Are Quality Scores in the Centers for Medicaid and Medicare Services Merit-based Incentive Payment System Associated With Outcomes After Outpatient Orthopaedic Surgery?

BACKGROUND: The Medicare Merit-based Incentive Payment System (MIPS) ties reimbursement incentives to clinician performance to improve healthcare quality. It is unclear whether the MIPS quality score can accurately distinguish between high-performing and low-performing clinicians. QUESTIONS/PURPOSES: (1) What were the rates of unplanned hospital visits (emergency department visits, observation stays, or unplanned admissions) within 7, 30, and 90 days of outpatient orthopaedic surgery among Medicare beneficiaries? (2) Was there any association of MIPS quality scores with the risk of an unplanned hospital visit (emergency department visits, observation stays, or unplanned admissions)? METHODS: Between January 2018 and December 2019, a total of 605,946 outpatient orthopaedic surgeries were performed in New York State according to the New York Statewide Planning and Research Cooperative System database. Of those, 56,772 patients were identified as Medicare beneficiaries and were therefore potentially eligible. A further 34% (19,037) were excluded because of missing surgeon identifier, age younger than 65 years, residency outside New York State, emergency department visit on the same day as outpatient surgery, observation stay on the same claim as outpatient surgery, and concomitant high-risk or eye procedures, leaving 37,735 patients for analysis. The database does not include a list of all state residents and thus does not allow for censoring of patients who move out of state. We chose this dataset because it includes nearly all hospitals and ambulatory surgery centers in a large geographic area (New York State) and hence is not limited by sampling bias. We included 37,735 outpatient orthopaedic surgical encounters among Medicare beneficiaries in New York State from 2018 to 2019. For the 37,735 outpatient orthopaedic surgical procedures included in our study, the mean ± standard deviation age of patients was 73 ± 7 years, 84% (31,550) were White, and 59% (22,071) were women. Our key independent variable was the MIPS quality score percentile (0 to 19th, 20th to 39th, 40th to 59th, or 60th to 100th) for orthopaedic surgeons. Clinicians in the MIPS program may receive a bonus or penalty based on the overall MIPS score, which ranges from 0 to 100 and is a weighted score based on four subscores: quality, promoting interoperability, improvement activities, and cost. The MIPS quality score, which attempts to reward clinicians providing superior quality of care, accounted for 50% and 45% of the overall MIPS score in 2018 and 2019, respectively. Our main outcome measures were 7-day, 30-day, and 90-day unplanned hospital visits after outpatient orthopaedic surgery. To determine the association between MIPS quality scores and unplanned hospital visits, we estimated multivariable hierarchical logistic regression models controlling for MIPS quality scores; patient-level (age, race and ethnicity, gender, and comorbidities), facility-level (such as bed size and teaching status), surgery and surgeon-level (such as surgical procedure and surgeon volume) covariates; and facility-level random effects. We then used these models to estimate the adjusted rates of unplanned hospital visits across MIPS quality score percentiles after adjusting for covariates in the multivariable models. RESULTS: In total, 2% (606 of 37,735), 2% (783 of 37,735), and 3% (1013 of 37,735) of encounters had an unplanned hospital visit within 7, 30, or 90 days of outpatient orthopaedic surgery, respectively. Most hospital visits within 7 days (95% [576 of 606]), 30 days (94% [733 of 783]), or 90 days (91% [924 of 1013]) were because of emergency department visits. We found very small differences in unplanned hospital visits by MIPS quality scores, with the 20th to 39th percentile of MIPS quality scores having 0.71% points (95% CI -1.19% to -0.22%; p = 0.004), 0.68% points (95% CI -1.26% to -0.11%; p = 0.02), and 0.75% points (95% CI -1.42% to -0.08%; p = 0.03) lower than the 0 to 19th percentile at 7, 30, and 90 days, respectively. There was no difference in adjusted rates of unplanned hospital visits between patients undergoing surgery with a surgeon in the 0 to 19th, 40th to 59th, or 60th to 100th percentiles at 7, 30, or 90 days. CONCLUSION: We found that the rates of unplanned hospital visits after outpatient orthopaedic surgery among Medicare beneficiaries were low and primarily driven by emergency department visits. We additionally found only a small association between MIPS quality scores for individual physicians and the risk of an unplanned hospital visit after outpatient orthopaedic surgery. These findings suggest that policies aimed at reducing postoperative emergency department visits may be the best target to reduce overall postoperative unplanned hospital visits and that the MIPS program should be eliminated or modified to more strongly link reimbursement to risk-adjusted patient outcomes, thereby better aligning incentives among patients, surgeons, and the Centers for Medicare ad Medicaid Services. Future work could seek to evaluate the association between MIPS scores and other surgical outcomes and evaluate whether annual changes in MIPS score weighting are independently associated with clinician performance in the MIPS and regarding clinical outcomes. LEVEL OF EVIDENCE: Level III, therapeutic study.

Incidence and Risk Factors for Revision Within 1 Year of Primary Carpal Tunnel Release.

BACKGROUND: The annual volume of carpal tunnel release (CTR) in the United States has been estimated to be 577 000 per year. Our objectives were to evaluate the incidence and risk factors for revision CTR within 1 year of primary CTR. METHODS: We identified all adult patients undergoing primary CTR from October 2015 to September 2019 in the New York Statewide Planning and Research Cooperative System database using Current Procedural Terminology (CPT) codes. We used the CPT modifier codes to determine laterality of index and revision procedures. We estimated multivariable hierarchical logistic regression models to evaluate risk factors for revision CTR within 1 year. RESULTS: Of the 80 423 primary CTR procedures, 178 (0.22%) underwent a revision CTR within 1 year of the index surgery. The mean (SD) age of the entire cohort was 58.69 (14.43) years, 61.1% were women, 73.2% were non-Hispanic white, 42.9% were covered through private insurance, and 9.5% had diabetes mellitus. Workers' compensation insurance (odds ratio [OR] = 1.83, 95% confidence interval [CI], 1.13-2.98, P = .02) and simultaneous bilateral CTR (OR = 14.91, 95% CI, 9.62-23.12, P < .001) were associated with revision CTR within 1 year of the index procedure. No models demonstrated an association between endoscopic technique or surgeon volume and revision CTR. CONCLUSIONS: The incidence of revision CTR within 1 year was lower than that previously reported. Patients covered by workers' compensation and those undergoing simultaneous bilateral CTR had higher likelihood of a revision CTR within 1 year, whereas endoscopic technique and surgeon volume were not associated with revision CTR within 1 year.

Association of Total Knee Replacement Removal From the Inpatient-Only List With Outpatient Surgery Utilization and Outcomes in Medicare Patients.

Importance: Little is known about the association of total knee replacement (TKR) removal from the Medicare inpatient-only (IPO) list in 2018 with outcomes in Medicare patients. Objective: To evaluate (1) patient factors associated with outpatient TKR use and (2) whether the IPO policy was associated with changes in postoperative outcomes for patients undergoing TKR. Design, Setting, and Participants: This cohort study included data from administrative claims from the New York Statewide Planning and Research Cooperative System. Included patients were Medicare fee-for-service beneficiaries undergoing TKRs or total hip replacements (THRs) in New York State from 2016 to 2019. Multivariable generalized linear mixed models were used to identify patient factors associated with outpatient TKR use, and with a difference-in-differences strategy to examine association of the IPO policy with post-TKR outcomes relative to post-THR outcomes in Medicare patients. Data analysis was performed from 2021 to 2022. Exposures: IPO policy implementation in 2018. Main Outcomes and Measures: Use of outpatient or inpatient TKR; secondary outcomes included 30-day and 90-day readmissions, 30-day and 90-day postoperative emergency department visits, non-home discharge, and total cost of the surgical encounter. Results: A total of 37 588 TKR procedures were performed on 18 819 patients from 2016 to 2019, with 1684 outpatient TKR procedures from 2018 to 2019 (mean [SD] age, 73.8 [5.9] years; 12 240 female [65.0%]; 823 Hispanic [4.4%], 982 non-Hispanic Black [5.2%], 15 714 non-Hispanic White [83.5%]). Older (eg, age 75 years vs 65 years: adjusted difference, -1.65%; 95% CI, -2.31% to -0.99%), Black (-1.44%; 95% CI, -2.81% to -0.07%), and female patients (-0.91%; 95% CI, -1.52% to -0.29%), as well as patients treated in safety-net hospitals (disproportionate share hospital payments quartile 4: -18.09%; 95% CI, -31.81% to -4.36%), were less likely to undergo outpatient TKR. After IPO policy implementation in the TKR cohort, there were lower adjusted 30-day readmissions (adjusted difference [AD], -2.11%; 95% CI, -2.73% to -1.48%; P < .001), 90-day readmissions ( -3.23%; 95% CI, -4.04% to -2.42%; P < .001), 30-day ED visits ( -2.45%; 95% CI, -3.17% to -1.72%; P < .001), 90-day ED visits (-4.01%; 95% CI, -4.91% to -3.11%; P < .001) and higher cost per encounter ($2988; 95% CI, $415 to $5561; P = .03). However, these changes did not differ from changes in the THR cohort except for increased TKR cost of $770 per encounter ($770; 95% CI, $83 to $1457; P = .03) relative to THR. Conclusions and Relevance: In this cohort study of patients undergoing TKR and THR, we found that older, Black, and female patients and patients treated in safety-net hospitals may have had lesser access to outpatient TKRs highlighting concerns of disparities. IPO policy was not associated with changes in overall health care use or outcomes after TKR, except for an increase of $770 per TKR encounter.

What Factors Are Associated With Revision Cubital Tunnel Release Within 3 Years?

BACKGROUND: It has been shown that patient demographics such as age, payer factors such as insurance type, clinical characteristics such as preoperative opioid use, and disease grade but not surgical procedure are associated with revision surgery to treat cubital tunnel syndrome. However, prior studies evaluating factors associated with revision surgery after primary cubital tunnel release have been relatively small and have involved patients from a single institution or included only a single payer. QUESTIONS/PURPOSES: (1) What percentage of patients who underwent cubital tunnel release underwent revision within 3 years? (2) What factors are associated with revision cubital tunnel release within 3 years of primary cubital tunnel release? METHODS: We identified all adult patients who underwent primary cubital tunnel release from January 1, 2011, to December 31, 2017, in the New York Statewide Planning and Research Cooperative System database using Current Procedural Terminology codes. We chose this database because it includes all payers and nearly all facilities in a large geographic area where cubital tunnel release may be performed. We used Current Procedural Terminology modifier codes to determine the laterality of primary and revision procedures. The mean age of the cohort overall was 53 ± 14 years, 43% (8490 of 19,683) were women, and 73% (14,308 of 19,683) were non-Hispanic White. The Statewide Planning and Research Cooperative System database organization does not include a listing of all state residents and thus does not allow for censoring of patients who move out of state. All patients were followed for 3 years. We developed a multivariable hierarchical logistic regression model to model factors independently associated with revision cubital tunnel release within 3 years. Key explanatory variables included age, gender, race or ethnicity, insurance, patient residential location, medical comorbidities, concomitant procedures, whether the procedure was unilateral or bilateral, and year. The model also controlled for facility-level random effects to account for the clustering of observations among these entities. RESULTS: The risk of revision cubital tunnel release within 3 years of the primary procedure was 0.7% (141 of 19,683). The median time to revision cubital tunnel release was 448 days (interquartile range 210 to 861 days). After controlling for patient-level covariates and facility random effects, and compared with their respective counterparts, the odds of revision surgery were higher for patients with workers compensation insurance (odds ratio 2.14 [95% confidence interval 1.38 to 3.32]; p < 0.001), a simultaneous bilateral index procedure (OR 12.26 [95% CI 5.93 to 25.32]; p < 0.001), and those who underwent submuscular transposition of the ulnar nerve (OR 2.82 [95% CI 1.35 to 5.89]; p = 0.006). The odds of revision surgery were lower with increasing age (OR 0.79 per 10 years [95% CI 0.69 to 0.91]; p < 0.001) and a concomitant carpal tunnel release (OR 0.66 [95% CI 0.44 to 0.98]; p = 0.04). CONCLUSION: The risk of revision cubital tunnel release was low. Surgeons should be cautious when performing simultaneous bilateral cubital tunnel release and when performing submuscular transposition in the setting of primary cubital tunnel release. Patients with workers compensation insurance should be informed they are at increased odds for undergoing subsequent revision cubital tunnel release within 3 years. Future work may seek to better understand whether these same effects are seen in other populations. Future work might also evaluate how these and other factors such as disease severity could affect functional outcomes and the trajectory of recovery. LEVEL OF EVIDENCE: Level III, therapeutic study.

Cell autonomous or systemic EGFR blockade alters the immune-environment in squamous cell carcinomas.

Targeting mutations and amplifications in the EGFR has been successful precision therapy for cancers of the lung, oral cavity and gastrointestinal track. However, a systemic immune reaction manifested by dose-limiting inflammation in the skin and gut has been a consistent adverse effect. To address the possibility that intra-tumoral immune changes contribute to the anti-cancer activity of EGFR inhibition, squamous cancers were produced by syngeneic orthografts of either EGFR null or wildtype mouse primary keratinocytes transduced with an oncogenic H-ras retrovirus. Flow cytometric, RNA and Bioplex immunoassay analyses of the tumor immune milieu were performed. Cancers forming from keratinocytes genetically depleted of EGFR were smaller than wildtype cancers and had fewer infiltrating FoxP3 Treg cells, lower Foxp3 RNA and a lower percentage of CD4 PD1 positive cells indicating a tumor cell autonomous regulation of its microenvironment. Hosts bearing wildtype cancers treated with gefitinib for 1 week showed a trend for smaller tumors. In this short term pharmacological model, there was also a trend to reduced FoxP3 cells and FoxP3 RNA in the tumors of treated mice as well as a substantial increase in the ratio of IL-1A/IL-1RA transcripts. These results suggest that relatively brief systemic inhibition of EGFR signaling alters the immune environment of the targeted cancer. Together these data imply that an EGFR dependent Treg function supports the growth of squamous cancers and is a target for the therapeutic activity of EGFR inhibition.

Accelerated partial breast irradiation through brachytherapy for ductal carcinoma in situ: factors influencing utilization and risks of second breast tumors.

The purpose of this study was to examine influencing factors and outcomes of accelerated partial breast irradiation through brachytherapy (APBIb) versus whole breast irradiation (WBI) for ductal carcinoma in situ (DCIS). From the Surveillance Epidemiology and End Results program of the US National Cancer Institute, we identified 40,749 women who were diagnosed with first primary DCIS between 2002 and 2011 and treated with breast-conserving surgery and radiotherapy. A multi-level logistic regression analysis was performed to estimate odds ratios of APBIb use. Hazard ratios (HRs) of developing ipsilateral breast tumors (IBTs) and contralateral breast tumors (CBTs) were analyzed in 1962 patients with APBIb and 7203 propensity score-matched patients with WBI, using Cox proportional hazards regression. Overall, 2212 (4.5 %) of 40,749 women (the whole cohort) received APBIb. Factors associated with the increased use of APBIb included older age, non-Hispanic white race/ethnicity, smaller tumor size, hormone receptor positivity, comedo subtypes, and urban residence. During the 46-month follow-up, 74 (0.8 %) and 131 (1.4 %) of 9165 propensity score-matched patients developed IBTs and CBTs, respectively. Compared with WBI, APBIb was associated with a significantly increased risk of IBTs (HR 1.74; 95 % CI 1.06-2.85) but not CBTs (OR 0.91; 95 % CI 0.59-1.41). This population-based study suggests that APBIb use for DCIS was influenced by patient and tumor characteristics as well as urbanization of residence. We observed a moderately increased IBT risk associated with APBIb versus WBI, suggesting that APBIb should be used with caution for DCIS before data from randomized controlled trials with long-term follow-ups are available.