Death and heart problems in diabetes patients starting dialysis who take GLP-1 receptor drugs

TriNetX database, which was recognized as a global health collaborative platform for clinical research, served as the source of data utilized in this study. The broad spectrum of information in this dataset included patient demographics, diagnoses (according to ICD-10-CM codes), procedures (based on ICD-10-PCS or Current Procedural Terminology), medications (coded according to the Veterans Affairs National Formulary), laboratory tests (based on Logical Observation Identifiers Names and Codes), genomics (coded according to the Human Genome Variation Society), and healthcare utilization records from 83 healthcare organizations (HCOs), comprising hospitals, primary care units, and specialized facilities. This platform has already been used in several studies due to its integrity [18, 19]. Based on the database, we constructed a cohort comprising over 2.8 million participants within the period from 1 January 2015 to 1 May 2023, to investigated either GLP-1RAs or long-acting insulin (LAI) treatment efficacy for diabetic patients undergoing acute dialysis. This study followed the Strengthening the Reporting of Observational Studies in Epidemiology (STROBE) reporting guideline for cohort studies.

The examination of TriNetX-derived data garnered institutional approval from the Institutional Review Board of Chi-Mei Hospital (Approval No: 11202-002), as well as endorsement from the respective institutional review boards of all participating hospitals. Adherence to the stipulations outlined in both the Health Insurance Portability and Accountability Act and the General Data Protection Regulation is vigilantly upheld through the mechanisms embedded within the TriNetX platform. Owing to the platform’s exclusive consolidation of de-identified data summaries and counts, it has been accorded an informed consent waiver by the Western Institutional Review Board [20]. The current investigation meticulously adheres to the ethical tenets articulated in the Declaration of Helsinki.

We identified a cohort of 82,041 patients diagnosed with type 2 diabetes and new-onset dialysis at the enrolled healthcare facilities during the study period (Fig. 1). The index date for all participants was 90 days after the initiation of dialysis. The 3-month window helps mitigate reverse causality effects, ensuring outcomes are more attributed to the GLP-1RAs. It also ensures data reliability, as immediate post-discharge records can be inconsistent.

Inclusion criteria were individuals aged 18 to 90 years, with a confirmed diagnosis of type 2 diabetes, and initializing dialysis during their hospital stay. Key exclusion criteria involved patients undergoing dialysis within three months before the commencement of dialysis. To mitigate immortal bias, individuals who had deceased within three months before the index date were also excluded.

Patients were categorized as GLP-1 RA users if they were prescribed a GLP-1 RA at any point within three months after dialysis commencement. Their counterpart was those prescribed LAI at any point within three months at the same timeframe. The cohort was subsequently stratified into two groups: the GLP-1RAs user group (n = 1682), and the LAI user group (n = 32,750).

Subgroup analyses were systematically conducted to scrutinize potential variations in risk associated with the desired outcomes among users of GLP-1RAs. These prespecified analyses took into consideration various factors, including age, hypertension, heart failure, estimated GFR, proteinuria, the enrolled time period, prior history of GLP-1RAs uses before the discharge, enrolment status before or after 2020, utilization of long- or short-acting GLP-1RAs, concurrent usage of other medications for glycemic control, and the use of renin-angiotensin-aldosterone system (RAAS) blockers. GLP-1RAs long-term user was referred to those who had GLP-1RAs treatment chronically before and after the index date. GLP-1RAs ever user was identified as a patient who has ever, at least within 3 months prior to the index date, utilized GLP-1RAs but discontinued the therapy after dialysis commencement. Conversely, a new user was defined as a patient who had never received GLP-1RAs before the index date but initiated its usage thereafter. Free from dialysis was defined as withdrawal from dialysis events within 180 days after the index date, while dialysis-dependent was defined as any presence of dialysis events occurring within 180 days after the index date. Positive/negative outcomes and exposure controls were meticulously delineated to discern the nuanced impact of GLP-1RAs across these specified subgroups.

The primary outcome was mortality, and the secondary outcomes included major adverse cardiac events (MACE) as well as major adverse kidney events (MAKE). We defined MACE as acute MI, coronary artery bypass, cardiac arrest, cerebral infarction, nontraumatic intracerebral hemorrhage, or all-cause mortality, while MAKE was defined as remaining dialysis at 3 years after the index date or all-cause mortality after the index date. All patients were vigilantly monitored for a period of up to 3 years to ascertain the occurrence of the outcomes of interest.

Different covariates were extracted to account for the variables in baseline characteristics between the two groups. Aside from demographic covariates such as age, sex, race, comorbidities, lifestyle, and medication usage were also considered.

To mitigate prospective disparities in baseline characteristics between the two study cohorts, we systematically amalgamated and algorithmically selected a multitude of high-dimensional covariates evaluated within the 12 months preceding the index event. The identification of comorbidities was based on ICD-10-CM codes (Supplementary table). In addition, we concurrently analyzed confounders including body mass index, and systolic blood pressure, as well as laboratory tests which consisted of HbA1c, estimated glomerular filtration rate (eGFR), potassium, total cholesterol, and alanine aminotransferase before dialysis. Short-acting GLP-1RAs were classified as exenatide and lixisenatide, while long-acting agents included liraglutide, dulaglutide, and semaglutide [21].

Variables were presented in either numerical format, accompanied by means and standard deviations, or categorical format, denoted by counts and percentages, contingent upon the characteristics of the covariates. To mitigate potential confounding variables, we leveraged propensity score matching (PSM) to establish comparable groups, systematically pairing each GLP-1 RA user with an LAI user. Adjusted hazard ratios (aHR) were subsequently computed to assess primary and secondary outcomes between the GLP-1RAs user and control groups [22].

This process was facilitated through the integrated feature within TriNetX, utilizing a greedy nearest-neighbor matching approach. The matching algorithm considered factors such as age, gender, race, comorbidities, lifestyle, medications, and laboratory data. The equilibrium of baseline characteristics in the propensity score-matched populations was gauged using absolute standardized mean differences, whereby a value < 0.1 indicated a negligible difference [23]. To circumvent challenges related to multicollinearity, precedence was accorded to continuous variables. Cases with missing data or those lost to follow-up were excluded to ensure data completeness. E-values were calculated for pre-specified outcomes to address the unmeasured confounders [24].

Moreover, we are currently planning a comprehensive subgroup analysis to explore potential variations in treatment effects within distinct subgroups. This endeavor aims to provide more tailored healthcare recommendations, particularly focusing on patients who have either ever or never used GLP-1RAs before initiating dialysis, as well as those who were able to discontinue dialysis due to the resolution of AKI.

To address concerns regarding immortal or ascertainment bias, our series of analyses involved initiating the timeframe on the 14th, 30th, or 60th days post-acute dialysis. Importantly, post-dialysis mortality was not excluded from the cohort and was followed from the first day after acute dialysis as part of the intention-to-treat (ITT) analysis. We computed E-values using the methodology proposed by Vander Weele and Ding [25]. These values serve as a measure to assess the magnitude of the risk ratio required for unmeasured confounding variables to potentially explain the observed disparities between GLP-1 RA users and non-users regarding the outcomes of interest [26].

To mitigate the impact of reverse causality, the observation period commenced from the index date and was extended for a maximum of 3 years. The relationship between GLP-1RAs users and control groups concerning both primary and secondary outcomes was assessed using the Cox proportional hazards model, allowing for the computation of adjusted hazard ratios (aHRs) [22]. Robust standard errors were employed to account for dependence within matched pairs. The assumption of proportional hazards was scrutinized using the generalized Schoenfeld approach on the TriNetX platform. In instances where assumptions were not met, aHRs were determined for specific time frames. Survival probabilities were computed using the Kaplan-Meier method.

Each analysis included a 95% confidence interval, with statistical significance established at a 2-sided P-value < 0.05.

Stratification of the expansive study cohort (n = 82,041) involved allocating individuals to either the GLP-1RAs group (n = 1685, 2.1%) or the LAI control group (n = 32,750), based on the administration of GLP-1RAs or LAI within timeframe spanning of one day to three months subsequent to the index date at dialysis commencement. (Table 1). Among the types, dulaglutide (n = 715, 42.4%) was the most commonly used GLP-1RAs, followed by semaglutide (n = 420, 24.9%) and liraglutide (n = 371, 22.0%). Adhering to this methodological rigor, 1,682 GLP-1 RA users and an equivalent number of LAI users, intricately balanced on pertinent covariates, were purposefully selected for the study. The mean age of the GLP-1RAs group was younger than that of the LAI group (59.3 ± 11.6 vs. 61.8 ± 12.8 years, p < 0.001) (Table 1). Males were the major gender, as well as the White was the predominant race in both groups. The eGFRs in the GLP-1RAs were higher than the LAI group (41.4 ± 36.1 vs. 36.6 ± 37.1 ml/min/1.73m², p < 0.001). After further investigating for the presumptive causes of dialysis commencement, the leading cause was ischemic heart disease (17.2%), followed by heart failure (13.6%) and sepsis (6.5%), with a majority of patients (25.0%) whose baseline kidney function was less than 15 ml/min/1.73m² (Supplementary Table 1).

The overall cohort had a median duration of 1.4 years, bracketed by the 25th percentile at 0.8 years and the 75th at 2.1 years, with the 90th percentile reaching 2.6 years (Supplementary Table 2). The all-cause mortality rate was 6.5% in the GLP-1RAs group and 11.0% in the LAI group, where the GLP‐1RAs group users displayed a significantly diminished risk of all-cause mortality (aHR = 0.63, p < 0.001) (Table 2, Supplemental Table 3). The E-value for the effect of GLP-1RAs on mortality was 2.54 (with a lower bound of 95% CI of 3.41). Additionally, a decreased risk of MACE (aHR = 0.65, p < 0.001), as well as a lower risk of MAKE (aHR = 0.75, p < 0.001) were detected in the GLP‐1RAs group compared to the LAI group (Fig. 2, Supplemental Tables 4, 5). The E-value for the effect of GLP-1RAs on MACE was 2.47 (with a lower bound of 95% CI of 3.33), and on MAKE was 1.75 (with a lower bound of 95% CI of 2.07) (Table 2).

Subgroup analyses were undertaken based on medication usage, comorbidities, body mass index, HbA1c, eGFR, and the utilization of short-acting and long-acting GLP-1RAs (Fig. 3). The results consistently unveiled an association between the use of GLP-1RAs and a reduced risk of mortality, MACE and MAKE, which is particularly noteworthy in patients devoid of proteinuria (aHR = 0.66, p < 0.001), characterized by HbA1C < 7.5% (aHR = 0.55, p < 0.001), and exhibiting BMI ≧ 30 kg/m² (aHR = 0.51, p < 0.001). Remarkably, the salutary impact of GLP-1RAs was accentuated in the context of long-acting GLP-1RAs. However, the association between GLP-1RA use and a decreased risk of mortality and MACEs remained consistent, regardless of different timeframes.

Patients with baseline kidney function better than 15 ml/min/1.73m² obtained significant benefited from GLP-1RAs usage compared to the LAI group [mortality (aHR = 0.57, p < 0.001), MACE (aHR = 0.68, p = 0.011), and MAKE (aHR = 0.77, p = 0.009)], but the benefit was not found in those with kidney function less than 15 ml/min/1.73m² [mortality (aHR = 0.60, p = 0.119), MACE (aHR = 0.89, p = 0.687), and MAKE (aHR = 1.11, p = 0.595)]. Among patients who had GLP-1RAs usage before the index date, the trend was only noted in long-term users [mortality (aHR = 0.57, p = 0.003), MACE (aHR = 0.53, p = 0.001) and MAKE (aHR = 0.69, p = 0.003)]. It is noteworthy that GLP-1RAs new users also exhibited a significantly decreased risk of mortality (aHR = 0.70, p = 0.013), MACE (aHR = 0.74, p = 0.047) and MAKE (aHR = 0.74, p = 0.004) compared to the LAI group. Surprisingly, GLP-1RAs ever users who discontinued the treatment did not show any improvement in mortality (aHR = 0.99, p = 0.967), MACE (aHR = 1.01, p = 0.971) or MAKE (aHR = 1.00, p = 0.995).

GLP-1RAs with an exendin backbone are primarily cleared by the kidneys [27]. Our analysis of this subgroup of GLP-1RAs users, including exenatide did not reveal a significant reduction in mortality (adjusted hazard ratio [aHR] = 0.45, p = 0.154), major adverse cardiovascular events (MACE) (aHR = 0.48, p = 0.193), or major adverse kidney events (MAKE) (aHR = 0.47, p = 0.230) compared to the LAI group (Supplementary Table 6).

Angiotensin-converting enzyme inhibitor (ACEI) or angiotensin II receptor blocker (ARB) use among diabetic patients recovered from dialysis-requiring AKI was associated with a lower risk of ESKD and all-cause mortality [28]. As an extension to the current evidence, a positive outcome analysis was performed and showed a significant reduction of MACE and all-cause mortality among ACEI/ARB users in our study population (Supplementary Table 7, Supplementary Fig. 1).

In order to gain insights into the possibility of discontinuing dialysis, compared to LAI, GLP-1RAs were consistently associated with a decreased risk of all-cause mortality, MACE, and MAKE at various selection periods of 14, 30, 60, and 90 days (Supplementary Table 8). To delineate each component of outcomes of interest, we analyzed mortality as well as MI (aHR = 0.63), heart failure (aHR = 0.73), and stroke (aHR = 0.74). The findings indicate that GLP-1RAs use was independently associated with improved outcomes for all these endpoints.

Of note, in dialysis patients who could withdraw from acute dialysis, defined as being free from dialysis at 180 days after the index date (Fig. 3), akin to the main analysis, GLP-1RAs users were associated with a reduced risk of all-cause mortality (aHR = 0.67, p = 0.004), and MACE (aHR = 0.62, p = 0.001). However, this effect was not observed in patients who continued to be dependent on dialysis.

To investigate the effect of GLP-1RAs on glycemic control, laboratory data of HbA1c were analyzed and showed consistently higher HbA1C levels in the GLP-1 RAs group throughout the study (Supplementary Fig. S2). Additionally, the magnitude of body weight and lipid profile changes among GLP-1RAs and LAI users were analyzed. Though HbA1c and body weight were reduced after treatment, no greater improvement of the lipid profile (low-density lipoprotein, LDL) and systolic blood pressure (SBP) were seen among patients treated with GLP-1RAs compared to LAI (Supplementary Table 9, Figs. S3–S5). Moreover, after dialysis, HbA1C levels and body weight were consistently higher in the GLP-1RAs group compared to the LAI group, indicating that the reduced risk of adverse outcomes associated with GLP-1RAs is not attributable to the “legacy effect”.

We further adjusted for diabetes-related organ injury, such as diabetic retinopathy and neuropathy, as proxies for diabetic severity. The results remained consistent with our main findings [mortality (aHR = 0.56, p < 0.001), MACE (aHR = 0.69, p = 0.001), and MAKE (aHR = 0.76, p < 0.001), Supplementary Table 10], suggesting that the worse outcomes observed in LAI patients were not solely attributable to differences in glycemic control or CVD burden. Additional specificity analyses were performed to compare the efficacy of GLP-1RAs and other second-line antihyperglycemic treatments users (thiazolidinedione (TZD), dipeptidyl peptidase IV inhibitor (DPP4i) or sulfonylureas (SU)), where the results were also consistent with our main finding [mortality (aHR = 0.71, p = 0.005), MACE (aHR = 0.76, p = 0.028), and MAKE (aHR = 0.84, p = 0.031), Supplementary Table 11)].

We utilized patients with gastroparesis and tachycardia as positive outcome controls to assess potential systematic bias [29, 30]. Notably, the risk of gastroparesis (adjusted hazard ratio [aHR] = 1.36, 95% CI = 1.00–1.85, p = 0.047) and tachycardia (aHR = 1.51, 95% CI = 1.00–2.28, p = 0.047) was significantly higher in the GLP-1RAs group (Supplementary Fig. 1). Conversely, incidences of melanoma, traumatic head injury, hernia, GI bleeding, and pneumonia, which were not expected to be linked to GLP‐1RAs use, showed no significant differences between the groups. Moreover, the risk of hypoglycemia among type 2 diabetes patients undergoing acute dialysis did not significantly differ between GLP-1RAs users and LAI users (aHR: 1.33 [0.94–1.88], p = 0.102) (Supplementary Table 12).

GLP-1RAs use was associated with a greater risk reduction in all-cause mortality compared to LAI, in line with contemporary studies that showed outcome improvement after GLP-1RAs use compared to its counterpart in patients with advanced CKD [32]. Moreover, our analysis revealed that the survival benefits of GLP-1RAs persisted regardless of concurrent use of other anti-diabetic agents or RAAS blockers.

The sustained discrepancy in HbA1C levels prompts consideration of the role of glycemic control in the observed reduction of cardiovascular risk associated with GLP-1RAs therapy use in this population, as indicated in the existing literature [33]. The consistent elevation in HbA1C levels among GLP-1RAs recipients throughout the study, suggests pleotropic effect of GLP-1RAs with additional benefits beyond glucose and weight lowering [33].

A clinical trial [FLOW trial, NCT03819153↗] on the efficacy of GLP-1RAs in diabetic patients with CKD showed a 25% reduction in kidney disease progression after GLP-1RAs use [16]. We observed a 25% reduction in the need to continue dialysis within 3 years in the GLP-1RAs group.

GLP-1RAs new use was associated with a substantial improvement in all-cause mortality, MACE, and MAKE, but the beneficial effect was not evident in GLP-1RAs ever users who had terminated treatment after dialysis commencement. It is in line with a study that showed an increased likelihood of major CV events after cessation of GLP-1RAs therapy, irrespective of subjects’ prior CV history [34]. This may also imply an enduring protective effect of GLP-1RAs that did not persist beyond the duration of active administration in AKD patients.

Diabetic management in CKD patients is vexatious as glucose homeostasis and drug excretion are altered as the kidney function declines [35]. Insulin is traditionally the last resort for patients with advanced CKD which permits frequent and precise adjustment for better glycemic control [36]. The emergence of long-acting GLP-1RAs offers an alternative to patients at dialysis commencement who had a limited choice of anti-glycemic agent and a higher risk of hypoglycemia [36]. A pilot study showed the superiority of liraglutide in reducing the hyperglycemic period on both dialysis and non-dialysis days [37]. Another study by Yajima et al. showed that dulaglutide as an add-on therapy to insulin could improve blood glucose levels and daily insulin needs without increasing the risk for hypoglycemia [38]. Similarly, our study showed that the risk of hypoglycemia was not different among the GLP-RAs and insulin users at dialysis commencement.

Nonetheless, the conspicuously minimal utilization of GLP-1RAs among these cohorts highlights the imperative for heightened awareness and adoption of this therapeutic regimen in type 2 diabetes. in the associated survival and cardiorenal effects attributed to GLP-1RAs were independent of concurrent administration of other anti-diabetic agents or RAAS blockers. Furthermore, considering the effects observed future inquiries should study the advantages of GLP-1RAs therapy in populations vulnerable to or convalescing from AKI, encompassing individuals undergoing acute dialysis procedures.

Our study has several limitations to consider. Firstly, this was an observational study with propensity score matching which can substantially reduce baseline differences between groups, but it can never correct for unmeasured confounders; therefore, the study cannot determine cause-and-effect relationships. The limited number of patients (2.1%) initiating dialysis within our study cohort impacts the robustness of our findings. The exact rationale for drug prescription, switching of medications, and drug adherence could not be evaluated. However, the study design was intended for treatment and our analysis tried to ensure consistent results, thereby helping to mitigate the potential for guarantee-time bias or immortal time bias [39]. Furthermore, the diseases and medical conditions were identified via the International Classification of Diseases (ICD) codes. Misclassification of the disease codes and underestimation of the prevalence might happen in real-world conditions. However, to try to mitigate these limitations, we employed validated outcome definitions and PSM. Additionally, we utilized various medications as proxies for disease severity, thereby addressing inherent limitations associated with electronic health records. To assess the impact of potential unmeasured confounding, we conducted an E-value analysis, along with propensity score matching and multivariate Cox proportional analysis incorporating various variables. A higher E-value, surpassing our odd ratio, indicates that only a modest unmeasured confounding variable would be needed to neutralize the estimated effect of the covariates.

Of note, the specificity test evaluating hernia, traumatic head injury, melanoma, pneumonia, and GI bleeding revealed no difference between patients with GLP-1RAs users or LAI in our negative control analysis, aiding in the removal of selection bias that can be caused by existing knowledge of an individual’s assignment. Thus, our findings may not apply to patients who are undergoing long-term dialysis. Given these limitations, a prudent interpretation of our results is advisable, and additional research is warranted to confirm and broaden the scope of our observations. To further validate these findings, large randomized controlled trials focusing on this specific patient population are necessary.

Not applicable.

Not applicable.

The authors declare no competing interests.

No datasets were generated or analysed during the current study.