Increase in major osteoporotic fractures after therapy with immune checkpoint inhibitors
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Abstract
Background Immune checkpoint inhibitors (ICIs) can cause severe and sometimes long-standing immune-related adverse events (irAEs). Enhanced immune activation from ICI can theoretically result in osteoclast activation, bone loss and fracture. The objective of this study was to evaluate the incidence rates of major osteoporotic fractures (MOFs) in patients with melanoma treated with ICI.
Methods We conducted a before–after cohort study using a commercial healthcare claims dataset of adult patients with melanoma from the USA who received ICI therapy between 2011 and 2022. Incidence rates of MOF before and after ICI initiation were ascertained using International Classification of Diseases 9/10 diagnostic codes.
Results The study cohort included 3137 patients, mean age was 68 years, of which 2010 (64%) were men. 40 (1.3%) patients had an MOF in the year before ICI initiation and 57 (1.8%) and 34 (1.8%) had an MOF in the first and second years after ICI initiation, respectively. The HR for MOF over the first year after versus the year before the first ICI dose was 1.82 (95% CI 1.24 to 2.66), and it was 1.85 (95% CI 1.12 to 2.90) over the second year. Prior fracture, older age, female sex and combination ICI therapy were associated with greater risk of MOF after ICI initiation.
Conclusion Patients who receive ICI are at increased risk of MOF after receiving therapy. Given the plausible biological pathway, osteoporosis and osteoporotic fractures may represent a novel irAE of ICI therapy.
What is already known on this topic
Immune checkpoint inhibitors (ICIs) can cause a wide range of immune-related adverse events (irAEs), although osteoporosis and fractures are not well recognised irAEs. One previous administrative database study found an increase in fracture risk after ICI initiation but the sample size was limited and data on bone metastasis was not available.
What this study adds
This study shows that major osteoporotic fracture risk increases after ICI initiation, independent of bone metastasis.
How this study might affect research, practice or policy
Osteoporotic fracture may be an unrecognised irAE of ICIs. Patients initiating ICIs may warrant bone health screening and treatment.
Introduction
Immune checkpoint inhibitors (ICIs) are antibodies that block inhibitory pathways associated with immune activation, which have been proven to be effective at fighting various tumours such as melanoma and lung, breast, gastrointestinal and kidney cancers. Since initial Food and Drug Administration (FDA) approval in 2011, the proportion of patients with cancer in the USA treatable with ICI increased from 1.5% to 43.6%.1 While ICIs have proven to be life saving for many patients, they are associated with immune-related adverse events (irAEs) affecting multiple organ systems including arthritis, myositis, colitis, dermatitis and endocrinologic dysfunction.2 3 Activation of T cells can also lead to bone resorption through the increased production of key bone-resorption cytokines such as receptor activator of nuclear factor kappa-B ligand (RANK-L) and tumour necrosis factor alpha (TNF-α).4 RANK-L and TNF-α trigger proliferation, maturation and activation of osteoclasts leading to bone resorption and, over time, osteoporosis leading to fragility fractures.5
Osteoporotic fractures are associated with decreased quality of life and increased risk of institutionalisation and death.6–8 While the impact of fractures specifically in ICI users is unknown, fractures have recently been shown to increase mortality risk in cancer survivors.7 In spite of the significant morbidity and mortality associated with fractures, osteoporosis screening and treatment are rarely offered to patients with cancer, even after suffering fractures.9
Despite the known effects of T-cell activation on bone, the effect of ICIs on bone has not been elucidated. Two small case series and a pharmacovigilance study have described fractures associated with ICI therapy.10 11 The case series describe a total of six patients who suffered osteoporotic fractures in the absence of diagnosed osteoporosis after ICI initiation.11 The pharmacovigilance study examined 822 drug-event pairs of bone and joint injuries and ICI use from the worldwide pharmacovigilance database Food and Drug Administration Adverse Event Reporting System and found a disproportionality signal of increased spinal compression and hip fractures in patients exposed to ICI compared with patients exposed to all other drugs, suggesting a possible causal relationship.10
A recent population-based study from Canada showed for the first time that the incidence rate of major osteoporotic fractures (MOFs) increased over twofold after ICI initiation.12 However, this study included multiple cancer types, including lung cancers which have a high affinity for bone metastases,13 making it difficult to separate out pathologic fractures from osteoporotic fractures using administrative healthcare data. Their sample size also limited their ability to examine potential predictors of osteoporotic fractures after ICI initiation. A larger sample size with a more homogeneous cancer cohort that is at lower risk of bone metastases would help to confirm the association between ICI use and osteoporotic fractures.
In this population-based cohort study using a large US insurance database, we examine the risk of osteoporotic fractures in patients with melanoma treated with ICI, before and after initiation of ICI treatment.
Methods
Data sources
This retrospective before–after cohort study evaluated patients with melanoma using Optum’s deidentified Clinformatics Data Mart (CDM) database, including patients enrolled between 1 January 2010 and 30 June 2021. Clinformatics is derived from a database of administrative health claims for members of large commercial and Medicare Advantage health plans.14 The University of Texas Health Science Center at Houston purchased the data license of the Optum CDM claims data. The data were stored on the University of Texas Science Center data server and could only be accessed through the institution’s virtual private network.
Cohort identification
We identified all men and women who were 18 years of age or older and had used at least one dose of FDA-approved ICI during the study period. Patients were required to have an International Classification of Diseases (ICD) 9/10 claims diagnosis of melanoma listed as the primary cancer between 60 days prior to and 60 days after the first ICI usage date (index date). Patients had to have continuous enrolment in the database for a minimum of 18 months prior to the index date and a minimum of 3 months after the index date (figure 1).
The exposure of interest was ICI usage. The ICI drugs included in this study were programmed cell death protein 1 (PD-1)/programmed death-ligand 1 (PD-L1) inhibitors (pembrolizumab, nivolumab, cemiplimab, durvalumab, atezolizumab, avelumab) and cytotoxic T-lymphocyte-associated protein 4 (CTLA-4) inhibitor, ipilimumab. Patients were excluded if they had three or more cancer diagnoses listed or used off-label combinations of ICI drugs on the same day (eg, combination of more than one PD-1 or PD-L1 inhibitor on the same day). Monotherapy was defined as exposure to only one ICI drug on one calendar date. Combination therapy was defined as a PD-1 or PD-L1 inhibitor and a CTLA-4 inhibitor administered on the same day.
Outcome and follow-up
The outcome of interest was incident fractures occurring in the year prior to and in the first and second years after ICI initiation. We identified fractures of hip, forearm, humerus or vertebrae using ICD 9/10 diagnostic codes from inpatient and outpatient claims records per previously validated fracture site-specific algorithms (online supplemental table S1).15 16 Collectively, we referred to a fracture at one of these sites as an MOF. An incident fracture event required at least two codes for a fracture in the same anatomical site within 90 days or at least one inpatient diagnosis listed in the first three diagnosis positions.
To ensure we were ascertaining new fracture events and not follow-up for a prevalent fracture, no fracture claims in the same anatomical site within the prior 6-month period were allowed. Outcomes were assessed from 18 months prior to the index date (to allow the 6-month washout period to avoid double-counting prevalent fractures) to the first MOF, last follow-up or death.
Covariates
Sociodemographic information including age, race, sex and region were obtained from enrolment data. Race was categorised into white and other due to low cell counts for races other than white. Region was categorised into Midwest, Northwest, South and West per the existing categories defined in the database. Year of ICI initiation (index date) was categorised as 2011–2016 and 2017–2021 based on the approval of ICI therapy in the adjuvant setting for resectable disease in 2017.17 Thus, the population of patients treated with ICI before and after 2017 would be different, with a higher proportion of lower-stage, resectable, melanoma included after 2017. Comorbidities were ascertained using the National Cancer Institute Comorbidity Index using ICD codes.18 Prior radiation therapy was ascertained using previously reported ICD billing codes.19
Glucocorticoid usage was ascertained using the pharmacy claims data, which includes all medications filled by a patient as an outpatient prior to the first fracture date. All systemic glucocorticoids included in the study were converted to prednisone-equivalent doses measured in milligrams per day. Average daily dose was calculated by summing the total dose dispensed divided by the total days of supply. Glucocorticoid usage was ascertained to the time of MOF, end of enrolment or 1 year, whichever came first.
Bone metastasis was identified using ICD 9/10 diagnostic codes from inpatient and outpatient claims recorded between 12 months before ICI initiation and 12 months after ICI initiation. A bone metastasis diagnosis was defined as two claims with ICD9 code 198.5 and ICD10 code C79.52 at least 30 days apart.20
Statistical analysis
Baseline characteristics were expressed as mean±SD or as a percentage of the cohort. Baseline characteristics were compared between those who experienced incident fractures and those without incident fractures using one-way analysis of variance for continuous variables and χ2 tests of independence for categorical variables. Fisher’s exact test was used to compare bone metastasis between those with and without incident fracture. P values less than 0.05 were considered statistically significant.
Follow-up time was stratified into the pre-ICI period and the post-ICI period as defined by the index date. Time to MOF was measured in both periods and compared using a log-rank test. Cox regression for correlated outcomes was performed to estimate HR of MOF in the post-ICI period as compared with the pre-ICI period with 95% CIs. Patients were censored at last follow-up or death.
MOF incidence rate per 1000 person-years was calculated by dividing the number of incident MOFs in the time period by the total person-years of follow-up. For incidence rate analysis, the follow-up time was stratified into the 365 days prior to the index date (year −1 to 0), the 365 days after the index date (year 0–1) and days 366–730 after the index date (year 1–2). The incidence rate ratios were compared between years 0–1 and 1–2 with the reference year −1 to 0 using the exact Poisson 95% CIs and the exact mid-p values.21 22
To examine predictors of MOF after ICI initiation, we ran a multivariable Cox regression model which included prior MOF, age as a continuous variable by decade, sex, year of ICI initiation, type of ICI therapy, race, number of comorbidities and average daily and total glucocorticoid use. Missing values for covariates were addressed using complete case analysis when performing the multivariable Cox regression model. The proportional hazards assumption was confirmed for each covariate in the Cox regression model both graphically and numerically using cumulative sums of martingale-based residuals.23 Statistical analyses were performed using the SAS software programme V.9.4.
Results
The study cohort consisted of 3137 individuals (mean age at ICI initiation 68.0 years, SD 13.8), of which 2010 (64.1%) were men. Table 1 summarises baseline characteristics of the cohort at the index date, stratified by incident MOF status. The mean observation time was similar in both groups (304 vs 289 days, p=0.324). For those who suffered an incident MOF, the average age was older (74.7 years vs 67.9 years, p<0.001), they were more likely to be women (p<0.001) and had slightly less total glucocorticoid exposure. There was a higher percentage of deaths within 1 year of ICI initiation in the group with incident MOF than in the group without (33.3% vs 21.6%, p=0.050). The groups were otherwise similar for year of ICI initiation, type of ICI therapy, race, region, comorbidities, bone metastasis, chemotherapy and radiation exposure (p>0.05). In total, only five individuals had missing values of covariates.
Table 1
|
Baseline characteristics by incident fracture status
In total, 40 individuals suffered an MOF in the year prior to starting ICI therapy, 57 individuals suffered an MOF in the first year after starting ICI therapy and 34 individuals suffered an MOF in the second year after starting ICI therapy. Time to MOF was significantly shorter in the post-ICI period (log-rank test p=0.003). The HR of suffering an incident MOF in the first post-ICI year as compared with the pre-ICI year was 1.82 (95% CI 1.24 to 2.66, p=0.002). The HR of suffering an incident MOF in the second post-ICI year as compared with the pre-ICI year was 1.85 (95% CI 1.12 to 2.90, p=0.007)
The incidence rate of MOF in the year prior to ICI initiation was 12.8 per 1000 patient-years, which was significantly lower than in the first year after ICI initiation, when it was 24.2 per 1000 patient-years (incidence rate ratio [IRR] 1.90, 95% CI 1.25 to 2.91, p=0.002, table 2). The fracture rate remained elevated in the second year after ICI initiation at 23.9 per 1000 patient-years (IRR 1.87, 95% CI 1.16 to 3.02, p=0.007).
Table 2
|
Fracture rate pre-ICI and post-ICI initiation
In multivariable models, prior fracture, older age, female sex and combination ICI therapy were associated with greater risk of MOF after ICI initiation (table 3). For each decade of increase in age, the hazard of fracture increased by 58% (HR 1.58, 95% CI 1.21 to 2.07). Having a prior MOF in the year prior to ICI therapy increased the hazard of incident MOF after ICI initiation by 5.48 times. Women were at 2.82 times the risk as compared with men. Combination ICI therapy increased fracture risk by 2.46 times as compared with monotherapy.
Table 3
|
Predictors of fracture after ICI: multivariable Cox regression model
Discussion
We found that the risk of suffering an MOF increased by over 80% in the first and second years after ICI initiation in patients with melanoma. Those who were women, of older age, with a history of MOF and exposed to combination ICI therapy were at greater risk of suffering an incident MOF after ICI initiation. Glucocorticoid use, considering either average daily dose or total cumulative dose, was not a significant predictor of MOF after ICI in our multivariable model. However, it should be noted that glucocorticoid use was low in our cohort.
Our primary outcome was consistent with the previous before–after population-based study which found a 2.43 (95% CI 1.34 to 4.27) times increased risk of MOF after initiation of ICI therapy.12 In our study, combination ICI therapy was associated with higher risk of fracture, which is consistent with existing literature that combination ICI therapy is associated with greater risk of irAEs as compared with ICI monotherapy.24 However, in the first study, no difference in risk of MOF was detected between the different types of ICI. This may represent inadequate sample size or a reflection of confounding by indication of underlying cancer type and the association between certain cancer types with increased fracture risk, a potential issue that we were able to mitigate by examining only one cancer type.
Screening tools and treatments to prevent cancer treatment-induced bone loss already exist.25–30 If ICI therapy increases risk of osteoporotic fractures, cancer survivors exposed to ICI therapy may need to be screened and treated for osteoporosis at a lower threshold than the general population. Cancer treatment-induced bone loss guidelines, which currently target those exposed to hormone deprivation therapies, may need to be expanded to include those who have been exposed to ICI.25 27–29 With the success of ICIs in advanced stage cancers, patients are living long enough for post-treatment osteoporosis to become one of the main sources of morbidity and determinants of quality of life. Early identification of those at risk may lead to earlier interventions to prevent bone loss/fractures.
Strengths of this study include adequate sample size to examine predictors of MOF in ICI users while restricting our cohort to one tumour type. We chose melanoma because out of the major tumour types for which ICI therapy is indicated, melanoma is the least likely to metastasise to bone.13 Less than 5% of our cohort had bone metastasis and there was no difference in frequency of bone metastasis between those who fractured and those who did not. Further, we used stringent and previously validated definitions of incident fracture and limited our analysis to MOFs, thereby reducing risk of contamination with other fractures or double-counting prevalent fractures as incident fracture.16 The predictors of MOF found in our study, including female sex, older age and a history of MOF, are consistent with known risk factors for osteoporotic fractures and implies validity in our MOF definitions.31
A limitation of our study is that we could not verify if the MOFs ascertained in this study were osteoporotic fractures or pathologic fractures at sites of bone metastases. This risk was partially mitigated by selecting a cohort of patients with cancer who had a low rate of bone metastasis. We excluded pathologic fracture codes, although misclassification of pathologic and osteoporotic fractures is frequent in administrative claims data.32 While we cannot be certain that all incident fractures in this study were non-pathologic, existing literature from multiple myeloma, prostate cancer, breast cancer and other solid tumours shows that both osteoporotic and pathologic fractures are prevented with antiresorptive bone agents such as zoledronic acid and denosumab and these same agents have been effective at preventing cancer treatment-induced bone loss.27 29 33–36 We were able to examine glucocorticoid use only in the outpatient setting. Thus, glucocorticoids used in hospital would not be captured. Further, the results of this study need to be validated in other cancer groups and populations and additional factors such as body mass index, a family history of osteoporosis, smoking status and alcohol use need to be considered.
Conclusion
MOFs increase after ICI initiation and may represent a new irAE of ICI therapy. Further research is needed to understand the direct causal effects of ICI treatment on bone biology, bone mineral density and fracture risk.
Contributors: CY and MES-A conceived the study. CY, MES-A, JIR, BZ, WDL and HZ created the analysis plan. BZ conducted the statistical analysis. CY wrote the first draft of the manuscript. All authors were involved in the interpretation of the results and editing the manuscript. MES-A is the guarantor.
Funding: This research was supported by funds from the University Cancer Foundation and the Duncan Family Institute for Cancer Prevention and Risk Assessment via a Cancer Survivorship Institutional Research Grant at the University of Texas MD Anderson Cancer Center and by MD Anderson’s National Cancer Institute Cancer Center Support Grant (P30 CA016672). NA-W has a career award from the National Institute of Allergy and Infectious Diseases (K01AI163412).
Competing interests: MES-A has received consultant fees in the past 12 months from Pfizer, Celgene and Syneos Health, unrelated to this work. BZ works at Medasource, providing statistical consulting services for Johnson & Johnson Pharmaceutical company. Other authors have nothing to disclose.
Patient and public involvement: Patients and/or the public were not involved in the design, or conduct, or reporting, or dissemination plans of this research.
Provenance and peer review: Not commissioned; externally peer reviewed.
Supplemental material: This content has been supplied by the author(s). It has not been vetted by BMJ Publishing Group Limited (BMJ) and may not have been peer-reviewed. Any opinions or recommendations discussed are solely those of the author(s) and are not endorsed by BMJ. BMJ disclaims all liability and responsibility arising from any reliance placed on the content. Where the content includes any translated material, BMJ does not warrant the accuracy and reliability of the translations (including but not limited to local regulations, clinical guidelines, terminology, drug names and drug dosages), and is not responsible for any error and/or omissions arising from translation and adaptation or otherwise.
Data availability statement
Data may be obtained from a third party and are not publicly available.
Ethics statements
Patient consent for publication:
Not applicable.
Ethics approval:
This study involves human participants but was deemed to be exempt by the institutional review board at the University of Texas MD Anderson Cancer Center, as it only included deidentified claims data (protocol PA14-0949). Individual patient consent was waived as we used deidentified administrative health data.
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