What this is
- Bariatric surgery effectively treats obesity in patients with type 2 diabetes mellitus (T2DM) requiring insulin.
- This study evaluates clinical outcomes and cost-effectiveness of bariatric surgery compared to best medical treatment (BMT).
- Data from the National Bariatric Surgical Registry was used to analyze insulin cessation rates and economic implications over five years.
Essence
- Bariatric surgery leads to a high rate of insulin cessation in patients with obesity and T2DM requiring insulin, resulting in lower overall healthcare costs compared to best medical treatment over five years.
Key takeaways
- 67% of patients no longer required insulin one year post-bariatric surgery, with rates remaining high for four years. This underscores the surgery's effectiveness in managing T2DM.
- Bariatric surgery was associated with lower total costs (GBP£22,057) compared to BMT (GBP£26,286) over five years, yielding a cost saving of GBP£4,229. This finding emphasizes the economic benefits of surgical intervention.
- Roux-en-Y gastric bypass (RYGB) had a higher insulin cessation rate (71.7%) compared to sleeve gastrectomy (64.5%) and adjustable gastric band (33.6%). This indicates that surgical choice impacts diabetes management outcomes.
Caveats
- Loss to follow-up in the National Bariatric Surgical Registry may affect the reliability of long-term outcomes. However, the follow-up rates are comparable to other national studies.
- The economic analysis was limited to a five-year horizon, which may not capture long-term cost-effectiveness of bariatric surgery.
- The study did not include detailed medication dosages before and after surgery, potentially underestimating the impact of surgery on diabetes management.
Definitions
- T2DM-Ins: Type 2 diabetes mellitus requiring insulin treatment.
- QALY: Quality-adjusted life year, a measure of disease burden that considers both the quantity and quality of life.
Simplified
Introduction
Over the last decade, bariatric surgery has been shown to be an effective treatment for type 2 diabetes mellitus (T2DM) in patients with obesity [1,2]. Surgery is associated with superior improvement in hyperglycaemia as compared to best medical treatment (BMT), an effect that is sustained for at least 5 years [3–6]. The improvement in hyperglycaemia is associated with a reduction in mortality [7,8] and diabetes-related complications [9,10]. Improvement in T2DM following bariatric surgery is mediated by both weight loss–dependent and weight loss–independent mechanisms [11,12].
T2DM is, however, a progressive, heterogenous disorder with a spectrum of severity [13,14]. To date, the major randomised controlled trials investigating the clinical outcomes of bariatric surgery for T2DM have focused predominantly on patients with more recent onset disease not requiring insulin, as opposed to patients with disease of longer duration requiring insulin [3,4]. To date, there has only been one study, a regional registry analysis, focused on patients who require insulin for their T2DM [15]. A number of retrospective studies have analysed the factors associated with successful diabetes remission following bariatric surgery [16–18]. These studies suggest that patients with more severe T2DM (defined as requiring insulin treatment and/or of long duration) are less likely to experience sustained remission of hyperglycaemia following bariatric surgery. These disappointing findings may explain reluctance in some settings towards surgical treatment for patients with obesity and longer standing T2DM requiring insulin (T2DM-Ins): the national commissioning guidelines in Scotland, for example, permit referral for bariatric surgery only for patients with new-onset T2DM (less than 5 years) [19].
In addition to the clinical benefits of bariatric surgery for individual patients with obesity and T2DM, a number of studies have analysed the healthpayer costs of bariatric surgery [20–22]. Although these studies suggest that surgery is cost-effective as compared to medical management, to date no economic evaluations focus on patients with T2DM-Ins. Moreover, many of these existing economic analyses predate the wide-scale adoption of newer antidiabetic medications such as glucagon-like peptide 1 receptor agonists (GLP-1 RA) and sodium-glucose transport protein 2 (SGLT2) inhibitors—medications which have recently changed the landscape of treatment for patients with more severe T2DM [23]. Though effective, these new medications have significant cost implications. There is a need, therefore, to investigate the clinical outcomes of bariatric surgery in a large cohort of patients with T2DM-Ins and evaluate the cost-effectiveness of a surgical strategy in this cohort.
The purposes of this study were two-fold: firstly, to evaluate clinical outcomes following bariatric surgery in patients with obesity and T2DM-Ins using a UK registry dataset which represents the largest cohort published to date; and secondly, to combine the data with other relevant sources to develop a model-based economic evaluation to assess the cost and cost-effectiveness of bariatric surgery versus BMT in this cohort.
Methods
The clinical study analysis and cost-effectiveness study framework were planned at the time of study conception, although no formal prospective analysis plan was recorded. For the clinical study, this included the variables that would be adjusted for during regression analysis. For the cost-effectiveness analysis, the model was designed, and data inputs agreed prior to running the model: these data inputs would include those derived from previous studies as well as the present clinical study. After the base case model had been run, and in response to peer reviewers’ comments, three alternative scenario analyses were additionally constructed and run: two for different ethnicities and one with an adjusted hypoglycaemia rate in the BMT group (see). This study is reported as per the Consolidated Health Economic Evaluation Reporting Standards (CHEERS) guideline (Checklist). S1 Text S1 CHEERS
Design of the clinical study
Data source and study population
To evaluate the clinical outcomes of patients with obesity and severe T2DM, as well as prognostic factors predictive of clinical outcomes, we extracted data from the National Bariatric Surgical Registry (NBSR). The NBSR is a bespoke database for the prospective collection of demographic, perioperative, and clinical outcome data for patients with obesity undergoing bariatric surgery in the UK and Republic of Ireland [24]. The details of the demographic and clinical data recorded in this database as well as the data quality are detailed in previous publications [25,26]. Fully anonymised data were extracted from the registry from patients that had previously consented to the collection of their data.
Diabetes status in NBSR is recorded preoperatively and at every postoperative visit as follows: no indication of T2DM; impaired glycaemia or impaired glucose tolerance (diet controlled); oral hypoglycaemics only; or insulin treatment (insulin with or without additional hypoglycaemic medications). As insulin use has consistently been identified as a strong negative predictor of remission of T2DM after bariatric surgery [16–18], we focused on patients that were using insulin for T2DM preoperatively (T2DM-Ins).
From the database, we identified all patients with T2DM-Ins who had undergone primary Roux-en-Y gastric bypass (RYGB), sleeve gastrectomy (SG), or adjustable gastric band (AGB) between 1 January 2009 and 31 May 2017. As the majority of patients have several follow-up episodes recorded on NBSR, data were selected as follows: for outcomes at 1 year, only patients with a follow-up appointment between 6- and 24-months post-surgery were included, and data were extracted from the clinic appointment closest to the 1-year point after surgery; for longer-term outcomes, data were extracted from the final recorded clinic appointment, with exclusion of any patients with less than 2 years’ follow-up. For diabetes status over time, all patients with any follow-up visit were included.
Ethics statement
The data holder NBSR complied with local ethics guidelines and use of this dataset for research purposes conformed with UK legislation and was approved by the Health Research Authority (17/CAG/0023).
Analytical approach
Data are presented as mean with standard deviation or number with percentage of total in parentheses.
Percent weight loss (%WL) was calculated as percent of total weight lost using the following formula:
Percent excess weight loss (%EWL) was calculated based on an optimum body mass index (BMI) of 25 kg/m2, using the following formula:
Comparison of baseline factors and outcomes by procedure was initially carried out by analysis of variance (means), quantile regression (medians), or chi-squared tests as appropriate. Further adjusted comparison of factors predicting insulin cessation following surgery were made using Poisson regression to generate relative risk (RR) ratios, 95% confidence intervals (CIs) and p-values using PROC GENMOD, SAS software version 9.4 (SAS Institute Inc., Cary, North Carolina, United States of America). Robust standard errors were estimated accounting for clustering by hospital, and an offset term was included based on follow-up time. For procedure type, RYGB was chosen as the reference category. Baseline factors used for adjustment were age, gender, initial BMI, smoking, number of comorbidities, duration of diabetes, and ethnicity. Additionally, further models adjusted for postoperative change in weight (with initial BMI removed), in order to assess any potential contributions to improvement in T2DM mediated through weight loss–independent mechanisms of the different operations. This analysis was included because it has been demonstrated that some bariatric procedures (such as RYGB) may be associated with greater weight loss–independent improvements in T2DM as compared to others [11,12]. Age and weight-related variables (BMI, weight loss, and excess weight loss) are presented within categories, but additional models were fitted with them as continuous variables.
Design of the health economic model
We developed a model-based management protocol in order to compare the costs and effects of a strategy of surgical intervention versus BMT for patients with obesity and T2DM-Ins, over a 5-year timeline horizon. As detailed in full in, individual patients with T2DM-Ins were simulated based on characteristics from the UK NBSR dataset and then duplicated to create an identical clone. In the model, one clone was treated with BMT, while the other was treated with bariatric surgery. This strategy ensures that the treatment comparisons are not being influenced by differences in patient characteristics but only based on the treatments received. Each clone or “patient” was then put through the model, and the costs and health outcomes were amassed for all patients in each treatment arm. The model is developed as a state-transition patient-level simulation with 1-year cycle length. S1 Text
Model inputs
The data from the NBSR as presented in this paper were utilised to inform baseline patient characteristics for the population (see “Model Inputs,”). S1 Text
For the purposes of this evaluation, given the inferior efficacy of AGB when compared to RYGB and SG in T2DM improvement (see results below), we modelled that patients in the surgical group would only undergo either RYGB or SG. We assumed, based on recent UK procedure prevalence data [27], that 58% would undergo RYGB and 42% SG.
The BMT regimen (which includes nutritional counselling) was determined from the latest guidelines from the American Diabetes Association and European Association for Study of Diabetes, and expert consensus (see S1 Text) [23]. All costs and outcomes after the first year were discounted 3.5% per year in line with National Institute for Health and Care Excellence (NICE) recommendations.
The model is fully described in, including the sources from which all model inputs were derived. S1 Text
Model outcomes
The model calculates the following outcomes:
Results
Clinical study
Description of cohort
A total of 3,261 surgical patients with T2DM-Ins were identified from the NBSR as having had primary RYGB, SG, or AGB during the designated time frame (Fig 1). Of these, 2,484 (76.2%) had at least 1 follow-up visit recorded in the NSBR, with 1,847 having one visit between 6- and 24-months post-surgery (“1-year follow-up”). Of these, 1,313 (71.1%) underwent RYGB, 397 (21.5%) SG, and 137 (7.4%) AGB. Demographic data for these patients are summarised in Table 1.
Primary procedures were defined as RYBG, SG, or AGB. Acceptable data required all the following: nonzero age, initial weight 70 to 400 kg, height 1 to 2 m, and duration of T2DM recorded.
Flowchart to illustrate selection of surgical patients from NBSR database for the clinical study. NBSR, National Bariatric Surgical Registry.
| All | AGB | SG | RYGB | ||
|---|---|---|---|---|---|
| Number of patients | (%)n | 1,847 (100) | 137 (7.4) | 397 (21.5) | 1,313 (71.1) |
| Age (years) | Mean (SD) | 51.1 (9.4) | 52.6 (9.6) | 52.2 (10.1) | 50.7 (9.1) |
| Initial weight (kg) | Mean (SD) | 132.7 (24.5) | 130.1 (21.8) | 138.3 (28.8) | 131.2 (23.0) |
| Median (IQR) | 131.0 (115.3–148.1) | 129.0 (113.8–143.6) | 134.7 (119.0–153.6) | 129.9 (115.0–145.8) | |
| Initial BMI (kg/m)2 | Mean (SD) | 47.2 (7.3) | 47.0 (6.3) | 49.1 (8.7) | 46.6 (6.9) |
| Median (IQR) | 46.3 (41.8–51.5) | 46.9 (41.8–51.5) | 47.7 (42.8–54.4) | 46.1 (41.6–50.7) | |
| Sex | |||||
| Men | (%)n | 667 (36.1) | 44 (32.1) | 156 (39.3) | 467 (35.6) |
| Smoking 001 | |||||
| Never | (%)n | 984 (56.1) | 62 (49.6) | 238 (63.0) | 684 (54.7) |
| Ex | (%)n | 642 (36.6) | 51 (40.8) | 116 (30.7) | 475 (38.0) |
| Current | (%)n | 127 (7.2) | 12 (9.6) | 24 (6.4) | 91 (7.3) |
| Duration of T2DM | |||||
| 0–5 years | (%)n | 454 (24.6) | 29 (21.2) | 100 (25.2) | 325 (24.8) |
| 6–10 years | (%)n | 568 (30.8) | 42 (30.7) | 116 (29.2) | 410 (31.2) |
| >10 years | (%)n | 825 (44.7) | 66 (48.2) | 181 (45.6) | 578 (44.0) |
| Number of comorbidities | |||||
| 0 | (%)n | 525 (28.4) | 42 (30.7) | 112 (28.2) | 371 (28.3) |
| 1 | (%)n | 623 (34.2) | 45 (32.9) | 133 (33.5) | 454 (34.6) |
| 2 or more | (%)n | 690 (37.4) | 50 (36.5) | 152 (38.3) | 488 (37.2) |
| Ethnicity 001 | |||||
| White | (%)n | 1,591 (90.4) | 125 (94.0) | 328 (87.0) | 1,138 (91.0) |
| Nonwhite | (%)n | 169 (9.6) | 8 (6.0) | 49 (13.0) | 112 (9.1) |
Clinical outcomes
At 1-year follow-up (mean of 355 days post-procedure), the mean percentage weight loss was 27.4%, with evidence of differential weight loss between surgical groups (p < 0.001; Table 2).
Overall, approximately one-third (32.7%) of the total cohort were still using insulin at 1 year, with another third (33.5%) no longer recorded as having T2DM. There was significant variation in T2DM status by procedure (p < 0.001); with 33.6% having ceased use of insulin in the AGB group compared to 64.5% and 71.7% in the SG and RYGB groups, respectively, and a smaller proportion of patients assessed as having no indication of T2DM following AGB (5.1%) than SG and RYGB (30.0% and 37.6%, respectively).
Follow-up of over 2 years (mean 1,132 days, maximum 3,274 days) was available for 857 patients, of whom 605 (70.6%) underwent RYGB, 156 (18.2%) SG, and 96 (11.2%) AGB (Table 3). Weight loss again varied by procedure (p < 0.001) with levels broadly similar to those reported at 1-year follow-up. For diabetes status, differences between procedures were still apparent (p < 0.001), with a wider gap now seen between the percentage of patients with no indication of T2DM in the RYGB (42.2%) and SG (26.9%) groups.
Fig 2 summarises T2DM status over 4 years, in 3-month periods, for all surgical patients with follow-up within those periods only. Prevalence of insulin use reached a plateau at around 19 to 24 months, stabilising at this level up to 4 years after surgery. Similarly, BMI reached a plateau at around 13 to 18 months, stabilising over the next 4 years (Fig 3).
T2DM status in patients over time since bariatric procedure. Percentage of patients with each T2DM status among those with a follow-up visit during each time period from bariatric procedure. Numbers at each visit were the following: month 0 to 6= 2,150; month 7 to 12= 1,446; month 13 to 18= 1,114; month 19 to 24= 639; month 25 to 30= 633; month 31 to 36= 251; month 37 to 42= 190; month 43 to 48= 108. T2DM, type 2 diabetes mellitus. n n n n n n n n
BMI in patients over time since bariatric procedure. Box and whisker plot (median and IQR) to illustrate BMI of patients among those with a follow-up visit during each time period from bariatric procedure. Whiskers represent the upper and lower adjacent values, with dots showing observations beyond these values. Numbers at each visit were the following: month 0 to 6= 2,133; month 7 to 12= 1,442; month 13 to 18= 1,112; month 19 to 24= 637; month 25 to 30= 633; month 31 to 36= 250; month 37 to 42= 189; month 43 to 48= 108. BMI, body mass index; IQR, interquartile range. n n n n n n n n
| All (= 1,847)n | AGB (= 137)n | SG (= 397)n | RYGB (= 1,313)n | -value p 002 | ||
|---|---|---|---|---|---|---|
| Days since procedure | Mean (SD) | 354.7 (89.1) | 362.6 (80.0) | 351.2 (91.5) | 354.9 (89.2) | 0.43 |
| Readmission within 30 days 002 | ||||||
| No | (%)n | 1,718 (94.5) | 127 (94.8) | 374 (95.4) | 1,217 (94.2) | 0.64 |
| Yes | (%)n | 100 (5.5) | 7 (5.2) | 18 (4.6) | 75 (5.8) | |
| Weight loss | ||||||
| %WL | Mean (SD) | 27.4 (9.3) | 15.8 (9.0) | 25.1 (9.2) | 29.4 (8.2) | <0.001 |
| Median (IQR) | 27.6 (21.6–33.6) | 15.5 (10.3–21.3) | 24.9 (19.3–30.4) | 29.5 (24.1–34.8) | <0.001 | |
| %EWL | Mean (SD) | 61.5 (22.9) | 35.0 (20.1) | 54.7 (22.8) | 66.3 (20.8) | <0.001 |
| Median (IQR) | 60.6 (47.0–75.3) | 34.6 (21.8–49.7) | 53.0 (39.8–67.4) | 64.9 (52.7–78.7) | <0.001 | |
| Diabetes status | ||||||
| No indication of T2DM | (%)n | 619 (33.5) | 7 (5.1) | 119 (30.0) | 493 (37.6) | <0.001 |
| Impaired fasting glycaemia | (%)n | 77 (4.2) | 4 (2.9) | 19 (4.8) | 54 (4.1) | |
| Oral hypoglycaemics | (%)n | 548 (29.7) | 35 (25.6) | 118 (29.7) | 395 (30.1) | |
| Insulin | (%)n | 603 (32.7) | 91 (66.4) | 141 (35.5) | 371 (28.3) | |
| All | AGB | SG | RYGB | -value p 003 | ||
|---|---|---|---|---|---|---|
| Number of patients | (%)n | 857 (100) | 96 (11.2) | 156 (18.2) | 605 (70.6) | |
| Days since procedure | Mean (SD) | 1,131.5 (466.9) | 1,455.2 (551.3) | 1,062.8 (413.6) | 1,097.9 (445.3) | <0.001 |
| Weight loss | ||||||
| %WL | Mean (SD) | 27.1 (11.1) | 17.2 (10.0) | 24.7 (11.5) | 29.3 (10.1) | <0.001 |
| Median (IQR) | 27.3 (19.5–34.9) | 17.0 (10.8–24.2) | 23.5 (17.4–32.2) | 29.1 (22.6–36.3) | <0.001 | |
| %EWL | Mean (SD) | 59.7 (25.0) | 37.7 (22.6) | 53.3 (26.1) | 64.9 (22.8) | <0.001 |
| Median (IQR) | 59.3 (43.6–76.6) | 36.5 (24.3–51.0) | 51.0 (35.7–70.1) | 64.4 (49.8–80.2) | <0.001 | |
| Diabetes status | ||||||
| No indication of T2DM | (%)n | 314 (36.6) | 17 (17.7) | 42 (26.9) | 255 (42.2) | <0.001 |
| Impaired fasting glycaemia | (%)n | 40 (4.7) | 3 (3.1) | 10 (6.4) | 27 (4.5) | |
| Oral hypoglycaemics | (%)n | 270 (31.5) | 24 (25.0) | 50 (32.1) | 196 (32.4) | |
| Insulin | (%)n | 233 (27.2) | 52 (54.2) | 54 (34.6) | 127 (21.0) | |
Prediction of insulin cessation by baseline factors
Insulin cessation was more prevalent in patients undergoing RYGB than in patients undergoing SG (RR 0.92, 95% CI 0.86 to 0.99, p = 0.02) or AGB (RR 0.45, 95% CI 0.34 to 0.60, p < 0.001) (Table 4). Male patients were more likely to cease insulin use after surgery (RR 1.14, 95% CI 1.07 to 1.23, p < 0.001). There was no evidence of different insulin cessation rates by number of comorbidities (RR 1.02, 95% 0.94 to 1.11 for 2 or more versus none). Patients with shorter T2DM duration were more likely to cease insulin (RR 1.40, 95% CI 1.29 to 1.53, p < 0.001, for patients with duration <5 years as compared to those with duration >10 years). When adjusted for other baseline demographic factors, procedure, gender, and duration of diabetes were all independent predictors of cessation of insulin use after surgery (p < 0.001).
| n | % on insulin at 6–24 month follow-up | RR (95% CI) unadjusted | RR (95% CI) mutually adjusted | |
|---|---|---|---|---|
| Operation type | ||||
| AGB | 137 | 66.4% | 0.45 (0.34–0.60) | 0.46 (0.35–0.61) |
| RYGB | 1,313 | 28.3% | 1 | 1 |
| SG | 397 | 35.5% | 0.92 (0.86–0.99) | 0.91 (0.84–0.98) |
| -value p 004 | <0.001 | <0.001 | ||
| Age (years) | ||||
| 17–39 | 222 | 35.6% | 0.89 (0.81–0.98) | 0.90 (0.83–0.97) |
| 40–49 | 540 | 30.4% | 1 | 1 |
| 50–59 | 718 | 31.9% | 0.95 (0.87–1.04) | 0.98 (0.90–1.06) |
| 60+ | 367 | 35.7% | 0.91 (0.81–1.01) | 0.97 (0.88–1.07) |
| -value p 004 | 0.96 | 0.13 | ||
| Sex | ||||
| Female | 1,180 | 35.9% | 1 | 1 |
| Male | 667 | 26.8% | 1.14 (1.07–1.23) | 1.14 (1.06–1.23) |
| -value p 004 | <0.001 | <0.001 | ||
| Initial BMI | ||||
| 40 or less | 284 | 34.5% | 1.04 (0.89–1.22) | 1.02 (0.87–1.19) |
| 40–45 | 479 | 35.3% | 1 | 1 |
| 45–50 | 490 | 32.0% | 1.04 (0.95–1.13) | 1.02 (0.94–1.11) |
| 50–55 | 324 | 31.2% | 1.05 (0.96–1.14) | 1.03 (0.95–1.12) |
| 55–60 | 176 | 31.8% | 1.09 (0.96–1.23) | 1.10 (0.98–1.24) |
| 60 or more | 94 | 23.4% | 1.14 (0.99–1.32) | 1.11 (0.96–1.27) |
| -value p 004 | 0.31 | 0.31 | ||
| Smoking | ||||
| Never | 984 | 32.4% | 1 | 1 |
| Ex vs. never | 642 | 32.9% | 1.01 (0.94–1.08) | 1.00 (0.93–1.07) |
| Current vs. never | 127 | 25.2% | 1.12 (1.01–1.23) | 1.09 (0.98–1.27) |
| -value p 004 | 0.051 | 0.1 | ||
| Comorbidities | ||||
| 0 | 525 | 36.2% | 1 | 1 |
| 1 | 632 | 30.2% | 1.06 (0.98–1.16) | 1.07 (1.00–1.15) |
| 2 or more | 690 | 32.2% | 1.02 (0.94–1.11) | 1.03 (0.95–1.12) |
| -value p 004 | 0.7 | 0.5 | ||
| T2DM duration (years) | ||||
| 0–5 | 454 | 19.8% | 1.40 (1.29–1.53) | 1.39 (1.28–1.50) |
| 6–10 | 568 | 27.3% | 1.31 (1.19–1.44) | 1.29 (1.17–1.42) |
| >10 years | 825 | 43.4% | 1 | 1 |
| -value p 004 | <0.001 | <0.001 | ||
| Ethnicity | ||||
| White | 1,591 | 32.4% | 1 | 1 |
| Nonwhite | 169 | 32.5% | 1.06 (0.96–1.18) | 1.09 (1.00–1.20) |
| -value p 004 | 0.4 | 0.21 | ||
Prediction of insulin cessation by subsequent change in weight
Lower %WL and %EWL at follow-up was associated with significantly poorer rates of insulin cessation (Table 5). To investigate whether the relative improvement in insulin cessation outcomes conferred by RYGB was related to weight loss, the model was fitted adjusting for all baseline factors except initial BMI, with either %WL (WL model) or %EWL (EWL model) included. Once weight loss was adjusted for using either model, SG was no longer associated with statistically inferior rates of insulin cessation compared to RYGB (RR 0.97, 95% CI 0.90 to 1.04, p = 0.37 for WL model and RR 0.97, 95% CI 0.91 to 1.04, p = 0.44 for EWL model). Even when adjusted for weight loss, however, AGB was still associated with poorer rates of insulin cessation than RYGB (RR 0.55, 95% CI 0.40 to 0.74 for WL model and RR 0.56, 95% CI 0.42 to 0.73 for EWL model, p < 0.001).
To assess whether nonlinearity between age, %WL, %EWL, and insulin cessation would impact the RR for insulin cessation conferred by the different operations, sensitivity analyses fitted alternative models using quadratic terms. These adjusted models generated approximately the same RRs, consistently finding AGB to be inferior to RYGB and SG for insulin cessation (). S1 Table
| n | % on insulin at 6–24 month follow-up | RR (95% CI) unadjusted | RR (95% CI) fully adjusted(WL model) 005 | RR (95% CI) fully adjusted(EWL model) 005 | |
|---|---|---|---|---|---|
| Operation type | |||||
| AGB | 137 | 66.4% | 0.45 (0.34–0.60) | 0.55 (0.40–0.74) | 0.56 (0.42–0.73) |
| RYGB | 1,313 | 28.3% | 1 | 1 | 1 |
| SG | 397 | 35.5% | 0.92 (0.86–0.99) | 0.97 (0.90–1.04) | 0.97 (0.91–1.04) |
| -value p 005 | <0.001 | <0.001 | <0.001 | ||
| Weight loss (%) | |||||
| 20% or less | 369 | 51.5% | 1 | 1 | _ |
| 20%–25% | 335 | 36.4% | 1.33 (1.17–1.52) | 1.21 (1.06–1.38) | _ |
| 25%–30% | 407 | 31.9% | 1.45 (1.27–1.66) | 1.33 (1.16–1.51) | _ |
| 30%–35% | 359 | 23.7% | 1.55 (1.36–1.78) | 1.37 (1.20–1.57) | _ |
| 35% or more | 377 | 20.2% | 1.53 (1.34–1.74) | 1.35 (1.19–1.54) | _ |
| -value p 005 | <0.001 | <0.001 | |||
| Excess weight loss (%) | |||||
| 25% or less | 75 | 68.0% | 0.51 (0.39–0.67) | _ | 0.64 (0.51–0.80) |
| 25%–50% | 471 | 40.6% | 1 | _ | 1 |
| 50%–75% | 825 | 30.7% | 1.16 (1.06–1.27) | _ | 1.13 (1.04–1.22) |
| 75%–100% | 388 | 22.4% | 1.26 (1.15–1.39) | _ | 1.19 (1.09–1.30) |
| 100% or more | 88 | 23.9% | 1.22 (1.04–1.43) | _ | 1.19 (1.00–1.40) |
| -value p 005 | <0.001 | <0.001 | |||
Cost and cost-effectiveness analysis
Detailed results are presented in.–Tables detail model inputs,provides additional results, and–Tables give uncertainty and scenario analyses.–Figs illustrate model design and patient flow through the models, whileandFigs provide additional results. The most important economic-related outcomes are summarised and presented below. S1 Text S2 S15 S16 Table S17 S19 S1 S3 S4 S5
Treatment acquisition costs
Table 6 summarises the results in terms of cumulative average treatment acquisition cost per patient over 5 years for surgery and BMT. Every patient in the bariatric surgery arm will follow the bariatric surgery costs (S10 Table), whereby their first-year treatment will have one-off surgery costs and subsequent drug costs. Every patient in the BMT arm will have drug costs as detailed in S11 Table which may vary each year, depending on whether treatment strategy stays the same (if hemoglobin A1c (HbA1c) falls below 8%) or is modified (S5 Table). If a patient dies before the end of the 5-year term (from diabetes-related deaths or other deaths), they will no longer contribute to the acquisition costs or any other costs (see S2 Fig for patient flow).
As shown, when compared to BMT, bariatric surgery is predicted to a lead to treatment acquisition cost saving over a 5-year time horizon.
| BS | BMT | Incremental cost (BS–BMT) | |
|---|---|---|---|
| Drug costs (GBP£) | 641 | 10,578 | −9,937 |
| Surgery cost (GBP£) | 5,544 | 0 | 5,544 |
| Total treatment costs (GBP£) | 6,185 | 10,578 | −4,393 |
Adverse events
In relation to costs directly attributable to adverse events of treatment (i.e., in the surgical arm costs of surgical complications plus adverse drug reactions; and in the BMT group the adverse drug reactions), the cumulative costs for the bariatric surgical group were GBP£1,152, and for the group undergoing BMT, GBP£955. This represents an incremental difference of GBP£197 in favour of BMT over a 5-year period.
Reductions in disease-related complications
Based on the assumptions of the effects of BMT and bariatric surgery on modifying HbA1c and BMI (both of which were the two most important predictors of T2DM complications, see S1 Text), bariatric surgery leads to a lower cumulative incidence of diabetes-related complications (Table 7) and consequently lower cost for the management of these complications (Table 8).
| BS | BMT | Incremental difference (BS–BMT) | |
|---|---|---|---|
| IHD (%) | 3.17 | 4.12 | −0.95 |
| MI (%) | 6.02 | 6.62 | −0.60 |
| CHF (%) | 2.36 | 6.43 | −4.07 |
| Stroke (%) | 1.63 | 2.06 | −0.43 |
| Amputation (%) | 0.29 | 0.67 | −0.38 |
| Renal failure (%) | 0.42 | 0.35 | 0.07 |
| BS | BMT | Incremental difference (BS–BMT) | |
|---|---|---|---|
| IHD cost (GBP£) | 414 | 542 | −128 |
| MI cost (GBP£) | 381 | 362 | 19 |
| CHF cost (GBP£) | 187 | 491 | −304 |
| Stroke cost (GBP£) | 283 | 352 | −69 |
| Amputation cost (GBP£) | 55 | 113 | −58 |
| Renal failure cost (GBP£) | 197 | 144 | 52 |
| Other costs(GBP£) 008 | 13,203 | 12,748 | 455 |
| Total cost (GBP£) | 14,720 | 14,753 | −33 |
Summary of total costs
In summary, bariatric surgery is predicted to result in a total cost saving of GBP£4,229 when compared to BMT over a 5-year time horizon (Table 9).
Unlike medication costs, the costs of surgery are incurred at the start of the model and not spread over the 5-year period; hence, at approximately 3.5 years after surgery, the total cost of a patient treated with bariatric surgery equals the total cost of a patient treated with BMT, whereby from that breakeven point, bariatric surgery becomes the cost-saving option.
| BS | BMT | Incremental difference (BS–BMT) | |
|---|---|---|---|
| Treatment acquisition costs (GBP£) | 6,185 | 10,578 | −4,393 |
| Adverse event costs (GBP£) | 1,152 | 955 | 197 |
| Cost of complications (GBP£) | 14,720 | 14,753 | −33 |
| Total costs (GBP£) | 22,057 | 26,286 | −4,229 |
Cost-effectiveness
As shown in Table 10, from a cost-effectiveness perspective, when compared to BMT, bariatric surgery is predicted to lead to a lower cumulative incidence of diabetes-related complications and is consequently associated with improved life expectancy and measures of quality of life.
Probabilistic sensitivity analysis demonstrated that bariatric surgery consistently leads to cost savings when compared with BMT and in more than 50% of cases to positive incremental health benefits (and). S16 Table S5 Fig
| BS | BMT | Incremental difference (BS–BMT) | ICER (cost/QALY) | NMB (GBP£) | NHB (QALYs) | |
|---|---|---|---|---|---|---|
| Costs (GBP£) | 22,057 | 26,286 | −4,229 | Dominated by BS 010 | 4,731 | 0.24 |
| Average QALYs | 3.18 | 3.15 | 0.03 | |||
| Life years gained in 5 years | 4.47 | 4.43 | 0.04 |
Discussion
We used the UK NBSR, a nationwide registry of patients undergoing bariatric surgery, to assess clinical outcomes of surgery for patients with obesity and T2DM-Ins. Our findings were then combined with data from the literature to develop a model to analyse cost-effectiveness of bariatric surgery for this cohort, when compared to BMT. The study demonstrated that bariatric surgery in patients with obesity and T2DM-Ins was associated with good medium-term clinical outcomes and was cost saving when compared to best medical management both in terms of “upfront” treatment costs and avoidance of future costs of complications. In this, the largest clinical series to date, two-thirds of patients with T2DM-Ins at baseline ceased use of insulin after surgery, with one-third ceasing all medication for T2DM. Our data suggest that these improvements persist for at least 4 years following surgery. These results are comparable to those of a regional database study which reported that 27% of patients on insulin at baseline continued to take insulin at 3 years post-RYGB, with 40% off all medication for T2DM [15]. Interestingly, our results are also similar to those reported for patients with both recent and long-standing T2DM: in a randomised controlled trial 5 years post-RYGB or SG, 35% of surgical patients had stopped taking all medications for T2DM [4]. Our findings therefore challenge the popular view that bariatric surgery has limited clinical efficacy for patients with more advanced T2DM [14].
Our data indicate that in patients requiring insulin for T2DM, AGB is associated with lower rates of insulin cessation and remission of T2DM than RYGB and SG. Greater weight loss has been associated with superior T2DM outcomes [16,29], and we found that this holds true for patients with T2DM-Ins. Moreover, even when adjusted for weight loss, AGB was associated with lower rates of insulin cessation when compared to RYGB or SG. These findings support the notion that improvements in T2DM seen after bariatric surgery have both weight loss–dependent and weight loss–independent components [12,30]. We observed a trend towards increased insulin cessation over time in the RYGB group, despite weight stability, suggesting a further possible late weight loss–independent effect of RYGB on T2DM.
The major novel finding of this study is that over a 5-year time horizon, the costs of bariatric surgery are predicted to be lower than those of medical management for patients with T2DM-Ins. Of particular note, the greatest savings stem from direct treatment costs: bariatric surgery is significantly cheaper than the medications that would otherwise be prescribed to patients with severe T2DM over a 5-year period. This is an important finding, given that the majority of previous economic evaluations concluded that the direct treatment costs of surgery exceeded those of BMT [21,31–33]. The difference may be explained by the fact that previous studies either predated the widespread adoption of newer pharmacological agents for diabetes or focused on patients with early T2DM who are often maintained on relatively inexpensive single oral agents [20–22].
In terms of adverse events, our financial allocations for surgical complications over the 5-year period are comparable to other models derived from UK data [20,22]; however, the majority of previous studies evaluating the costs of bariatric surgery versus medical management have not included costings for adverse events related to treatment in the medically treated patients [20,21]. The newer medications in use for T2DM such as GLP-1 RA and SGLT-2 inhibitors have side effect profiles that require medical attention and treatment in a proportion of patients [34,35]. Though these adverse medical events do have cost implications, the adverse events costs for surgical patients are still slightly higher than for patients treated with BMT in this study.
With regard to avoidance of complications, previous economic evaluations have demonstrated contradictory results. In the UK, Gulliford and colleagues demonstrated that although a bariatric surgical strategy in patients with obesity and T2DM had higher expected cost than medical management, the cost of subsequent clinical gains was sufficiently low to make surgery cost-effective to a healthcare payer (GBP£7,129/QALY gained) [20]. By contrast, Borisenko and colleagues found that the avoidance of complications through a surgical strategy in patients with obesity and T2DM lead to direct healthcare savings [22]. This saving, however, occurred over a long time horizon (for female patients 10 years and for male patients over a lifetime). We have demonstrated that not only are there cost savings within the cohort of patients with T2DM-Ins due to avoidance of future complications, but also these savings occur over a very short time horizon of less than 5 years. It is likely that the differences between our study findings and previous analyses are due to the fact that our study was designed to specifically investigate the sub-cohort of patients with T2DM-Ins, for whom BMT involves expensive medications.
Our study has some limitations. The NBSR dataset contains limited long-term follow-up: we attempted to address this issue by mandating a minimum follow-up period. Moreover, it should be noted that loss to follow-up rate in this study is comparable to other national registry studies (e.g., [15]), and there is no evidence of any systematic bias with regard to the outcomes of those who did and did not attend follow-up. Furthermore, it should be noted that the total number of patients with T2DM-Ins with 4-year follow-up in the present study is larger than any previously published study. With regard to the comparison of the individual procedures, this was not a randomised controlled trial, and hence, there were significant size disparities (as well as potentially clinical and demographic differences) in the cohorts of patients undergoing AGB, SG, and RYGB. In addition, the NBSR does not include details on the dosage and number of medications that the patients took before and after surgery; however, it should be noted that the classification of diabetes status in the database is likely to have underestimated the efficacy of surgery as some patients in remission of diabetes are placed on prophylactic metformin [36].
With regard to the health economic model, we accept that the lack of HbA1c data in the NBSR cohort is a significant limitation as it does introduce a degree of uncertainty in our estimates of future diabetes-related complications. In the present study, changes in HbA1c levels post-surgery in our model were inferred from previous studies. Nonetheless, HbA1c levels may be less economically important than changes in medications, particularly given our finding that the direct medication costs in the BMT group (as opposed to changes in disease-specific complication rates) are the most significant factor in the cost saving associated with bariatric surgery. As with all models, ours was unable to include all variables that may impact on overall outcomes. For example, our model was not designed to consider the broader cost implications of weight loss and improvement in T2DM status on occupational productivity. Additionally, we were unable to incorporate the potential differential effects of bariatric surgery as compared to BMT on lifestyle factors such as physical exercise and mental health status, which may, in turn, affect health and cost outcomes more broadly. Finally, our time horizon perspective for cost-effectiveness was deliberately short at 5 years, and therefore there is uncertainty around long-term cost-effectiveness.
It is also worth noting that both medical and surgical treatments for patients with obesity and T2DM evolve over time: this is true of the available medications and operations, as well as the evidence regarding their efficacy and side effects. For example, in the surgical group, we have not analysed the impact of other procedures such as loop gastric bypass as this was infrequently performed at the time the data were collected. With respect to BMT, since the time the model was devised, it has become clear that use of both GLP-1 RA and SGLT2 inhibitors may confer additional benefits for patients with T2DM in terms of reduction of adverse cardiovascular and renal outcomes [37,38]—future analyses would factor this in.
In summary, this study provides evidence that a strategy of treating patients with obesity and T2DM-Ins with SG or RYGB is associated with a significant incidence of diabetes remission and a high incidence of cessation of insulin therapy. Moreover, while previous economic analyses have suggested that a surgical strategy for T2DM provides clinical benefits but with higher up-front cost to the healthcare payer, this study indicates that for patients with T2DM-Ins, the total cost to the health payer is reduced following bariatric surgery as compared to BMT over a 5-year time period. This pattern is seen even when the clinical benefits of bariatric surgery over BMT, in terms of avoidance of future complications, are not considered.
Supporting information
Abbreviations
Data Availability
There are restrictions on the availability of data for this study, due to the initial patient consent forms, which only allow the sharing of data for research purposes. Researchers wishing to access an anonymized dataset containing individual participant data can apply to the research data management service at St George's University of London UK (researchdata@sgul.ac.uk), where the data is held in a repository. The link is https://doi.org/10.24376/rd.sgul.12841151↗.
Funding Statement
VV, OAK and HT received grant funding from Medtronic UK to support the building of the cost effectiveness model and the data analytics required to derive optimal inputs for the model. CL is an employee of Medtronic UK (www.medtronic.co.uk↗). Medtronic UK played no role in study design, data collection and analysis, decision to publish or preparation of the manuscript.
References
Associated Data
Supplementary Materials
Data Availability Statement
There are restrictions on the availability of data for this study, due to the initial patient consent forms, which only allow the sharing of data for research purposes. Researchers wishing to access an anonymized dataset containing individual participant data can apply to the research data management service at St George's University of London UK (researchdata@sgul.ac.uk), where the data is held in a repository. The link is https://doi.org/10.24376/rd.sgul.12841151↗.