What this is
- The SURMOUNT-OSA trial evaluated the effects of tirzepatide on cardiometabolic risk factors in participants with obstructive sleep apnea (OSA) and obesity.
- This analysis focuses on secondary outcomes related to changes in blood pressure, inflammatory markers, and lipid profiles.
- Results indicate that tirzepatide significantly improved various cardiometabolic measures compared to placebo, with mediation analysis exploring the roles of weight and OSA metrics.
Essence
- Tirzepatide treatment significantly reduced systolic blood pressure and inflammatory markers in patients with obstructive sleep apnea and obesity compared to placebo. The improvements were mediated by changes in body weight and OSA metrics.
Key takeaways
- Tirzepatide led to a significant reduction in systolic blood pressure, with a change of −7.9 mmHg in study 1 and −4.3 mmHg in study 2 compared to placebo. These reductions suggest potential cardiovascular benefits for patients with OSA.
- The percent change in high-sensitivity C-reactive protein () was significantly reduced by −28.9% in study 1 and −45.1% in study 2 with tirzepatide treatment. This indicates a decrease in inflammation associated with cardiometabolic risk.
- Tirzepatide also significantly improved lipid profiles, with reductions in triglycerides of −32.2% in study 1 and −31.5% in study 2. These changes contribute to a lower risk of cardiovascular complications.
Caveats
- The studies did not have sufficient duration or power to assess long-term cardiometabolic outcomes like myocardial infarction or stroke. Larger studies are needed for definitive conclusions.
- Participants with mild OSA and diabetes were excluded, limiting the generalizability of findings to broader populations with OSA and obesity.
Definitions
- HOMA-IR: Homeostatic Model Assessment for Insulin Resistance, a method to estimate insulin resistance based on fasting insulin and glucose levels.
- hsCRP: High-sensitivity C-reactive protein, a marker of inflammation that can indicate cardiovascular risk.
Simplified
Results
Participants
A total of 469 participants were randomized to receive either tirzepatide or placebo across study 1 (Fig. 1; 234 participants; tirzepatide n = 114, placebo n = 120) and study 2 (Fig. 1; 235 participants; tirzepatide n = 120, placebo n = 115). The full participant disposition can be found in Fig. 1. The baseline characteristics of investigated cardiometabolic risk measures were, in general, comparable between the tirzepatide and placebo groups across both study 1 and study 2 at baseline. The details of the baseline demographics and clinical characteristics can be found in Table 1, some of which have been previously reported13.
Study design flowchart. The data from a previously published study protocol. HbA1c, hemoglobin A1C; MTD, maximum tolerated dose; TZP, tirzepatide. [13]
| Characteristic | Study 1 | Study 2 | ||||
|---|---|---|---|---|---|---|
| Tirzepatide MTD (=114)n | Placebo (=120)n | Total (=234)n | Tirzepatide MTD (=120)n | Placebo (=115)n | Total (=235)n | |
| Age, years | 47.3±11.0 | 48.4±11.9 | 47.9±11.5 | 50.8±10.7 | 52.7±11.3 | 51.7±11.0 |
| Female,(%)n | 36 (31.6) | 41 (34.2) | 77 (32.9) | 33 (27.5) | 32 (27.8) | 65 (27.7) |
| BMI, kgm−2 | 39.7±7.3 | 38.6±6.7 | 39.1±7.0 | 38.6±6.1 | 38.7±6.0 | 38.7±6.0 |
| AHI, events per hour | 52.9±30.5 | 50.1±31.5 | 51.5±31.0 | 46.1±22.4 | 53.1±30.2 | 49.5±26.7 |
| OSA severity,(%)n | ||||||
| No apnea | 0 (0.0) | 1 (0.8) | 1 (0.4) | – | – | – |
| Mild | 1 (0.9) | 2 (1.7) | 3 (1.3) | 0 (0.0) | 2 (1.8) | 2 (0.9) |
| Moderate | 39 (34.2) | 43 (36.1) | 82 (35.2) | 35 (29.4) | 37 (32.5) | 72 (30.9) |
| Severe | 74 (64.9) | 73 (61.3) | 147 (63.1) | 84 (70.6) | 75 (65.8) | 159 (68.2) |
| SASHB, %min h(CV (%))−1† | 153.6 (102.7) | 137.8 (104.1) | 145.3 (103.4) | 132.2 (83.4) | 142.1 (112.5) | 137.0 (97.5) |
| SBP, mmHg | 128.2±11.9 | 130.3±10.8 | 129.3±11.4 | 130.7±14.2 | 130.5±12.8 | 130.6±13.5 |
| DBP, mmHg | 83.7±8.9 | 83.9±8.7 | 83.8±8.8 | 83.2±8.1 | 80.5±8.6 | 81.9±8.5 |
| hsCRP, mg l(CV (%))−1† | 3.6 (120.0) | 3.8 (110.7) | 3.7 (115.1) | 3.0 (124.2) | 2.7 (123.4) | 2.8 (123.6) |
| HDL-C, mmol l(CV (%))−1† | 1.1 (23.3) | 1.2 (23.4) | 1.1 (23.4) | 1.1 (20.8) | 1.2 (27.3) | 1.1 (24.1) |
| Non-HDL-C, mmol l(CV (%))−1† | 3.8 (29.6) | 3.7 (24.3) | 3.7 (27.1) | 3.8 (24.0) | 3.5 (26.1) | 3.7 (25.2) |
| Triglycerides, mmol l(CV (%))−1† | 1.7 (59.8) | 1.7 (51.0) | 1.7 (55.4) | 1.7 (43.5) | 1.7 (52.2) | 1.7 (47.5) |
| Fasting insulin, mU l(CV (%))−1† | 22.8 (89.0) | 17.9 (60.0) | 20.3 (76.5) | 17.9 (64.9) | 20.8 (72.9) | 19.1 (69.1) |
| HbA1c (%) | 5.7±0.4 | 5.6±0.4 | 5.7±0.4 | 5.6±0.4 | 5.7±0.4 | 5.6±0.4 |
| HOMA-IR (CV (%))† | 5.6 (104.7) | 4.4 (63.8) | 5.0 (86.3) | 4.5 (67.1) | 5.1 (80.1) | 4.7 (73.4) |
| Hypertension,(%)n | 84 (73.7) | 93 (77.5) | 177 (75.6) | 91 (75.8) | 91 (79.1) | 182 (77.4) |
| Prediabetes,(%)n | 74 (64.9) | 78 (65.0) | 152 (65.0) | 69 (57.5) | 64 (55.7) | 133 (56.6) |
Changes in cardiometabolic risk measures
The SURMOUNT-OSA statistical analysis plan prespecified assessment of changes in SBP and DBP, hsCRP, HDL-C, non-HDL-C, LDL-C, VLDL-C and fasting insulin. The changes in HOMA-IR were analyzed post hoc.
Changes in SBP and DBP were assessed at week 48 to prevent confounding effect of PAP discontinuation at week 52 in study 2, all other changes were assessed at week 52.
There was a significant estimated treatment difference (ETD) between tirzepatide and placebo for change in SBP from baseline at week 48 both in study 1 (−7.9 mmHg; 95% confidence interval (CI) −11.0 to −4.9; P < 0.001) and in study 2 (−4.3 mmHg; 95% CI −7.3 to −1.2; P = 0.007). The ETD between tirzepatide and placebo of change in DBP from baseline at week 48 was significant in study 1 (−3.2 mmHg; 95% CI −5.4 to −1.0; P = 0.005) but not in study 2 (Table 2).
The ETD between tirzepatide and placebo for percent change in hsCRP from baseline at week 52 was significant both in study 1 (−28.9% ± 8.2%; P = 0.003) and in study 2 (−45.1% ± 8.0%; P <0.001) (Table 2).
The ETD between tirzepatide and placebo for percent change in HDL-C from baseline at week 52 was significant both in study 1 (7.2% ± 2.1%; P < 0.001) and in study 2 (10.0% ± 2.8%; P < 0.001). The ETD between tirzepatide and placebo for percent change in non-HDL-C from baseline at week 52 was significant both in study 1 (−13.0% ± 3.1%; P < 0.001) and in study 2 (−14.3% ± 2.5%; P < 0.001). The ETD between tirzepatide and placebo for percent change in triglycerides from baseline at week 52 was significant both in study 1 (−32.2% ± 3.8%; P < 0.001) and in study 2 (−31.5% ± 3.7%; P < 0.001) (Table 2).
The ETD between tirzepatide and placebo for percent change in LDL-C from baseline at week 52 was not significant in study 1 but was significant in study 2 (−10.3% ± 3.0%; P = 0.001). The ETD between tirzepatide and placebo for percent change in VLDL-C from baseline at week 52 was significant both in study 1 (−32.6% ± 3.7%; P < 0.001) and in study 2 (−31.4% ± 3.7%; P < 0.001) (Table 2).
The ETD between tirzepatide and placebo for percent change in fasting insulin from baseline at week 52 was significant both in study 1 (−41.4% ± 5.0%; P < 0.001) and in study 2 (−45.4% ± 5.4%; P < 0.001). The ETD between tirzepatide and placebo for percent change in HOMA-IR from baseline at week 52 was significant both in study 1 (−48.0% ± 4.9%; P < 0.001) and in study 2 (−54.5% ± 5.0%; P < 0.001) (Table 2).
| Study 1 | Study 2 | |||||
|---|---|---|---|---|---|---|
| Tirzepatide | Placebo | ETD | Tirzepatide | Placebo | ETD | |
| Change in SBP (mmHg) from baseline at week 48 | −9.6±1.1 9 | −1.7±1.1 | −7.9 (−11.0 to −4.9) 9 † | −7.6±1.1 9 | −3.3±1.2 8 | −4.3 (−7.3 to −1.2) 8 † |
| Change in DBP (mmHg) from baseline at week 48 | −5.2±0.8 9 | −2.0±0.8 7 | −3.2 (−5.4 to −1.0) 8 † | −3.0±0.7 9 | −1.8±0.8 7 | −1.2 (−3.4 to 0.9)† |
| Percent change in hsCRP from baseline at week 52 | −44.2±4.4 9 | −21.4±6.6 8 | −28.9±8.2 8 | −50.7±4.8 9 | −10.4±9.8 | −45.1±8.0 9 |
| Percent change in HDL-C from baseline at week 52 | 10.6±1.5 9 | 3.1±1.5 7 | 7.2±2.1 9 | 15.0±2.0 9 | 4.5±2.0 7 | 10.0±2.8 9 |
| Percent change in non-HDL-C from baseline at week 52 | −15.0±2.1 9 | −2.3±2.5 | −13.0±3.1 9 | −15.8±1.6 9 | −1.8±2.1 | −14.3±2.5 9 |
| Percent change in triglycerides from baseline at week 52 | −32.9±2.6 9 | −1.0±4.0 | −32.2±3.8 9 | −35.2±2.3 9 | −5.4±3.8 | −31.5±3.7 9 |
| Percent change in LDL-C from baseline at week 52 | −8.9±2.7 8 | −4.3±3.0 | −4.8±4.2 | −10.2±2.0 9 | 0.0±2.5 | −10.3±3.0 8 |
| Percent change in VLDL-C from baseline at week 52 | −32.4±2.5 9 | 0.3±3.9 | −32.6±3.7 9 | −34.9±2.3 9 | −5.0±3.8 | −31.4±3.7 9 |
| Percent change in fasting insulin from baseline at week 52 | −44.2±3.3 9 | −4.7±5.9 | −41.4±5.0 9 | −48.5±3.4 9 | −5.6±6.9 | −45.4±5.4 9 |
| Percent change in HOMA-IR from baseline at week 52 | −51.2±3.2 9 | −6.2±6.4 | −48.0±4.9 9 | −55.8±3.3 9 | −2.7±7.9 | −54.5±5.0 9 |
Mediation analysis
Mediation analysis was performed to estimate the proportion of tirzepatide treatment-associated changes in cardiometabolic risk measures due to either an effect of weight reduction or an effect of changes in sleep-disordered breathing measured by AHI and SASHB.
In a pooled study 1 and study 2 population, the tirzepatide effect on SBP was significantly mediated by combined effect of changes in body weight, AHI and SASHB, and by change in body weight alone. However, the proportion mediated by changes in OSA metrics, AHI and SASHB alone, was not statistically significant (Fig. 2).
The proportions of tirzepatide-associated change in DBP mediated by combined effect of changes in body weight, AHI and SASHB or effects of any of the mediators alone were not statistically significant (Fig. 2).
The tirzepatide-associated change in hsCRP was significantly mediated by combined effect of changes in body weight, AHI and SASHB, by change in body weight alone and by changes in OSA metrics AHI and SASHB (Fig. 2).
The tirzepatide-associated change in triglycerides was significantly mediated by combined effect of changes in body weight, AHI and SASHB, by change in body weight alone and by changes in OSA metrics AHI and SASHB (Fig. 2).
The tirzepatide-associated change in HDL-C was significantly mediated by combined effect of changes in body weight, AHI and SASHB and by change in body weight alone. However, the proportion mediated by change in OSA metrics AHI and SASHB was not statistically significant (Fig. 2).
The tirzepatide-associated change in non-HDL-C was significantly mediated by combined effect of changes in body weight, AHI and SASHB. However, the proportions mediated by change in body weight alone, or mediated by change in OSA metrics, AHI and SASHB, were not statistically significant (Fig. 2).
The tirzepatide-associated change in HOMA-IR was significantly mediated by combined effect of changes in body weight, AHI and SASHB, by change in body weight alone and by change in OSA metrics AHI and SASHB (Fig. 2).
Proportion of tirzepatide effect on cardiometabolic risk measures mediated by body weight, AHI and SASHB. The data are presented as model-based estimate for the mean (95% CI). Statistical analyses were performed using the bootstrap method. All hypothesis testing was conducted using a two-sided framework, and the results are summarized with 95% CIs, which were derived from the corresponding 2.5th and 97.5th percentiles of the bootstrapped estimates (HOMA-IR= 336; non-HDL-C= 341; HDL-C= 342; triglycerides= 341; hsCRP= 342; DBP= 364; SBP= 364). *< 0.05, **< 0.01, ***< 0.001 representing significant proportion mediated. n n n n n n n P P P
Discussion
In this study, we observe marked improvements in cardiometabolic risk measures with tirzepatide therapy compared with placebo. These included previously reported improvements in SBP, DBP and hsCRP13, as well as improvements in the lipid profile, fasting insulin and HOMA-IR. The improvements in cardiometabolic risk measures were both statistically significant and clinically meaningful and, therefore, tirzepatide treatment may lead to improvement in overall cardiometabolic risk in patients with OSA and obesity. The mediation analysis determined that changes in AHI and SASHB significantly mediated reductions in hsCRP, HOMA-IR and triglycerides, but notably, there was no positive mediation of AHI and SASHB observed on SBP and DBP.
The optimal treatment for patients with OSA and obesity has been unclear. Chirinos et al. reported a comparison of the impact of PAP therapy versus lifestyle weight-loss intervention versus the combination of both treatment approaches7. The results, in aggregate, support that treating both OSA as well as obesity may be the optimal treatment, with the awareness and acknowledgment that weight reduction in and of itself mitigates OSA. Of note, randomized trials so far have not demonstrated significant effect of PAP therapy on major cardiovascular outcomes6,15–19. The reasons for these findings are unclear, but several potential explanations have been proposed. First, adherence to PAP therapy can be quite variable with major improvements expected only in those with excellent adherence to PAP therapy. Indeed, a recent meta-analysis reported improved cardiometabolic outcomes in patients with OSA who had optimal PAP adherence20. Second, the stratification of patients with OSA for participation in randomized controlled trials may be needed to account for cardiometabolic risk. Cluster analyses have suggested that only a subset of patients with OSA may be at major cardiometabolic risk, and thus, randomized controlled trials may need to identify high risk patients a priori rather than the typical one-size-fits-all approach21,22. Ongoing efforts using endotyping techniques may help to identify patients most likely to benefit from various interventions in the design of future randomized trials23. Third, the lack of observed improvement in outcomes in randomized trials of PAP therapy for OSA in the light of success of bariatric surgery in improving cardiovascular outcomes24 may also reflect the failure of some trials to address underlying causes of OSA, such as obesity. In fact, some randomized studies have shown small but significant increases in body weight with PAP therapy, which emphasizes the need to address both OSA and obesity rather than either condition alone25. The results from our analyses of SURMOUNT-OSA provide a compelling rationale that improvements in OSA metrics appear to be associated with benefits in addition to those observed by weight reduction. We observed statistically significant independently mediated reductions by OSA metrics in hsCRP, HOMA-IR and triglycerides. In addition, the combination of weight with OSA metrics, but not weight or OSA improvements alone, significantly mediated reductions in non-HDL cholesterol. Of note, the mediation effect of weight on SBP appears to be larger than that for weight and OSA combined, and AHI/SASHB did not show any mediation effect alone. None of our variables were significant mediators of the improvement seen in DBP, suggesting that there may be other unrecognized variables contributing to cardiometabolic benefit with tirzepatide therapy for comorbid obesity and OSA. The implication for clinical practice is that treatment of OSA in patients with OSA and obesity should always include obesity treatment, and medications such as tirzepatide may represent a therapeutic option for such patients. Therapy of OSA in patients with obesity may be initiated by PAP and tirzepatide, with evaluation of PAP therapy continuation being done based on the treatment effect of tirzepatide therapy26.
Notably, the finding that the observed improvement in SBP with tirzepatide therapy was significantly mediated only via obesity or the combined effect of body mass index/AHI/SASHB changes but not by independent improvement in OSA was surprising, given the extensive literature on the impact of OSA on SBP. Considerable data from large epidemiological studies and human interventional studies have shown a modest but significant impact of OSA on SBP27–30. One potential explanation may be that the point estimate for weight may have less variance than the estimate for AHI, given the night-to-night variability in sleep apnea31,32. Indeed, a recent study suggested that multinight recordings of sleep apnea were required to capture a large percentage of the variance in blood pressure33. Though study 1 and study 2 were not designed for direct comparison between PAP and non-PAP participants, the results indicate that for participants in study 2, who were on PAP, the improvement in OSA with tirzepatide did not yield the same benefits on both SBP and DBP as for participants who were not on PAP, as PAP may have already improved SBP at baseline. Thus, the findings should not weaken the perception of an important role of OSA treatment in blood pressure control confirmed by previous studies34,35.
The mediation analysis compared the effect of tirzepatide on cardiometabolic risk factors through its impact on weight and on OSA severity without reflecting on a possible direct effect of tirzepatide on these factors. The metabolic effect of GLP-1 and GLP-1/GIP receptor agonists appears to integrate their direct effect on pancreatic islet function with long-term weight reduction that increases insulin sensitivity and reduces beta-cell workload in persons with prediabetes and obesity36. Animal models have shown that GLP-1 receptor agonists may ameliorate excessive sympathetic activity in the hypertensive-diabetic condition37. In addition, GIP receptor agonism, specific for tirzepatide, has been shown to have a direct effect on insulin sensitivity and lipid metabolism38. Future research is needed to explore direct effects of tirzepatide on cardiometabolic risk in the realms of OSA as well as mechanisms of its effect on AHI, SASHB and other measures attributed to OSA.
The studies and analysis have a number of strengths. The studies bring results of prespecified endpoints from prospective, controlled, randomized trials. The existing evidence of the relationship between OSA and CVD is largely based on retrospective analyses and, therefore, prospective randomized trial data are necessary to prove some of the concepts created. The mediation analysis of the pooled data from these prospective studies investigates how weight reduction and OSA alleviation improved cardiometabolic risk measures independently, controlling for confounders. This analysis has also provided the size of these effects, and the findings may represent important information for clinical decision making on therapy of patients with OSA and obesity. Despite the strengths of the studies, we acknowledge a number of limitations. First, the studies did not have sufficient duration of follow-up or statistical power to examine the impact of tirzepatide on cardiometabolic outcomes such as myocardial infarction or stroke. Larger studies with longer follow-up may be required to prove that tirzepatide has benefits on these outcomes of interest in patients with OSA and obesity. Second, the SURMOUNT-OSA study excluded people with mild OSA, as well as those with diabetes, and with body mass index <30 kg m−2. Emerging data suggest that treatment with tirzepatide or GLP-1 receptor agonists results in less weight reduction in patients with type 2 diabetes than in those without diabetes12,39. More data are required to determine which patients with OSA are most likely to benefit from tirzepatide.
In SURMOUNT-OSA, tirzepatide mitigated cardiometabolic risk for patients with moderate-to-severe OSA and obesity. Presented results provide support for the concept that treating both OSA and obesity in patients with a combination of both diseases is required to optimize cardiometabolic benefits. Further work is required to determine which patients with OSA benefit the most from different therapeutic approaches.
Methods
Study design, procedures and participants
The SURMOUNT-OSA program included two 52-week, randomized, placebo-controlled phase 3 studies. Study 1 included participants who were unwilling or unable to use PAP therapy, and study 2 included participants who had been using PAP therapy for at least 3 months at screening, and who planned to continue PAP for the duration of the trial. Participants were randomly assigned in a 1:1 ratio to receive either tirzepatide at the maximum tolerated dose (10 or 15 mg) or placebo once weekly. The SURMOUNT-OSA program was registered at ClinicalTrials.gov↗ (NCT05412004↗), and the two studies’ full design, key eligibility criteria, procedures and primary efficacy and safety results have been published previously13,14. Participants were screened and enrolled irrespective of their sex. Sex was self-reported by participants.
Objectives
First, this analysis investigated the association of tirzepatide with changes in cardiometabolic risk markers in participants with moderate-to-severe OSA and obesity. Second, the analysis estimated the relative contribution of weight loss, AHI and SASHB reduction to the improvement in cardiometabolic characteristics of subjects treated with tirzepatide.
Parameters measured included change from baseline in SBP, DBP and levels of hsCRP, HDL-C, non-HDL-C, triglycerides, LDL-C, VLDL-C, fasting insulin and HOMA-IR, in tirzepatide versus placebo.
Mediation analysis was performed to estimate the proportion of tirzepatide treatment-associated changes in cardiometabolic risk measures due to either an effect of weight reduction or an effect of changes in sleep-disordered breathing measured by AHI and SASHB. SASHB is a cumulative measure of oxygen desaturation associated with apneas and hypopneas which, in observational studies, predicted OSA-related cardiovascular mortality and morbidity better than AHI40,41.
For each cardiometabolic risk measure, three analyses were performed: estimation of the proportion of efficacy mediated by change from baseline in body weight, change from baseline in AHI and SASHB and, lastly, change from baseline in all three mediators combined.
Improvements in these mediators with tirzepatide treatment compared with placebo from SURMOUNT-OSA studies have been previously published and are as follows:
ETD between tirzepatide and placebo in study 1 was −16.1% (95% CI −18.0 to −14.2) for body weight, −20.0 events per hour (95% CI −25.8 to −14.2) for AHI and −70.1%min h−1 (95% CI −90.9 to −49.3) for SASHB13. ETD between tirzepatide and placebo in study 2 was −17.3% (95% CI −19.3 to −15.3) for body weight, −23.8 events per hour (95% CI −29.6 to −17.9) for AHI and −61.3%min h−1 (95% CI −84.7 to −37.9) for SASHB13.
Statistical analysis
Changes in SBP, DBP and hsCRP from SURMOUNT-OSA have already been reported using treatment-regimen estimand analysis13. The analyses reported here were guided by the ‘efficacy’ estimand; the analysis included data collected before permanent discontinuation of study intervention and was conducted using the efficacy analysis set. For efficacy analysis, missing values were imputed using multiple imputation based on the reason of intercurrent events. All results are reported using the efficacy estimand unless otherwise specified.
Unless otherwise noted, all tests of treatment effects were conducted at a two-sided alpha level of 0.05, and the CIs were calculated at 95%. In statistical summaries and analyses, participants were analyzed as randomized.
The mixed model repeated measures analysis, a restricted-maximum-likelihood-based model, was used to analyze continuous longitudinal variables. All the longitudinal observations at each scheduled postbaseline visit were included in the analysis. The model includes the fixed class effects of treatment, strata (pooled country/geographic region, baseline OSA severity and gender), visit and treatment-by-visit interaction, as well as the continuous, fixed covariate of baseline value. The significance tests were based on least-squares means and type III tests. As all of these endpoints were exploratory in nature, the P values were not adjusted for multiplicity. Statistical analyses were performed using SAS version 9.3.
Mediation analyses were conducted to decompose the total effect of tirzepatide on cardiometabolic risk markers into direct effect and indirect effect. The direct effect quantified the effect of tirzepatide versus placebo on change in cardiometabolic outcomes, independent of changes in mediators. Conversely, the indirect effect captured the effect of tirzepatide versus placebo on change in cardiometabolic outcomes associated with changes in mediators. Because these comparisons involve non-observable counterfactual scenarios, natural effect models were employed to estimate the direct and indirect effects42. The total effect was defined as the sum of these two components. The proportion mediated was calculated as the indirect effect divided by the total effect then multiplying by 100%, and the standard errors were derived using the bootstrap method. The mediation analyses were performed on the pooled study 1 and study 2 populations. The outcome was the change in cardiometabolic risk measure from baseline to the end of the study. Analyses on SBP and DBP were performed on the original scale, and analyses on hsCRP, HDL-C, non-HDL-C, triglycerides and HOMA-IR were performed on the log scale. Baseline covariates included region, sex, baseline cardiometabolic risk measure, AHI, body weight and log-transformed SASHB. We investigated the effects of mediators for three scenarios: first, a single mediator of change from baseline in body weight; second, two independent mediators of change from baseline in AHI and change from baseline in SASHB to represent changes attributable to OSA severity improvement; and lastly, a combination of the effect of changes in body weight, AHI and SASHB as three parallel mediators. The post-treatment confounders were controlled for and included change in AHI and SASHB when the mediator was change from baseline in body weight and change in body weight when the mediator was change from baseline in AHI and SASHB. No post-treatment confounders were controlled for when all of the change from baseline in body weight, AHI and SASHB were mediators. Log transformation was always applied for SASHB. The mediation analyses were performed using the ‘CMAverse’ package version 0.1.0 in R version 4.1.2 (ref. 42).
Pearson’s correlation coefficients were also calculated between the cardiometabolic risk measures and the sleep-disordered breathing parameters on the pooled study 1 and study 2 populations. Analyses on SBP and DBP were performed on the original scale, and analyses on hsCRP, HDL-C, non-HDL-C, triglycerides and HOMA-IR were performed on the log scale. These results are presented in Extended Data Table 1.
Ethics and informed consent
The study was approved by ethics review boards at each site, presented in. Supplementary Table 1
This study was conducted in accordance with consensus ethical principles derived from international guidelines including the Declaration of Helsinki and Council for International Organizations of Medical Sciences International Ethics Guidelines, applicable ICH GCP Guidelines, International Organization for Standardization (ISO) 14155 and applicable laws and regulations.
Participants or their legally authorized representatives signed a statement of informed consent that meets the requirements of 21 Code of Federal Regulations 50, local regulations, ICH guidelines, privacy and data protection requirements, where applicable, and the IRB/IEC or study center.
Reporting summary
Further information on research design is available in the Nature Portfolio Reporting Summary linked to this Article.
Extended Data
| AHI | Body Weight | log(SASHB) | |
|---|---|---|---|
| SBP | 0.11 10 | 0.29 12 | 0.12 10 |
| DBP | 0.08 | 0.17 11 | 0.13 10 |
| hsCRP | 0.27 12 | 0.37 12 | 0.38 12 |
| HDL-C | −0.18 12 | −0.29 12 | −0.30 12 |
| Non-HDL-C | 0.25 12 | 0.35 12 | 0.28 12 |
| Triglycerides | 0.34 12 | 0.47 12 | 0.36 12 |
| HOMA-IR | 0.38 12 | 0.53 12 | 0.4 12 |
Supplementary Material
Supplementary information The online version contains supplementary material available at https://doi.org/10.1038/s41591-025-04071-1↗.
Acknowledgements
We thank the participants, the study teams and the investigators. We thank S. Curley, PhD (Eli Lilly and Company) for editorial assistance. This study was funded by Eli Lilly and Company. The study sponsor had a role in the study design, data collection, data analysis, interpretation of data, writing of the report and the decision to submit the paper for publication.
Footnotes
Data availability
Data from the analyses in this study cannot be shared publicly due to the sponsor’s (Eli Lilly and Company) contractual obligations. Lilly provides access to all individual participant data collected during the trial, after anonymization, with the exception of pharmacokinetic or genetic data. Data are available to request 6 months after the indication studied has been approved in the USA and European Union and after primary publication acceptance, whichever is later. No expiration date of data requests is currently set once data are made available. Access is provided after a proposal has been approved by an independent review committee identified for this purpose and after receipt of a signed data sharing agreement. Data and documents, including the clinical study report, blank or annotated case report forms, will be provided in a secure data sharing environment. For details on submitting a request, see the instructions provided at www.vivli.org↗. Contact the corresponding author for details on submitting a request. Source data are provided with this paper.
Code availability
No novel code was used for data analysis in the current study.
References
Associated Data
Supplementary Materials
Data Availability Statement
Data from the analyses in this study cannot be shared publicly due to the sponsor’s (Eli Lilly and Company) contractual obligations. Lilly provides access to all individual participant data collected during the trial, after anonymization, with the exception of pharmacokinetic or genetic data. Data are available to request 6 months after the indication studied has been approved in the USA and European Union and after primary publication acceptance, whichever is later. No expiration date of data requests is currently set once data are made available. Access is provided after a proposal has been approved by an independent review committee identified for this purpose and after receipt of a signed data sharing agreement. Data and documents, including the clinical study report, blank or annotated case report forms, will be provided in a secure data sharing environment. For details on submitting a request, see the instructions provided at www.vivli.org↗. Contact the corresponding author for details on submitting a request. Source data are provided with this paper.
No novel code was used for data analysis in the current study.