.For an in-depth exploration of PB, Fig. 9b introduces a radial plot integrated with the solid regression line derived from Egger's test.
Subsequent to the primary investigation, a subgroup analysis (SGA) was meticulously conducted, encompassing various stratifications based on distinct factors, including publication year, patient matching, the number of referral centers involved, and the ROB assessment employing the ROBINS-I tool.For studies published post-2018, the MD I exhibited a value of − 0.014, accompanied by a CI 95% spanning [− 0.029; 0.002].On the other hand, for studies predating this period, the MD I was determined as − 0.007, with a corresponding CI 95% of [− 0.023; 0.009].The outcomes regarding patient matching unveiled an MD I of − 0.007 within the CI 95% range of [− 0.026; 0.013] for matched analyses, whereas the nonmatched studies displayed an MD I of − 0.013, enclosed within the CI 95% bounds of [− 0.025; − 0.001].Additionally, for multicenter studies, the MD I stood at − 0.016 within the CI 95% interval of [− 0.031; − 0.001], while single-center studies yielded an MD I of − 0.008 within the CI 95% bounds of [− 0.022; 0.007].Further subdivision based on the ROB assessment revealed intriguing findings.For studies categorized as "ROBINS-I: Low", the MD I was estimated at − 0.016, with a CI 95% of [− 0.032; 0.001].Similarly, studies classified as "ROBINS-I: Moderate" displayed an MD I of − 0.004 within the CI 95% of [− 0.020; 0.013].Lastly, for studies categorized as "ROBINS-I: Serious", the MD I stood at − 0.015, encompassing the CI 95% interval of [− 0.046; 0.015].In a systematic manner, the outcomes of the subgroup analysis collectively, do not present robust statistical significance Fig. 9 Funnel plot presenting publication bias assessment in all the examined studies, incorporating a curved regression line to investigate for small study effects (a).Radial plot complemented with an integrated regression line, to assess the significance of publication bias using Egger's test (b) regarding the distinction between RAPN and OPN as for the proportion of ischemia (I).The above discerning findings aptly demonstrate the equivalence of the two surgical approaches in terms of the per minute requirement for intraoperative ischemia during PN.The relevant SGA results are provided as forest plots in Additional file 1: Figs.20-23, while the pooled analysis results are presented concisely as percentages of IT over OT in the first section of Table 2.
Conclusively, a meta-regression analysis (MRA) was complementarily conducted at both the pooled data and subgroup levels, employing a restricted maximum likelihood linear model.This model facilitated the construction of regression lines to represent the change in corresponding effects.Illustratively, Fig. 10a portrays the overall comparative effect of RAPN versus OPN concerning the MD I , juxtaposed against the publication year.Similarly, Fig. 10b showcases the same comparative Table 2 The meta-analysis results for the complete set of studies that were isolated The first three levels of sensitivity analysis are included for each subgroup under investigation.Statistically significant findings are highlighted in bold.However, absolute statistical significance was considered of low clinical significance, as the proportion of ischemia in both RPN and OPN was determined to be around 12-13% of the total surgical time An asterisk (*) implies the presence of a single study in the subgroup of interest  analysis, this time in relation to the quality assessment score, as measured through NOS.In both graphical representations, the observed effects exhibit a consistent pattern, irrespective of the publication year or the awarded number of quality stars.Notably, the quantitative trend revolves around the zero line, suggesting a neutral effect.The scope of the MRA was further extended to encompass subgroup levels as previously defined.Across these subgroups, the comparative effect consistently maintains its neutrality, reinforcing the uniformity of the above findings.Collectively, the analysis presented above points towards the absence of a significant disparity between RAPN and OPN with regard to the novel I variable.This lack of distinction holds true regardless of the publication year or the assessed quality level established through the NOS scale.The respective results are presented in Additional file 1: Figs.24-26 (Fig. 11).

Sensitivity analysis
In the last part of this section, we present the results of the sensitivity analysis (SA) that was conducted at four distinct levels.Initially, a subset of studies was isolated through exclusion criteria targeting studies with low accuracy of reported results.The precision of each study's findings was ascertained through the utilization of the inverse variance method, visually represented through the range of 95% confidence intervals (CI 95% ) presented in the respective forest plots.Following the determination of summary statistics for CI 95% across the entire array of studies, a permissible range equivalent to 2 SDs was established based on previously conducted calculations.Consequently, 25 studies were deemed ineligible and excluded from the analysis, resulting in a final cohort of 37 studies with a more compacted profile pertaining to Fig. 11 Forest plot showing the comparative effect as the mean difference of I (MD I ) between RAPN and OPN in the subset of studies with increased accuracy of reported results, for the first level of the sensitivity analysis the precision of reported I estimates.In aggregate, data emanating from a total of 22,238 patients were analyzed, with 12,961 individuals allocated to the experimental group and 9277 assigned to the control group.The pooled effect estimate was computed as follows: MD I = − 0.008, with CI 95% = [− 0.022; 0.006].Despite efforts to enhance accuracy, substantial heterogeneity persisted (Cochran's Q = 2255.36,Higgins I 2 = 98.4%,CI 95% = [98.2%;98.6%]), corroborated by inter-study variance: τ 2 = 0.0018, with CI 95% = [0.0012;0.0030].This degree of heterogeneity can be attributed to variability in the method of data retrieval for I, emphasizing the pronounced disparity in the strategies employed for implementing intraoperative ischemia across the amalgamated studies.A revised funnel plot characterized by relative symmetry surrounding the overall effect estimate is presented in Fig. 12a.The implementation of the Egger's test for PB assessment resulted in an MB of 0.4362, with an SE of 3.0206.The ensuing linear regression analysis yielded a t value of − 0.14 and a p value of 0.8860.Consequently, the statistical insignificance of PB is reaffirmed, a conclusion further reinforced by the visual symmetry evident in the corresponding plot.Moreover, the absence of substantial small study effects is also evident (Q-Q′ statistic = 1.34, p value = 0.2465).In Fig. 12b, the radial plot delineates the refined compilation of 37 studies, incorporating a solid regression line derived from the Egger's test.The minimal deviation of this regression line from the dashed line representing actual data suggests a similarity between the present analysis and the initial findings.
The scope of the sensitivity analysis was expanded to encompass previously scrutinized subgroups.In studies published subsequent to 2018, the comparative effect manifested as follows: MD I = − 0.019, with CI 95% = [− 0.037; − 0.0001].Conversely, for studies previously published, the effect estimate was: MD I = − 0.006, with a corresponding CI 95% of [− 0.017; 0.028].In instances where patient matching protocols had been employed, the resultant effect was: MD I = − 0.003, accompanied by a CI 95% of [− 0.028; 0.022].Conversely, for studies that deviated from such a protocol, the observed effect was: MD I = − 0.013, with CI 95% = [− 0.030; 0.004].Upon further analysis, for studies conducted across multiple centers, the effect MD I equaled − 0.013, along with a corresponding CI 95% of [− 0.031; 0.006].On the other hand, for analyses confined to a single center, the effect was ascertained as: MD I = − 0.005, with a CI 95% of [− 0.027; 0.017].Moreover, upon stratification according to the ROBINS-I tool, studies classified as "ROBINS-I: Low" exhibited an effect estimate of: MD I = − 0.015, with a CI 95% of [− 0.032; 0.002].Similarly, studies classified as "ROBINS-I: Moderate" yielded an effect estimate of: MD I = − 0.007, accompanied by a CI 95% of [− 0.034; 0.019].For the subgroup characterized as "ROB-INS-I: Serious", the effect estimate was calculated as: MD I = 0.005, with a CI 95% of [− 0.048; 0.057].In light of these findings, within the confines of these meticulously selected subgroups characterized by adherence to reporting accuracy, no statistically significant differences are evident in terms of normalized ischemia time (I) between the two surgical techniques under comparison.A comprehensive compilation of these outcomes is provided in Additional file 1: Fig. 27.The relevant results are summarized as percentages of IT over OT, at the first level of SA in Table 2.The initial phase of the SA was also augmented by the inclusion of an MRA. Figure 13a displays the alteration in the comparative effect vis-à-vis the year of publication, while Fig. 13b portrays the effect in relation to the quality stars assigned according to the NOS assessment.Analogous to the findings in the primary analysis, MD I appears to exhibit a consistent pattern irrespective of the moderating variables, maintaining alignment with the horizontal axis of neutrality.These uniform outcomes were consistently replicated across all the pre-defined subgroups.Detailed graphical representations of the MRA results can be found in Additional file 1: Figs.28-29.In the second level of SA, a distinct study selection criterion was employed for analysis.Specifically, studies that applied patient matching and concurrently evaluated as "ROBINS-I: Low" were isolated, to enhance the reliability of ensuing outcomes.This combined criterion yielded a novel set comprising 19 studies, encompassing 10,213 patients, with 6423 undergoing RPN/ RAPN and 3790 undergoing OPN.From the analysis of aggregated data concerning the comparative effect, the following finding emerged: MD I = − 0.015, with a CI 95% = [− 0.035; 0.005], confirming our initial findings indicating the absence of significant disparity in terms of the proportion of ischemia in the RAPN versus OPN comparison.The pertinent results are presented in Fig. 14, and the respective field concerning the second level of SA in Table 2. Regarding heterogeneity, the following emerged: Cochran's Q = 584.49,Higgins I 2 = 96.9% with a CI 95% = [96.1%;97.6%], and τ 2 = 0.00017 with a CI 95% = [0.0009;0.0038], without substantial differentiation from our prior findings.In Fig. 15a, the relevant funnel plot for assessing PB and small study effects is depicted, which in this case seems to exert significant impact (Q-Q′ statistic = 13.35,p value = 0.0003).Subsequently, Fig. 15b displays the corresponding radial plot with the solid line denoting the Egger's test.In this instance, the outcome was: MB = − 1.5110 with SE = 2.3966, whereas through linear regression analysis it was: t value = − 0.63, and p value = 0.5368, demonstrating the absence of substantial PB.The final phase of this level of SA was augmented by MRA, where no significant deviations were observed compared to the already presented findings.Specifically, in this study set, the comparative effect was uniformly distributed around zero, both in terms of publication year and the qualitative status of the included studies according to the NOS.The relevant diagrams are presented in Fig. 16.
At the third level of SA, the total population of integrated patients served as the sole criterion for study selection.Specifically, after initially calculating the average population across the initial study set, records were isolated where the sum of populations in their experimental and control arms exceeded this average.The aim of this specific analysis was the complete elimination of small studies, thereby enabling the estimation of comparative effects from analyses of larger feasible size, with the presumption that they provide the most robust results.The final set included 15 studies, encompassing a total of 17,937 patients, with 10,995 in the RPN/RAPN arm and 6942 in the OPN arm.Pooled data analysis yielded the following result: MD I = 0.001 with a CI 95% = [− 0.026; 0.028], as depicted in Fig. 17.From the above, it became evident that even in the case of large studies, no difference emerges between RAPN and OPN concerning the I variable.However, heterogeneity remained at previously high levels (Cochran's Q = 1409.54,Higgins I 2 = 99% with a CI 95% = [98.8%;99.2%], and τ 2 = 0.0024 with a CI 95% = [0.0013;0.0060]).In this case as well, PB did not exhibit significant impact based on the Egger's test (t value = 0.90, p value = 0.3847), while the relevant funnel and radial plots are provided in Additional file 1:  The fourth and final level of SA involve the theoretical exploration of the variation in MD I between RAPN and OPN, for a range of successive values of the correlation coefficient (r) between the original variables (IT, OT).In this case, the two compared groups (RAPN, OPN) share a common coefficient, with r sequentially taking values from − 0.99 to + 0.99.The aim was to verify whether a substantial difference exists in the MD I between the extreme values of r, followed by the interpretation of the physiological impact of the resulting findings.In the section 2, the hypothesis was formulated that the most positive r values (i.e.those proximal to + 1) are related to the level of difficulty in performing the PN, with the expected consequence of an increase in IT with an increase in OT, and vice versa.On the other hand, the most negative r values (i.e.those proximal to − 1) are theoretically associated with the specific strategy regarding ischemia application from the perspective of the treating surgeon.Figure 19 illustrates the variation of the comparative effect (MD I ) between RAPN and OPN for successive values of r, as previously described.From a careful examination of the diagram, a nearly constant comparative effect is observed across the entire spectrum of r values.Interpreting this finding, it can be concluded that the difference between the aforementioned surgical approaches in terms of normalized ischemia time (I) is not influenced by the difficulty in performing PN, nor by the intraoperative choices of the surgeon.Additionally, based on the findings derived earlier, it can be asserted that the proportion of ischemia (I) is an inherent characteristic of both RAPN and OPN, without a substantial difference between the two approaches.Extending this reasoning, it could be further hypothesized that the I variable constitutes a distinct characteristic of PN itself, essentially serving as a constant.However, drawing secure conclusions in this regard requires further investigation and lies beyond the scope of this study.
Remaining within the context of Fig. 19 and comparing it with the findings from earlier levels of the SA, it is noted that in the case of a common correlation coefficient between RAPN and OPN, there is an apparently significant advantage for the former in terms of the proportion of intraoperatively applied ischemia (I).Nevertheless, the relatively high heterogeneity level observed discourages acceptance of this finding as universally valid.This position is significantly reinforced by confirming the existence of different and non-zero correlation coefficients between RAPN and OPN groups.Furthermore, the variation of MD I across the range of r values within subgroup levels is presented in Additional file 1: Figs.34-35.In this case, a similar possibly pseudo-significant advantage emerges, from studies published after 2018, those without patient matching, multicenter studies, and those of "ROBINS-I: Low" class.
Finally, animated plots were appropriately constructed to highlight the dynamic changes of PB and MD I in both the aggregated data and the various subsets of investigated subgroups.Animated Plot 1 demonstrates the alteration of the funnel plot for PB estimation.The gradual accentuation of asymmetry suggests an increase in the impact from PB.In contrast, Animated Plot 2, depicting the corresponding radial plot change, doesn't reveal significant divergence between the solid line of Egger's test and the dashed line corresponding to the acquired data, which aligns with the non-statistically significant effect of PB on the overall effect estimation.In the context of MRA, Animated Plots 3-10 and Animated Plots 11-15 present the variation of MD I using publication year and NOS quality stars as moderators, respectively.A common finding emerges from these: the initial trend of RAPN superiority over OPN in terms of the proportion of ischemia diminishes towards zero with the incremental shift of r from − 0.99 to + 0.99.In conclusion, it's worth noting the non-significant difference in MD I between the extreme values of r, an observation that was thoroughly discussed previously.

Discussion
The present study introduces the novel variable of ischemia proportion (I) to facilitate the comparison of RAPN and OPN as for their relative ischemia requirements.The research addresses the limitations associated with using absolute ischemic time as the sole parameter for such a comparison.Notably, the analysis reveals a substantial discrepancy in OT, with RAPN generally requiring approximately 20 min more than OPN.Conversely, the difference in absolute IT proved statistically insignificant, with RAPN exhibiting only a marginal one-minute reduction compared to OPN.This observation does not suggest a significant physiological impact.Therefore, the study introduces the novel variable of normalized IT to OT to offer a nuanced perspective on ischemia application in PN procedures.The I variable is systematically computed across various studies and sensitivity analysis levels, consistently indicating no significant difference between RAPN and OPN.The mean difference in the proportion of ischemia (MD I ) tends to regress around zero, with only a faint inclination favoring RAPN in limiting ischemia.The expected value of I (EV I ) for both surgical approaches approximates 12-13%.However, forest plots present a remarkable degree of heterogeneity, warranting further investigation.This heterogeneity level may be attributed to variations in the definition of the novel variable, the inclusion of non-randomized and of low sample size studies, and variability in ischemia implementation strategies.Individual estimates within the forest plots reveal persistent residual heterogeneity, suggesting genuine disparities in I and MD I among the included studies.This insight is particularly significant, implying that the strategy for implementing ischemia possibly differs across studies, leading to unabated heterogeneity.This variability could be explained by two primary technical aspects in conducting PN: one involving a more liberal approach to ensure hemostasis by employing ischemia, and the other aiming to optimize postoperative renal function recovery and prevent acute kidney injury (AKI) by minimizing intraoperative ischemia duration.While MD I tends to approach zero even when a significant portion of surgical time is dedicated to ischemia in both RAPN and OPN, it is conceivable that a baseline ischemia duration is fundamental for PN procedures in general.However, this assumption cannot be definitively confirmed with the available data.
The international literature extensively explores the application of intraoperative ischemia in PN, revealing numerous variations in both duration and type [12,[32][33][34].Additionally, ischemia duration (IT) plays a pivotal role in the composite outcome referred to as the "Trifecta", which assesses renal tumor excision quality by considering complication rates, resection margin status, and renal function changes.Two primary definitions of the Trifecta concept are prominent, primarily differing in the assessment of their impact on patients' renal function.Both definitions require the simultaneous fulfillment of three criteria: the first includes negative surgical margins, the absence of urological complications, and an ischemia duration of less than 20 min, while the second replaces IT with the percentage change in the estimated glomerular filtration rate (eGFR), which should generally remain below 10% [35][36][37].These variations highlight the complexity involved in analyzing the impact from IT and the variability in ischemia application techniques.In a retrospective cohort study, Sawada et al. conducted a comparative analysis comparing RAPN to OPN for the treatment of small renal masses.Rigorously adjusting for individual patient and tumor characteristics, the researchers revealed RAPN's superiority over OPN in critical aspects such as estimated blood loss (EBL), IT, and hospital length of stay (LOS).Despite the fact that no statistically significant differences emerged in perioperative complications or positive surgical margin rates, RAPN notably excelled in preserving renal function immediately post-surgery and at the three-month follow-up.This study provides valuable insights into specific aspects of the diverse range of ischemia techniques and underscores the pivotal role of ischemia duration in achieving favorable outcomes in PN [38].Furthermore, the absolute IT remains a focal point of investigation concerning postoperative renal function in patients undergoing PN.In this regard, Antonelli et al. sought to validate Martini's nomogram, an estimator of post-PN renal function decline, using extensive data from multiple medical centers in Italy.Employing this nomogram across OPN, LPN, and RAPN procedures demonstrated strong predictive accuracy for the latter two techniques at 6-month and 12-month marks.However, predictive efficacy waned for OPN, a trend consistent across all approaches by the 48-month assessment.Notably, patients in higherrisk categories demonstrated an increased probability of experiencing renal function decline, although the nomogram's predictive accuracy fell below 70% at the 48-month checkpoint [39].
The above findings underscore the particular interest in investigating both the absolute ischemia duration and the technical aspects concerning its application within the context of international literature related to PN.Several studies have focused on comparing RAPN versus OPN in relation to the absolute IT [40,41].The current analysis represents an initial attempt to explore IT as a proportion of OT, as the aforementioned original variables appear to be significantly correlated.Our results have demonstrated equivalence between OPN and RAPN concerning the inherent need for ischemia, an anticipated outcome due to the relatively universally applicable strategies of IT minimization in PN procedures.The ultimate goal in the development of the prototype I variable also encompasses its further utilization in subsequent studies for detecting inherent differences in IT demands among various surgical approaches that involve ischemia application.

Strengths and limitations
The current investigation demonstrates several strengths and limitations, which this section thoroughly evaluates.
A primary strength lies in the introduction of the novel I variable, previously absent in the original data of the included studies.This variable aims to assess the comparative impact of RAPN versus OPN on the proportion of ischemia, a quantifiable metric crucial for evaluating ischemia duration within the context of PN and its direct correlation with surgical precision.This hypothesis was well-founded due to the dual influence of intraoperatively applied ischemia duration, driven both by surgical techniques and the inherent complexities of PN, on postoperative renal function.Another strength is the focus on a concise triad of variables: ischemia time (IT), operative time (OT), and the ischemia proportion (I), all subjected to thorough examination.The study draws upon a comprehensive dataset derived from an extensive body of international literature comparing RAPN and OPN.Methodological rigor is evident in the systematic literature search and the application of inclusion criteria, ensuring transparency and consistency, as detailed in the section 2. Furthermore, the present study conducts an extensive analysis using robust methodologies, encompassing both aggregate-level and subgroup-level assessments.Employing a multilevel approach, it utilizes meta-regression and sensitivity analyses to ensure a comprehensive and consistent extraction of insights from the compiled data.These strengths collectively enhance the validity and reliability of the study's findings.
However, the present analysis has notable limitations, primarily stemming from the computationally intensive nature of its methodology.It includes predominantly non-randomized comparative studies of RAPN versus OPN, often characterized by modest sample sizes.This extensive inclusion, coupled with repetitive calculations, results in a significant degree of heterogeneity, as discussed in the Sects.3 and 4. The reliance on estimators and the assumption of normal distribution within each comparative arm of the included studies contribute to this level of heterogeneity.Additionally, limitations arise from the approximation of the correlation coefficient (r) between IT and OT, due to the unavailability of individual patient data for direct calculation.Despite these limitations, it's essential to recognize that the study's results align coherently with the underlying physiological rationale governing the original variables.

Future potential
Despite its inherent constraints, the present study holds significant implications concerning the introduced novel variable.As elucidated earlier, the marginal difference in I between RAPN and OPN, quantified as MD I , appears to have minimal influence within the typical duration of PN.This finding suggests the possible existence of a fundamental baseline level of ischemia proportion intrinsic to PN, warranting comprehensive investigation across RAPN, LPN, and OPN.Future research could involve determining summary statistics for IT, OT, and the newly devised I variable within each patient cohort, enhancing the computation of the correlation coefficient (r) and refining the theoretical framework.It is worth noting that the I metric, primarily driven by the IT variable, may not fully capture the multidimensional nature of surgical precision in PN.Consequently, our future efforts will focus on comparatively investigating the multifaceted outcome of surgical precision in the context of the per minute estimated blood loss (EBL), aiming to establish a comprehensive framework for robust interpretation and sound conclusion-drawing.

Conclusions
In the present investigation, we undertook a retrospective comparative analysis between RAPN and OPN with a focus on the ischemia proportion.To facilitate this examination, a novel variable denoted as I was thoroughly formulated, serving as a measure inversely reflecting surgical precision.Specifically, we leveraged essential data from primary comparative studies, isolating the original variables IT and OT, and ultimately estimating the pertinent statistical parameters for I through appropriate estimator functions.Subsequently, a meta-analysis was conducted to derive an overall effect estimate, gauged through the mean difference between the two surgical approaches under comparison.Upon subjecting the collected data to a rigorous multilevel analysis, no statistically significant disparity emerged between RAPN and OPN in terms of the normalized ischemia duration relative to the total operative time.Notably, this finding was reinforced by MRA, which underscored the stability of the finding across various dimensions such as publication year and quality assessment based on the NOS scale.Additionally, sensitivity analysis reaffirmed the consistency of the initial findings.Consequently, we inferred the presence of a fundamental baseline level of ischemia proportion within the majority of PN procedures.To explore this hypothesis more comprehensively, further investigations will be warranted in subsequent studies.

Fig. 3 Fig. 4 Fig. 5
Fig. 3 Concise diagram illustrating the temporal activity intervals of the included studies by patient matching

Fig. 6
Fig.6 Summary plot illustrating the evaluation of all incorporated studies using the ROBINS-I tool, presenting their percentages corresponding to the risk level within each of its seven domains (a).ROBINS-I assessment stratified by patient matching (b)

Fig. 10
Fig. 10 Meta-regression analysis plots showing the change in the comparative effect (MD I ) between RAPN versus OPN, along with the CI 95% , in the aggregated studies, using as moderator the publication year (a) and the score in quality stars based on the NOS scale (b)

Fig. 12 90 Fig. 13
Fig.12 Funnel plot presenting publication bias assessment in the subset of studies corresponding to the first level of sensitivity analysis, that incorporates a curved regression line to investigate for small study effects (a).The respective radial plot with an embedded regression line, to assess the significance of publication bias using Egger's test (b)

Fig. 30 .
This analysis was extended to the subgroup level, where for studies published after 2018, the result was: MD I = − 0.008 with a CI 95% = [− 0.043; 0.027], while for previously published studies it was: MD I = 0.025 with a CI 95% = [− 0.026; 0.077].Additionally, for studies with patient matching, it was: MD I = − 0.007 with a CI 95% = [− 0.059; 0.045], whereas for those without patient matching, it was: MD I = 0.010 with a CI 95% = [− 0.019; 0.038].Furthermore, for multicenter studies, it was: MD I = − 0.012 with a CI 95% = [− 0.039; 0.015], while for single-center analyses, it was: MD I = 0.020 with a CI 95% = [− 0.046; 0.087].Lastly, regarding the ROB assessment, in those studies classified as "ROBINS-I: Low", the result was: MD I = − 0.025 with a CI 95% = [− 0.056; 0.006], for those categorized as "ROBINS-I: Moderate", it was: MD I = 0.014 with a CI 95% = [− 0.032; 0.060], while the group "ROBINS-I: Serious" included only one study.The relevant results are presented in Additional file 1: Fig. 31.In Table2, all the above findings are summarized comprehensively as a percentage of IT over OT, in the respective fields pertaining to the third level of SA.Finally, during the MRA on pooled data, a similar pattern of uniform zero-comparative effect emerged, as shown in Fig.18.Analogous results were also obtained during MRA at the subgroup level, as presented in Additional file 1: Fig.32-33.

Fig. 14 90 Fig. 15 90 Fig. 16
Fig. 14 Forest plot showing the comparative effect as the mean difference of I (MD I ) between RAPN and OPN in the subset of "ROBINS-I: Low" studies with patient matching, for the second level of the sensitivity analysis

Fig. 19
Fig.19 Plot depicting the change in the comparative effect (MD I ) between RAPN and OPN, along with the CI 95% , for consecutive r values, at the fourth level of the sensitivity analysis and for the total of included studies

Table 1
Included studies, detailing title, author, publication year, methodology, duration of activity, quality assessment, patient population in each arm of the comparison, and baseline differences between populations

Table 1 (
continued) RAPN robot-assisted partial nephrectomy, OPN open partial nephrectomy, NOS Newcastle-Ottawa Scale, ROBINS-I Risk of Bias in Non-randomized Studies of Interventions, N exp patient population in experimental arm (RAPN), N ctrl patient population in control arm (OPN)