Original Research Osteoporosis Therapy After Fracture in Elderly Men Angela J. Shepherd, MD, Bret T. Howrey, PhD, Alvah R. Cass, MD, SM, and Gregg S. Wilkinson, PhD, MA Abstract Objective: To report the effect of osteoporosis treatment on the rate of subsequent fractures among older men after fragility fracture. Methods: Analysis of claims data of 10,608 men 65 years of age who had a fracture that occurred during 2001 2005. Subsequent fractures, prescription drugs dispensed, procedures, therapies, and comorbidities were compared for men who received osteoporosis treatment and those who did not. Results: 4.5% of men (n = 478) received treatment. The rate of subsequent fracture was 13.5% in the treated men and 10.8% in the untreated men. Stratification by site of fracture or age at fracture did not affect results. There was no difference in number of days to subsequent fracture in the treated and untreated men. Conclusions: Few men receive treatment after an osteoporotic fracture and adherence to treatment was poor. There was no reduction in subsequent fracture with osteoporosis pharmacotherapy. The low treatment rate precludes definitive conclusions about efficacy in the clinical setting but may suggest a lack of consensus among practicing physicians about the utility of treatment in elderly men with fragility fractures. Osteoporosis is responsible for significant morbidity and mortality in men [1]. Men who have experienced a vertebral fracture have a fourfold increase in risk for subsequent fractures, and men with other fractures have a twofold increased risk for future fractures [2 5]. Antiresorptive agents are consistently associated with a 25% to 30% reduction in primary and subsequent fractures in postmenopausal women [6 11]. However, the literature is limited regarding the efficacy of antiresorptive agents for secondary prevention in men with prevalent fractures. Two studies reported good efficacy of antiresorptives for primary prevention of vertebral fractures in men with osteoporosis [12,13]. In both studies, men with pre-existing osteoporotic fractures made up approximately 50% of both treatment and control groups, with reductions of about 60% for new vertebral fractures in the treatment groups reported. More recently, a 24-month double-blind, placebo-controlled study of men with primary or hypogonadism-associated osteoporosis reported a 67% reduced risk of new morphometric vertebral fracture among men receiving the intervention (zoledronic acid once yearly). Because of the small number of fractures, neither clinical vertebral fractures nor nonvertebral fractures were reduced to a statistically significant degree [14]. In a randomized controlled trial of secondary fracture prevention after hip fracture in a population that included 75% women and 25% men, an overall 35% risk reduction was reported in patients treated with zoledronic acid. The rates of secondary vertebral and nonvertebral fractures were reduced significantly [8]. Despite the availability and likely efficacy of antiresorptive agents in the treatment of osteoporotic-related fractures, few men receive treatment after a low-impact fracture [15 17]. The objective of our study was to measure treatment rates and the effect of osteoporotic therapy on the rate of subsequent fracture among men after low-impact fracture. METHODS Data Source We conducted our study using a large US claims and integrated laboratory database that included commercially insured patients from all 50 states (Clinformatics Data Mart, OptumInsight Life Sciences). These data include de-identified patients and physicians and include claims for inpatient and outpatient care, pharmaceuticals, and durable medical equipment for 13 million annual lives. Study Population First we identified men aged 65 years and older who were enrolled between 1 January 2001 and 31 Decem- From the Department of Family Medicine, The University of Texas Medical Branch, Galveston, TX. www.jcomjournal.com Vol. 20, No. 7 July 2013 JCOM 303
Osteoporosis Therapy ber 2005. Because we examined men 65 and older, our sample included men with primary health insurance coverage through commercial insurance and those on Medicare who participated in supplemental plans. Next, we identified men who had an index fracture during the study period (n = 28,662) who were also continuously enrolled for at least 6 months prior to and 6 months following the index fracture. Fractures were determined based on the reported International Classification of Diseases, 9th Revision (ICD-9-CM) codes on the inpatient or outpatient claim. (See Appendix for a complete listing of IDC-9-CM codes used.) For the purposes of this study, fracture was defined as any closed fracture, except of the skull, face, finger, ankle, or toe, that appeared as a billed diagnosis during the study period with no claim for a fracture in the preceding 6 months. In the multicenter Study of Osteoporotic Fractures of 9704 nonblack women 65 years of age and older, these types of fractures (wrist, foot, humerus, intertrochanteric region of the hip, rib, toe, leg, pelvis, hand, clavicle and vertebral body) were found to be significantly related to reduced appendicular bone mass [18]. We excluded men who received care in hospice, skilled nursing, or rehabilitation facilities because pharmaceutical claims information was not available during those periods. In addition, we excluded any men diagnosed with co-existing cancer codes associated with bony metastasis in the 6 months prior to the index fracture [19] and those whose index fracture was associated with an ICD-9-CM E-code suggesting high-impact trauma (eg, transportation accidents and falls from more than a standing height). The E-code list is available upon request. We also excluded men who had multiple fractures in different body parts or in the same area within 1 week of the index fracture, as these diagnoses are suggestive of high-impact trauma. Finally, we excluded men who had a claim for osteoporosis treatment in the 6 months preceding the index fracture. The final cohort was 10,608 men: 478 treated and 10,130 untreated. We followed treated and untreated men from the date of the index fracture. Follow-up ended on the date of diagnosis of a subsequent fracture, disenrollment, or the end of the study (31 December 2005). Dependent Variable Our main outcome was a subsequent fracture following the index fracture. Subsequent fractures were determined using the same criteria as those used for index fractures. Subsequent fractures whose ICD-9-CM codes (first 4 digits) did not match the index fracture were considered true second fractures. In cases of vertebral fractures, if the index fracture was not otherwise classifiable by location as lumbar, thoracic, or cervical, then all subsequent claims for vertebral fractures were excluded due to inability to definitively adjucate new fractures versus claims relating to the index vertebral fracture. To verify claims associated with second fractures as unique and not follow up claims relating to the index fracture, fracture claims at the same site were required to have an associated Current Procedural Terminology (CPT) code describing treatment of the fracture in order to be considered subsequent fracture. Physician adjudication of subsequent fracture claims was done at 4 key points in the algorithm (Figure 1). Two family physicians (Cass and Shepherd) independently reviewed claims to determine accuracy of allocation into True subsequent fracture or Not subsequent fracture groups: (1) 100 cases of subsequent fracture claims within 90 days of index fracture were reviewed, (2) all 21 claims of subsequent fractures more than 90 days from the index fracture with the same diagnostic codes as index fracture and CPT codes were reviewed, (3) 100 claims of subsequent fractures more than 90 days with the same diagnostic codes as index fracture without CPT codes were reviewed, and (4) all 71 claims with nonspecific vertebral codes either as index or subsequent fracture. Each adjucation confirmed the likelihood that the fractures were correctly identified. The sensitivity of medical service claims to correctly classify fracture has been reported as 85%, with a range of 25% for thorax (rib or sternum) fractures to 97% for hip fractures. Underreporting is not common as claims are linked to physician payment and false-positive reporting is also unlikely due to the high penalty for fraudulent claims [20]. Covariates Our main independent variable was a filled prescription for an osteoporosis treatment, as determined by the presence of a prescription in the pharmacy claims. We considered treatment to be any bisphosphonate (alendronate, etidronate, ibandronate, risedronate, or zoledronic acid), calcitonin, or teriparatide. Using an intention-to-treat model, men were considered treated if the pharmacy claims indicated that a prescription for osteoporosis treatment was filled at least once in the 6 months following the index fracture. Men whose treatment was initiated 304 JCOM July 2013 Vol. 20, No. 7 www.jcomjournal.com
Original Research 4 digits Dx codes match n = 1441 CPT codes n = 21* No CPT codes n = 1420* Subsequent Fx No Fx > 90 days n = 2645 Specific Fx Codes n = 1133 Subsequent Fx With subsequent Fx codes n = 5936 No match N = 1204 Nonspecific vertebral codes n = 71* Unconfirmed Fx n = 66 No Fx Men 65+ cohort (n = 10,608) 90 days n = 3291* No Fx Confirmed Fx n = 5 Subsequent Fx No Fx codes n = 4672 No Fx Figure 1. Steps of data extraction for subsequent fracture. Dx = diagnosis; Fx = fracture.* = adjudication points. after the subsequent fracture were not considered treated. The duration of therapy was calculated by counting the number of prescriptions dispensed from the start of therapy to the subsequent fracture date, date of disenrollment, or end of study date. Duration of treatment was modeled as a continuous variable. Changes from one prescription for osteoporosis treatment to another were considered as continuous for analysis of treatment duration. We adjusted for potential confounders: age, year of index fracture, index fracture site, osteoporosis diagnosis, risk of secondary osteoporosis, tertiary tricyclic antidepressants, benzodiazepines, selective serotonin reuptake inhibitors, type 2 diabetes, COPD/asthma, and depressive disorders. Additional adjustments were made for indicators of frailty or fall risk: procedure claims for physical therapy and mobility procedures, durable medical equipment, diagnoses of abnormal gait, syncope and debility. Finally, we adjusted for medications associated with falling or decreased bone density: hydrocodone/ codeine containing analgesics, prednisone and proton pump inhibitors. Statistical Analysis We first generated nonparametric Kaplan-Meier curves to examine the differences between the treated and untreated groups in probability of subsequent fracture over time. We then performed semiparametric Cox proportional hazards models to estimate the difference in the hazard of a subsequent fracture for the treated and untreated groups. The number of days from index fracture to subsequent fracture was considered the primary endpoint. Men were censored at the end of the study period or end of their enrollment in the insurance plan. Models were first run for the whole sample and then stratified by index fracture site: hip, spine, and other. Initial models included only the treatment variable. The next set of www.jcomjournal.com Vol. 20, No. 7 July 2013 JCOM 305
Osteoporosis Therapy models added age, and the third set of models added the remaining covariates. The proportionality assumption was tested through examination of scaled Schoenfeld residuals and was found not to be violated [21]. RESULTS A total of 28,662 men had a study-defined fracture between 2001 and 2005. After exclusions of concurrent users of osteoporosis treatment, removal of men who did not have adequate time in the study, removal of men involved in accidents, with cancer diagnoses that can metastasize to bone and multiple concurrent fractures suggestive of high trauma, the final sample included 10,608 men. Of that group, 478 men received treatment within the first 6 months after fracture and 10,130 men did not receive treatment. Table 1 shows the characteristics of the study population in the 6 months prior to index fracture. Overall, the average age of the men at index fracture was 75 years. The proportion of men who received treatment was 4.51%. Mean number of years of continuous enrollment for treated and untreated men was 4.4 years, with a standard deviation of 1.6 years. The diagnosis of osteoporosis was higher in the treated group (11%) compared with the untreated group (2.5%). Treated men were more likely to have filled prescriptions for antidepressants (tricyclics and selective serotonin reuptake inhibitors), narcotic analgesics, proton pump ihibitors and oral prednisone. No differences were found between the treated and untreated men for most of the chronic conditions examined. COPD was the most notable exception. 28% of the treated men had COPD compared to 16% of the untreated men. Arthropathies, syncope, debility and depression were also slightly more prevalent in the treated men. A total of 1159 men (10.92%) were determined to have a subsequent fracture. The average time from index to second fracture was 435 days for the treated group and 403 days for the untreated group. Treated men filled the initial prescription 55 to 59 days post-fracture; mean length of treatment during follow-up was 478 days (16 months): 491 days (16.3 months) in the treated men with subsequent fracture and 380 days (12.7 months) in the treated men without subsequent fracture. 24% of the men who had a claim for the initial prescription had no more osteoporosis treatment prescription claims after the first prescription filling. Ad hoc analyses of the men who sustained a subsequent fracture (not included in tabled results) revealed that in the 6 months preceeding the subsequent fracture, these men were three times more likely to have received benzodiazepines (9.3% vs 3.4%) and twice as likely to have received narcotic analgesics (23% vs 13%) or prednisone prescriptions (6% vs 2.7%). Cox proportional hazard ratios of subsequent fracture by index fracture site are presented in Table 2. Hazard ratios for subsequent fractures tended to be greater for men with vertebral index fractures, but there was no difference in hazard ratios between treated and untreated men in crude, age-adjusted or fully adjusted models. Stratification of subsequent fracture by age (5-year intervals) resulted in hazard ratios for men 65 to 69 years of age of 0.80, (95% CI, 0.36 1.75), for men 70 to 74 years of age of 1.15, (95% CI, 0.60 2.21), for men 75 to 79 years of age of 1.18, (95% CI, 1.09-3.00), and for men 80 years of age or older of 0.96 (95% CI, 0.66 1.42). Figure 2 shows the time to subsequent fracture for treated vs. untreated men. There was no difference in the number of days to subsequent fracture between the treated and untreated group as shown by the Kaplan-Meier curves. DISCUSSION This report examined the effect of osteoporosis treatment following an index fracture on the occurrence of subsequent fracture in insured older men in the United States. We found very low treatment rates (4.5%) and suboptimal adherence, with only 76% refilling the prescription after initiation of therapy. In the limited number of men who initiated treatment, the results of this study failed to demonstrate a reduction in subsequent fractures (all sites). There were 13.6% subsequent fractures in treated men vs 10.8% in untreated men. Limitations Our study has numerous limitations, including the small number of men who received treatment and poor compliance rate, which limits the power to detect differences between treated and untreated men. A large cohort study by Siris et al reported that a sample size of more than 30,000 compliant and noncompliant individuals was needed to detect a difference in fracture rates of 10% and 8.5% [24]. Regarding treatment biases, several characteristics of our treated group suggest that these men may have been more frail, more likely to fall, and more prone to fracture than the untreated men. Men in the treated group were 306 JCOM July 2013 Vol. 20, No. 7 www.jcomjournal.com
Original Research Table 1. Characteristics of Study Population During 6 Months Prior to Index Fracture Treatment No Treatment Total n % n % n Study subjects 478 4.51 10130 95.49 10608 Mean age at index fracture, yr 76.11 74.92 Number of days enrolled ± SD 1654 544 1611 570 10608 Osteoporosis diagnosis 51 10.67 254 2.51 305 Risk of secondary osteoporosis by diagnosis* 30 6.28 599 5.52 589 Fall-risk diagnosis 213 44.56 4236 41.82 4449 Medications associated with increased risk Tertiary tricyclic antidepressant 24 5.02 247 2.44 271 Benzodiazepine 65 13.60 791 7.81 856 Selective serotonin reuptake inhibitor 67 14.02 812 8.02 879 Narcotic analgesics 182 38.08 2402 23.71 2584 Proton pump inhibitors 28 5.86 288 2.84 316 Oral prednisone 68 14.23 452 4.46 520 Chronic medical conditions Heart disease 128 26.78 2522 24.90 2650 Hypertension 219 45.82 4605 45.46 4824 Hyperlipidemia 134 28.03 3134 30.94 3268 COPD/asthma 134 28.03 1582 15.62 1716 Arthropathies 33 6.90 432 4.26 2180 Osteoarthritis 141 29.50 3066 30.27 3207 Syncope 38 7.95 541 5.34 579 Abnormal gait 140 29.29 2391 23.60 2531 Debility 52 10.88 689 6.80 741 Depressive disorders 33 6.90 432 4.26 465 Diabetes type 2 81 3.77 397 4.69 478 Other Frailty index 12 2.51 173 1.71 185 Durable medical equipment 50 10.46 2794 27.58 2844 *Includes hyperthyroidism, hyperparathyroidism, Cushing s syndrome, cirrhosis, chronic kidney disease, and testicular hypofunction. Includes Parkinsonism, rheumatoid arthritis, osteoarthritis, dementia, alcoholism, type 1 diabetes mellitus, and stroke. Includes procedural codes for mobility issues (G0151,A0130, A0425, S0209, S5130, S9131, T1019, T1021) and physical therapy (97001, 97010, 97012, 97014, 97035, 97110, 97112, 97140, 97530, G0283). p value significant at < 0.01. statistically more likely to have a pre-existing diagnosis of osteoporosis, a major risk factor for fracture. In addition, men in the treated group were more likely to be taking medications that adversely affect bone density, ie, selective serotonin reuptake inhibitors [25 29], proton pump inhibitors [30 34], and prednisone [35,36]. Treated men were also more likely to be on medications associated with falling, such as tricyclic antidepressants, benzodiazepines, and narcotic analgesics [26,28,29,37]. Finally, men in the treated group were more likely to be diagnosed with debility, which is synonymous with at least a temporary state of frailty. However, after accounting for these observed differences in the final adjusted model, we detected no apparent benefit of treatment fol- www.jcomjournal.com Vol. 20, No. 7 July 2013 JCOM 307
Osteoporosis Therapy Table 2. Cox Proportional Hazard Ratios Modeling the Association of Treatment with Hazard of Subsequent Fracture Site of Index Fracture n Subsequent Fractures Person- Years Hazard Ratio (95% Confidence Interval) Treatment Only Age Adjusted Fully Adjusted* Hip 1468 289 2597 1.21 (0.671 2.19) 1.24 (0.68 2.24) 1.18 (0.63 2.22) Spine 1328 143 2638 1.53 (0.99 2.37) 1.48 (0.95 2.30) 1.47 (0.92 2.36) Other 7812 727 15978 1.19 (0.83 1.71) 1.06 (0.74 1.52) 0.94 (0.65 1.37) Overall 10,608 1159 21,213 1.27 (0.99 1.63) 1.17 (0.91 1.51) 1.14 (0.88 1.48) *Models adjusted for osteoporosis, fall risk diagnosis, tricyclic antidepressants, benzodiazepines, SSRIs, hydrocodone, PPIs, prednisone, heart disease, hypertension, hyperlipidemia, COPD, arthropathy, osteoarthritis, syncope, abnormal gait, debility, depression, frailty, durable medical equipment. lowing an osteoporotic fracture. While the hazard ratios declined in the final adjusted model, the overall change in magnitude suggests that the impact of the factors that may have affected treatment decisions was small. Duration of treatment is also an important factor in prevention; studies in osteoporotic women have shown that about 15 months of osteoporosis treatment is required before any difference is seen in hip fracture rates between treated and untreated women [38]. The average length of treatment in our study was 16 months. Other limitations include those inherent in claims data research. Residual confounding is a potential limitation of claims data research. We took steps to minimize this by restricting the entire cohort to men who had sustained an index fragility fracture, making treated and untreated men more comparable. We also required untreated men to be in the same period of cohort entry as treated men. Administrative data also limits information on ethnicity/race, use of over-the-counter agents such as calcium or vitamin D, family history, smoking, prior fractures not contained in the record, weight, results of bone mineral density measurements or radiographs, height, and body mass index, and frailty. Again, we attempted to manage many of these limitations by requiring all men to have had already sustained a fragility fracture; however, it is not possible to estimate how comparable the 2 groups were on unreported variables. Finally, we attempted to minimize the lack of ability to quantify frailty directly by examining CPT codes for physical therapy, durable medical equipment for walkers and canes, and diagnosis codes for abnormal gait, syncope and debility as indirect measures of frailty. Our study population was limited to insured men 65 years of age and older. In addition, men who received care in an inpatient skilled nursing facility or nursing home were necessarily excluded due to lack of prescriptive information needed to determine treatment status. Because Medicare is available at age 65, our study findings are most relevant to men 65 years of age with Medicare and supplementary commercial health insurance. Claims data may contain coding errors, resulting in misclassification of fractures. We attempted to minimize this type of error by having 2 physicians adjudicate approximately 300 cases of subsequent fracture claims. Claims with codes that were nonspecific (for either index or subsequent vertebral fracture) were excluded because it was not possible to ascertain whether the later claims were related to the index vertebral fracture or a second vertebral fracture. This requirement may have resulted in underestimating subsequent vertebral fractures. Finally, a limitation in our study is the lack of ability to control disenrollment or dropout from the database. One of the challenges encountered in working with private insurance data for men over the age of 65 is disenrollment due to Medicare eligibility. It is unclear to what extent such disenrollment impacts both the numerator and denominator. However, assuming the rate of dropout is relatively uniform among the treated and untreated men, calculations based on such data are stable. In addition, because this study utilized prescription fills that were not limited to the Medicare spending limit (AKA donut hole ), the results maintain high specificity. Comparison with Other Studies Our findings are similar to a report by Cree in a cohort of hip fracture patients made up of 26% men. In their report of 356 treated patients during 1996 2001, treatment did not change the rate of subsequent hip fracture rates 308 JCOM July 2013 Vol. 20, No. 7 www.jcomjournal.com
Original Research 1.00 0.75 Probability 0.50 Not Treated Treated p = 0.06 0.25 0.00 0 500 1000 1500 2000 2500 No. of Days Figure 2. Kaplan-Meier plot of second fracture-free survival. Survival time starts (0) at day 90 following the index fracture. (6% vs. 4%) with a reported adherence rate of 62% at 1.5 years [39]. All men who received treatment in the study received bisphosphonates. Like ours, their study took place in a real-world setting and had low use of osteoporosis treatment. The fact that neither study was able to show differences when studying small numbers (< 500) patients may likely reflect power issues. Our findings did not concur with those from 3 randomized controlled trials looking at primary prevention of fractures in men. In these studies (which included approximately 50% of men with prior osteoporotic fractures), alendronate treatment resulted in a 60% reduction for new vertebral fractures. New nonvertebral fractures were not reduced significantly [12,13]. The men in both controlled trials were considerably younger (57 years [12] and 63 years [13]) than those in our study (75 years). In these controlled trials, compliance was not an issue, nor was length of follow-up time, as all men were required to have at least 2 years of follow-up with monitored treatment. Our study was done at a time when zoledronic acid was rarely used for men, but in the 2007 report of the HORIZON Recurrent Fracture Trial involving 2127 persons (508 men) with hip fracture, Lyles et al reported a significant (35%) risk reduction for any new clinical fracture with zoledronic acid [8]. In a 2013 report on primary prevention of fracture by Boonen et al involving 1199 men (574 in the intention to treat group), zolendronic acid was associated with a 67% risk reduction in morphometric vertebral fractures after 2 years; reductions were also reported in men with clinical vertebral or nonvertebral fractures, but these reductions did not reach significance due to the small overall number of fractures [14]. These studies suggests that treatment with intravenous zoledronic acid and 100% compliance, we can expect to see some reduction in subsequent fractures. Conclusions The current claims data study of 10,608 elderly men diagnosed with a fragility fracture failed to show significant reductions in fractures after treatment with (mostly) oral bisphosphonates; this lack of significance may be due to insufficient power to detect differences due to small numbers of treated men (4.5%) and a relatively rare event as the endpoint (subsequent fracture). The lack of treatment benefit observed in our study may have been influenced by the advanced age and cormorbidity burden; the low treatment rates, suboptimal compliance, and length of duration of treatment prior to a subsequent fracture likely influenced results. To illustrate this point, the mean time to treatment was about 60 days; the mean time to a www.jcomjournal.com Vol. 20, No. 7 July 2013 JCOM 309
Osteoporosis Therapy subsequent fracture was 435 days. The intervening time interval may have been too short to realize the benefit of treatment. Lack of treatment post-fracture may carry adverse health consequences for patients as well as increased health care costs for the health care system. If patients are to benefit from the fracture risk reductions reported in clinical trials, clinicians may want to consider yearly intravenous therapy and collaborate with researchers to discover novel ways to increase compliance with long-term oral medications. Further large scale studies are needed if we are to better understand how to achieve a reduction of subsequent nonvertebral fractures in elderly men. Acknowledgment: We would like to thank Karen Pierson, Assistant Director of Research Support Services, for her assistance with data management. Corresponding author: Angela J. Shepherd, MD, Dept. of Family Medicine, The University of Texas Medical Branch, 301 University Blvd., Galveston, TX 77555, ajshephe@ utmb.edu. Funding/support: This study was conducted with the support of the Institute for Translational Sciences at the University of Texas Medical Branch, supported in part by a Clinical and Translational Science Award (UL1TR000071) from the National Center for Advancing Translational Sciences, National Institutes of Health. Financial disclosures: None. Author contributions: conception and design, AJS, BH, ARC, GSW; analysis and interpretation of data, AJS, BH, ARC, GSW; drafting of article, AJS, BH, GSW; critical revision of the article, AJS, BH, ARC, GSW; statistical expertise, BH, ARC, GSW; obtaining of funding, GSW; collection and assembly of data, AJS, BH. References 1. Roerholt C, Eiken P, Abrahamsen B. Initiation of antiosteoporotic therapy in patients with recent fractures: a nationwide analysis of prescription rates and persistence. 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Original Research Appendix. ICD-9-CM codes Code Description Code Description Spine 805 VERTEBRL FX W/O CORD INJ 805.06 FX C6 VERTEBRA-CLOSED 805.0 FX CERVICAL VERTEBRA-CL 805.07 FX C7 VERTEBRA-CLOSED 805.00 FX CERVICAL VERT NOS-CL 805.08 FX MULT CERVICAL VERT-CL 805.01 FX C1 VERTEBRA-CLOSED 805.2 FX DORSAL VERTEBRA-CLOSE 805.02 FX C2 VERTEBRA-CLOSED 805.4 FX LUMBAR VERTEBRA-CLOSE 805.03 FX C3 VERTEBRA-CLOSED 805.6 FX SACRUM/COCCYX-CLOSED 805.04 FX C4 VERTEBRA-CLOSED 805.8 VERTEBRAL FX NOS-CLOSED 805.05 FX C5 VERTEBRA-CLOSED Hip 820.00 FX FEMUR INTRCAPS NOS-CL 820.2 PERTROCHANTERIC FX-CLOS 820.01 FX UP FEMUR EPIPHY-CLOS 820.20 TROCHANTERIC FX NOS-CLOS 820.02 FX FEMUR, MIDCERVIC-CLOS 820.21 INTERTROCHANTERIC FX-CL 820.03 FX BASE FEMORAL NCK-CLOS 820.22 SUBTROCHANTERIC FX-CLOSE 820.09 FX FEMUR INTRCAPS NEC-CL 820.8 FX NECK OF FEMUR NOS-CL Other 807.0 FX OF RIB-CLOSED 812.20 FX HUMERUS NOS-CLOSED 807.00 FX RIB NOS-CLOSED 812.21 FX HUMERUS SHAFT-CLOSED 807.01 FX ONE RIB-CLOSED 812.4 FX LOWER HUMERUS-CLOSED 807.02 FX TWO RIBS-CLOSED 812.40 FX LOWER HUMERUS NOS-CL 807.03 FX THREE RIBS-CLOS 812.41 SUPRCONDYL FX HUMERUS-CL 807.04 FX FOUR RIBS-CLOSE 812.42 FX HUMER, LAT CONDYL-CL 807.05 FX FIVE RIBS-CLOSE 812.43 FX HUMER, MED CONDYL-CL 807.06 FX SIX RIBS-CLOSED 812.44 FX HUMER, CONDYL NOS-CL 807.07 FX SEVEN RIBS-CLOS 812.49 FX LOWER HUMERUS NEC-CL 807.08 FX EIGHT/MORE RIB-CLOSED 813.0 FX UPPER RADIUS/ULNA-CL 807.09 FX MULT RIBS NOS-CLOSED 813.00 FX UPPER FOREARM NOS-CL 808 PELVIC FX 813.01 FX OLECRAN PROC ULNA-CL 808.0 FX ACETABULUM-CLOS 813.02 FX CORONOID PROC ULNA-CL 808.2 FX OF PUBIS-CLOSED 813.03 MONTEGGIA'S FX-CLOSED 808.41 FX OF ILIUM-CLOSED 813.04 FX UPPER ULNA NEC/NOS-CL 808.42 FX ISCHIUM-CLOSED 813.05 FX RADIUS HEAD-CLOSED 808.8 PELVIC FX NOS-CLOS 813.06 FX RADIUS NECK-CLOSED 810.0 FX CLAVICLE-CLOSED 813.07 FX UP RADIUS NEC/NOS-CL 810.00 FX CLAVICLE NOS-CLOSED 813.08 FX UP RADIUS W ULNA-CLOS 810.02 FX CLAVICLE SHAFT-CLOSED 813.2 FX RADIUS/ULNA SHAFT-CL 810.03 FX CLAVICL, ACROM END-CL 813.20 FX SHAFT FOREARM NOS-CL 812.0 FX UPPER HUMERUS-CLOSED 813.21 FX RADIUS SHAFT-CLOSED Appendix. 812.00 Data FX UP Collection END HUMERUS Tool NOS-CL for VAP in Pediatric Post-Acute 813.22 Care (continued) FX ULNA SHAFT-CLOSED 812.01 FX SURG NCK HUMERUS-CLOS 813.23 FX SHAFT RAD W ULNA-CLOS 812.02 FX ANATOM NCK HUMERUS-CL 813.4 FX LOWER RADIUS/ULNA-CL Code Description Code Description 812.03 FX GR TUBEROS HUMERUS-CL 813.40 FX LOWER FOREARM NOS-CL 812.09 FX UPPER HUMERUS NEC-CL 813.41 COLLES' FX-CLOSED 812.2 FX HUMERUS SHAFT/NOS-CL Other 813.42 FX DISTAL RADIUS NEC-CL 813.43 FX DISTAL ULNA-CLOSED 821.0 FX FEMUR SHAFT/NOS-CLOSE 813.44 FX LOW RADIUS W ULNA-CL 821.00 FX FEMUR NOS-CLOSED 813.8 FX RADIUS/ULNA NOS-CLOSE 821.01 FX FEMUR SHAFT-CLOSED 813.80 FX FOREARM NOS-CLOSED 821.2 FX LOWER END FEMUR-CLOSE 813.81 FX RADIUS NOS-CLOSED 821.20 FX LOW END FEMUR NOS-CL 813.82 FX ULNA NOS-CLOSED 821.21 FX FEMORAL CONDYLE-CLOSE 813.83 FX RADIUS W ULNA NOS-CL 821.22 FX LOW FEMUR EPIPHY-CLOS 814.00 FX CARPAL BONE NOS-CLOSE 821.23 SUPRACONDYL FX FEMUR-CL 814.01 FX NAVICULAR, WRIST-CLOS 821.29 FX LOW END FEMUR NEC-CL 814.02 FX LUNATE, WRIST-CLOSED 823.00 FX UPPER END TIBIA-CLOSE 814.03 FX TRIQUETRAL, WRIST-CL 823.01 FX UPPER END FIBULA-CLOS 814.04 FX PISIFORM-CLOSED 823.02 FX UP TIBIA W FIBULA-CL 814.05 FX TRAPEZIUM BONE-CLOSED 823.2 FX SHAFT TIB/FIB-CLOSED 814.06 FX TRAPEZOID BONE-CLOSED 823.8 FX TIBIA/FIBULA NOS-CLOS 814.07 FX CAPITATE BONE-CLOSED 825.0 FX CALCANEUS-CLOSE 814.08 FX HAMATE BONE-CLOSED 825.2 FX TARSL/METATARS NEC-CL 814.09 FX CARPAL BONE NEC-CLOSE 825.20 FX FOOT BONE NOS-CLOSED 815.00 FX METACARPAL NOS-CLOSED 825.21 FX ASTRAGALUS-CLOSED 815.01 FX 1ST METACARP BASE-CL 825.22 FX NAVICULAR, FOOT-CLOS 815.02 FX METACARP BASE NEC-CL 825.23 FX CUBOID-CLOSED 815.03 FX METACARPAL SHAFT-CLOS 825.24 FX CUNEIFORM, FOOT-CLOS 815.04 FX METACARPAL NECK-CLOSE 825.25 FX METATARSAL-CLOSED 815.09 MULT FX METACARPUS-CLOSE 825.29 FX FOOT BONE NEC-CLOSED 818.0 FX ARM MULT/NOS-CLOSED 827.0 FX LOWER LIMB NEC-CLOSED 819.0 FX ARMS W RIB/STERNUM-CLOSED www.jcomjournal.com Vol. 20, No. 7 July 2013 JCOM 311
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