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J Am Heart Assoc. 2017 October; 6(10): e006814.
Published online 2017 October 5. doi:  10.1161/JAHA.117.006814
PMCID: PMC5721874

Prediction Score for Anticoagulation Control Quality Among Older Adults

Kueiyu Joshua Lin, MD, ScD, MPH,corresponding author 1 , 2 , 3 Daniel E. Singer, MD, 2 , 3 Robert J. Glynn, PhD, ScD, 1 , 3 Suzanne Blackley, MA, 5 Li Zhou, MD, PhD, 4 , 6 Jun Liu, MD, 1 Gina Dube, PharmD, CACP, RPh, 7 Lynn B. Oertel, MS, ANP‐BC, CACP, 8 and Sebastian Schneeweiss, MD, ScD 1 , 3



Time in the therapeutic range (TTR) is associated with the effectiveness and safety of vitamin K antagonist (VKA) therapy. To optimize prescribing of VKA, we aimed to develop and validate a prediction model for TTR in older adults taking VKA for nonvalvular atrial fibrillation and venous thromboembolism.

Methods and Results

The study cohort comprised patients aged ≥65 years who were taking VKA for atrial fibrillation or venous thromboembolism and who were identified in the 2 US electronic health record databases linked with Medicare claims data from 2007 through 2014. With the predictors identified from a systematic review and clinical knowledge, we built a prediction model for TTR, using one electronic health record system as the training set and the other as the validation set. We compared the performance of the new models to that of a published prediction score for TTR, SAMe‐TT 2R2. Based on 1663 patients in the training set and 1181 in the validation set, our optimized score included 42 variables and the simplified model included 7 variables, abbreviated as PROSPER (Pneumonia, Renal dysfunction, Oozing blood [prior bleeding], Staying in hospital ≥7 days, Pain medication use, no Enhanced [structured] anticoagulation services, Rx for antibiotics). The PROSPER score outperformed SAMe‐TT 2R2 when predicting both TTR ≥70% (area under the receiver operating characteristic curve 0.67 versus 0.55) and the thromboembolic and bleeding outcomes (area under the receiver operating characteristic curve 0.62 versus 0.52).


Our geriatric TTR score can be used as a clinical decision aid to select appropriate candidates to receive VKA therapy and as a research tool to address confounding and treatment effect heterogeneity by anticoagulation quality.

Keywords: anticoagulant, atrial fibrillation, quality control, stroke, venous thromboembolism
Subject Categories: Arrhythmias, Atrial Fibrillation, Secondary Prevention, Risk Factors, Anticoagulants

Clinical Perspective

What Is New?

  • In patients aged ≥65 years, our prediction model for anticoagulation control quality outperformed the published score, SAMe‐TT2R2.
  • Time in the therapeutic range was ≥70% (area under receiver operating characteristic curve 0.71 versus 0.57, a significant difference.).

What Are the Clinical Implications?

  • Our prediction score for anticoagulation quality can help clinicians select the appropriate older adult candidates to receive vitamin K antagonist therapy and can provide researchers with a tool to adjust for confounding and to investigate treatment effect heterogeneity due to predicted anticoagulation quality.


Vitamin K antagonist (VKA; eg, warfarin) therapy is an effective anticoagulation option for stroke prevention in patients with nonvalvular atrial fibrillation (AF) and for treatment and secondary prevention of venous thromboembolism (VTE; including deep vein thrombosis and pulmonary embolism).1, 2, 3 The safety and effectiveness of VKAs, however, depends on regular international normalized ratio (INR) monitoring and anticoagulation control quality, often measured by the time in therapeutic range (TTR), for which INR 2.0 to 3.0 is the standard therapeutic range for AF and VTE.4, 5, 6 Patients on VKA with poor anticoagulation quality (ie, low TTR) have been shown to have a higher risk of thromboembolic and bleeding complications and thus a worse risk–benefit ratio.4, 7, 8

Although clinical trials have shown that direct‐acting oral anticoagulants (DOACs) are therapeutically advantageous over or at least noninferior to VKAs,9, 10, 11 clinical equipoise still exists when patients are likely to have good anticoagulation control based on pretreatment characteristics.7, 12 This choice is particularly difficult to make in older adults because DOACs have been associated with a higher risk of major gastrointestinal bleeding than VKAs in the older population.13, 14, 15 Moreover, chronic kidney disease is highly prevalent in older adults,16 which makes lack of routine monitoring tests for DOACs a challenge rather than an advantage because some DOACs are substantially renally excreted (eg, 80% for dabigatran). Consequently, it is critical to understand how patient characteristics are associated with anticoagulation quality so we can identify the ideal candidates for VKA therapy.

In the existing literature, there is only 1 published prediction score for anticoagulation quality: the SAMe‐TT2R2 score.17 It did not consider some clinically important predictors for TTR (eg, polypharmacy, hospitalizations, antibiotic use)18, 19, 20, 21, 22 and was found to have suboptimal performance in external validation populations (area under receiver operating characteristic curve [AUC] for relevant clinical end points <0.6).23, 24, 25 In addition, although the majority of oral anticoagulant users are older adults,3, 18 SAMe‐TT2R2 was developed with 52.7% of the population aged <70 years. Because comorbidity profiles vary substantially by age, the generalizability and applicability of SAMe‐TT2R2 in the older population is unclear.

We aimed to develop and validate a new prediction model for TTR, particularly in patients aged ≥65 years taking VKA for nonvalvular AF or VTE. Because prior studies found that the TTR predictors identified in AF patients were similar to those in VTE patients,18 for clinical simplicity we developed 1 score for both indications but validated the performance in patients with nonvalvular AF and VTE separately.


Data Source

We linked electronic health record (EHR) data from 2 large US academic provider networks with Medicare claims data. The first network consists of 1 tertiary hospital, 2 community hospitals, 17 primary care centers, and 1 anticoagulation clinic that manages VKA‐related care for all patients within the network. The second network includes 1 tertiary hospital, 1 community hospital, 16 primary care centers, and an anticoagulation clinic. Patients in network 1 were used as the training set for the prediction model derivation, and those in network 2 were used as the validation set. The EHR database contains information on patient demographics, diagnosis and procedure codes, medications, lifestyle factors, laboratory data, and various clinical notes. Both inpatient and outpatient EHR data were used in this study. The Medicare claims data contain information on demographics, inpatient and outpatient diagnosis and procedure codes, and dispensed medications.26 This study was approved by Partners HealthCare Institutional Review Board (IRB).

Study Population

In the linked Medicare claims–EHR data, we identified all patients aged ≥65 years with nonvalvular AF or VTE initiating a VKA from January 1, 2007, to December 31, 2014, with no use of any oral anticoagulants (VKAs or DOACs) in the prior 90 days (new user design27). The VKA initiation date was the index (cohort entry) date. The study cohort was required to have at least 180 days of continuous enrollment in Medicare inpatient, outpatient, and prescription benefits with at least 1 EHR encounter with date of service after January 1, 2007, and before the index date. To ensure our ability to assess the primary outcome reliably, patients were required to have at least 5 INR values recorded in the system. To assess whether this requirement would select an unrepresentative cohort, we compared the distributions of the combined comorbidity score28 in those with versus without at least 5 INRs. We computed standardized differences between proportions of each combined comorbidity score category in those with versus without 5 INRs. A standardized difference of <0.1 was used to indicate an acceptable discrepancy.29

Outcome Definition of the Anticoagulation Control

We calculated TTR using Rosendaal's method,30 which assigns an INR value to each day by linear interpolation of successive observed INR values with gaps <56 days. After interpolation, we computed the proportions of time that fell within the therapeutic range (INR 2.0–3.0). We ascertained TTR starting the 29th day after the index date until the earliest of the following: 12 months after the index date, lack of INRs with a gap ≤56 days, death, discontinuation of VKA, or study end (December 31, 2014). We did not assess TTR for the first month because variability of INR values in the first month generally reflects expected fluctuations in INRs during the titration phase of VKA therapy. VKA discontinuation was defined based on an algorithm validated in a prior study in which high agreement with actual VKA use was demonstrated by chart review (κ=0.84).31

Candidate Predictors and Building of the TTR Prediction Model

We conducted a systematic review to identify original articles reporting predictors of anticoagulation control quality (assessed by TTR or INR variability) in users of VKAs, after multivariate adjustment. Figure 1 summarizes the search terms and the selection process. The significant predictors reported by the selected articles, along with variables deemed clinically important to predict anticoagulation quality, were used as the candidate predictors to build our prediction model. Based on these variables, we built a model predicting continuous TTR by Lasso regression with 5‐fold cross‐validation, using the data in the training set.32 We referred to the predicted TTR derived from this model as the geriatric TTR score. To build a simplified model for clinical use, we excluded biophysiologic variables requiring additional testing and used Lasso regression with a Bayesian information criterion, which tends to generate a more parsimonious model than do other criteria.33 The points of the scoring system were the nearest integer proportional to the unstandardized coefficient in this simplified model. All predictors were assessed in the 180 days before (and including) the initiation of a VKA, with the exception of receiving structured anticoagulation management service, which was assessed until 28 days after VKA initiation (immediately before the start of the follow‐up).

Figure 1
Systematic review on significant predictors for anticoagulation quality (TTR). AF indicates atrial fibrillation; INR, international normalized ratio; TTR, time in therapeutic range; VKA, vitamin K antagonist; VTE, venous thromboembolism.

Performance of the Geriatric TTR Score Versus SAMe‐TT2R2

We calculated a coefficient‐based and simplified version of the SAMe‐TT2R2 score for each patient (see Table S1 for details).17 Model performance was compared (1) between the geriatric TTR score and the coefficient‐based SAMe‐TT2R2 score and (2) between the simplified point system of the geriatric TTR score and the simple SAMe‐TT2R2 score. The validation set was subdivided into AF and VTE populations. We computed the AUC when predicting TTR >70%, a cutoff to indicate good anticoagulation quality in the literature.34, 35 We then computed the AUC when predicting incidence of a composite clinical outcome of stroke, systemic arterial embolism, VTE, and major bleeding (see detailed definitions in Table S2) that occurred between the 29th and 365th days following the index date (ie, the same ascertainment period as TTR). We also evaluated thromboembolic and bleeding events separately. In addition, we computed Hosmer–Lemeshow goodness‐of‐fit statistics to assess calibration of the models. The hypothesis testing for AUC comparison was done with methods proposed by DeLong et al.36

Missing Data

The information on smoking and body mass index was recorded in the study EHRs as both structured data and text in the clinical notes. To reduce missing data, we used natural language processing37 to extract information on these 2 variables from the clinical notes; this approach reduced the proportion of patients missing smoking data from 54.4% to 7.8% and of those missing body mass index from 38.5% to 32.2% (see Data S1 for details). For those still missing smoking and body mass index information after natural language processing and with other variables with missing data, we used the missing indicator method in the analysis.

Statistical Analyses

First, we tested the sensitivity of our results to the length of the baseline assessment period (365 instead of 180 days) and the definition of the new initiator of VKA (no use of VKA in the 180 days instead of 90 days before the index date). We calculated the Spearman correlation coefficient between the new scores based on revised strategies and the original score to quantify discrepancies. Second, to evaluate whether our results were sensitive to outliers or skewed the distribution of TTR, we repeated our analyses after (1) Box–Cox transformation of TTR38 and (2) exclusion of those with extreme outcomes (TTR=0) from the analysis. The statistical analyses were conducted with SAS 9.4 (SAS Institute Inc).


Systematic Review

From a total of 3692 studies, we selected 16 articles (Figure 1 summarizes the search and selection process). Among them, 11 articles investigated patients taking VKA for nonvalvular AF,17, 18, 20, 22, 39, 40, 41, 42, 43, 44, 45 4 for mixed indications19, 21, 46, 47 and 2 for VTE.18, 48 Based on these selected articles, we identified 8 positive and 42 negative predictors (Table 1). To enrich the candidate predictor pool, we added 23 variables based on clinical knowledge (see Table S3 for the full list of candidate predictors and their definitions).

Table 1
Significant Predictors for Anticoagulation Control Quality From a Systematic Review

Patient Characteristics of the Study Population

Among 14250 VKA new initiators with at least 180 days of Medicare enrollment and 1 EHR encounter in the study system, we selected the study cohort with at least 5 INRs recorded in our database, including 1663 patients in the training set, 694 in the AF validation set, and 487 in the VTE validation set. The distribution of combined comorbidity score was similar in patients with versus without 5 INRs with a mean standardized difference of 0.02 between proportions of all combined comorbidity score categories in those included versus excluded (Figure S1). The mean TTR was 0.47 to 0.56 in our training and validation sets (Table 2 and Figure S2). We observed modest differences in some predictors in AF versus VTE validation populations (eg, higher prevalence of cancer and more use of antibiotics in the VTE; Table 2).

Table 2
Patient Characteristics of the Study Populations

Prediction Models for TTR

From 50 predictors identified in the systematic review and 23 additional variables, we built the new geriatric TTR score with 42 predictors through lasso regression (R 2=0.19; Table 3). The simplified model included a total of 7 variables (R 2=0.14). We summarized these variables using the acronym PROSPER (Pneumonia, Renal dysfunction, Oozing blood [prior bleeding], Staying in hospital ≥7 days, use of Pain medications, lack of Enhanced [dedicated and structured] anticoagulation care, Rx for antibiotics; see Table 4 and Table S3 for detailed definitions). There was no significant difference between the AUCs of PROSPER versus the full geriatric TTR model predicting TTR >70% in the validation set (AUC 0.678 versus 0.680, P=0.86 for difference). The 2 most influential predictors of TTR were lack of participation in a dedicated anticoagulation management service (assigned 4 points) and renal dysfunction (assigned 2 points). The rest of the variables were assigned 1 point each.

Table 3
The Geriatric TTR Prediction Model for Anticoagulation Control Qualitya
Table 4
Simplified Geriatric Prediction Score for Anticoagulation Control Qualitya: PROSPER

Comparison of Performance: SAMe‐TT2R2 Versus Geriatric TTR Score

In the training set, the AUC for the geriatric TTR score predicting TTR >70% (AUC=0.71) was substantially larger than that for coefficient‐based SAMe‐TT2R2 (AUC=0.57, P<0.001 for difference); the AUC for the geriatric TTR score predicting the primary clinical outcome (AUC=0.65) was significantly larger than that for SAMe‐TT2R2 (AUC=0.53, P<0.001 for difference). The results were similar in the validation set (Figure 2). This pattern was consistent when the validation set was subdivided into AF and VTE validation sets (Table 5). We also found similar findings when the composite clinical outcome was subdivided into thromboembolic versus bleeding outcomes (Table S4). The Hosmer–Lemeshow goodness‐of‐fit test for predicting TTR >70% confirmed good calibration for the both the full geriatric model and coefficient‐based SAMe‐TT2R2 in the training and validation sets (Table S5).

Figure 2
Comparison of AUC: new geriatric score superior to SAMe‐TT2R2. A, Predicting TTR >70%. B, Predicting clinical outcomes. *Composite outcomes of incident stroke, systemic embolism, VTE, and major bleeding events. AF indicates atrial fibrillation; ...
Table 5
Comparison of Model Performance of Original SAMe‐TT2R2 and Geriatric TTR Score

Comparison of Performance: SAMe‐TT2R2 Simple Scoring System Versus PROSPER

In the training set, the AUC for PROSPER predicting TTR >70% (AUC=0.67) was substantially larger than that for SAMe‐TT2R2 (AUC=0.55, P<0.001 for difference); the AUC for PROSPER predicting the primary clinical outcome (AUC=0.62) was significantly larger than that for SAMe‐TT2R2 (AUC=0.52, P<0.001 for difference). A similar pattern was observed in the AF and VTE validation sets when predicting both types of outcomes (Table 5). Patients stratified by PROSPER had a clear decreasing trend of mean TTR, ranging from 0.71 to 0.30, in both the training and validation sets (Table 6).

Table 6
Mean TTR by Simplified New Geriatric Score

Sensitivity Analyses

After changing the length of baseline assessment period from 180 to 365 days, the revised prediction score was highly correlated with the original one (Spearman coefficient=0.89). After defining new initiation of VKA as no use in the 180 days rather than 90 days before the index date, the revised prediction score was highly correlated with the original one (Spearman coefficient=0.99). The performance of these revised models was similar to that of the original model (Table S6). After Box–Cox transformation, the distribution of TTR became more symmetric (Fisher‐Pearson skewness coefficient49 reduced by 46%), resulting in a prediction score highly correlated with the predicted value generated by the original model (Spearman coefficient=0.99). Similar patterns were found when excluding those with TTR 0 (Table S6).


We developed and validated a new prediction score in the older adult population. Our geriatric TTR score included 42 predictors, and the simplified clinical scoring system, PROSPER, had 7 variables. The geriatric TTR score and PROSPER outperformed the corresponding coefficient‐based and simple version of SAMe‐TT2R2, available for the past 4 years, when predicting TTR ≥70% and thromboembolic and bleeding outcomes for those aged ≥65 years. The performance of PROSPER was not significantly worse than that of the full model in the validation set.

Physicians can use geriatric TTR scores to identify patients with good predicted TTR (>70%) as good candidates for VKA therapy for nonvalvular AF or VTE; otherwise, a DOAC may be preferred unless contraindicated. It is feasible to develop an automated program in an EHR system for computing the predicted TTR based on the full model as a clinical decision support tool; otherwise, PROSPER can be readily calculated without an aid. Our findings suggest that a PROSPER score >2 is predictive of having poor TTR; therefore, initiating a VKA may not be ideal. This cut point is associated with reasonable specificity (75%) for TTR >70% and sensitivity (85%; Table 7) for TTR <50% (another cut point suggested in the literature to indicate poor anticoagulation quality34). Alternatively, the categorization of PROSPER as 0 to 2, 3 to 6, and ≥7 approximately subdivided the population into tertiles that correlated well with TTR. These 3 categories may be used to indicate low, moderate, and high risk of having poor TTR (Table 8). Our work highlights the importance of a structured approach to warfarin management; lack of a dedicated anticoagulation management service was found to be the strongest predictor of poor TTR. This finding is in line with several prior studies in which structured anticoagulation care was shown to improve TTR and to reduce risk of complications.50, 51, 52, 53 In the current era when DOACs are available, unstructured warfarin management is a particularly unattractive treatment option. If DOAC treatment is not possible and a patient has a PROSPER score >2, providers should encourage patient participation in a dedicated anticoagulation management service or some equivalently well‐organized warfarin treatment setting (eg, a practice with a nurse dedicated to managing warfarin). Renal dysfunction, defined as the presence of acute kidney injury, chronic kidney disease, or end‐stage kidney disease in the prior 180 days, was also found to be an important predictor of poor TTR. The anticoagulation decision is particularly difficult in AF patients with renal dysfunction, for whom there is uncertainty as to the net benefit of warfarin or DOACs with poor renal function. One approach can be to favor use of a DOAC that is less renally excreted (eg, apixaban) with necessary dose adjustment.

Table 7
Sensitivity and Specificity in the Validation Set (AF and VTE)
Table 8
TTR by the Simplified Geriatric Score Categories

Our score can also be helpful in a research context. First, researchers can evaluate the potential treatment‐effect heterogeneity by levels of predicted anticoagulation quality based on the full model with a computer program. This assessment can provide direct evidence for choosing the ideal candidates for VKA versus DOACs based on the pretreatment characteristics predictive of anticoagulation quality. Next, our score can be used as a proxy adjustment tool for confounding by anticoagulation control quality. This adjustment is otherwise difficult because calculating TTR requires intensive INR recording in the study databases, which are often incomplete or nonexistent. Because some researchers do not have information on biophysiologic variables, we also presented an alternative model excluding these variables that requires additional testing (Table S7). This alternative model had performance similar to the geriatric TTR score (data not shown).

We have demonstrated that the performance of the new geriatric TTR score was clearly superior to that of SAMe‐TT2R2 in the older adult population. The authors of SAMe‐TT2R2 demonstrated good discrimination performance only when predicting those with TTR <5th percentile but not for those with TTR <25th percentile (AUC=0.58).17 However, the latter is closer to the clinical relevant cut points (eg, TTR >70% usually composes about 30% to 40% of the population17, 18, 34). Because the majority of VKA users are older adults3, 18 who are also more vulnerable to developing bleeding complications,54 we developed an alternative score dedicated to patients aged ≥65 years. We built a prediction model for both nonvalvular AF and VTE indications because prior studies found that AF and VTE patients share many risk factors for TTR18 and because including interaction terms with the VKA indications did not materially improve the model in our analysis. We validated the performance of our model in AF and VTE populations separately and found consistent results.

There are some important limitations. We used linked claims EHR data for higher data quality: The claims data provided comprehensive data across care settings, and EHRs provided necessary clinical information to ascertain TTR and important predictors. However, requiring overlap of the 2 databases reduces our sample size substantially and limits our ability to investigate each clinical outcome individually.55 Besides, for biophysiologic variables (eg, body mass index, albumin levels), we had 29% to 34% people with missing data in the relevant period. We handled it by the missing indicator method because not having certain tests done could, by itself, be informative of the general health state, and this approach allows use of these scores even if some variables are not available. As a sensitivity analysis, the scores not including these variables with missing data were highly correlated with the original one and had similar model performance (data not shown). In addition, some of the possible determinants of TTR are not available in our data sets, such as diet information and genetic profiles associated with warfarin pharmacokinetics, which may limit our model performance. Consequently, our prediction scores should be used as an aid, not as the only ground for decision‐making. Next, we chose to build one prediction model for both nonvalvular AF and VTE indications because prior studies found that AF and VTE patients have many common risk factors for poor anticoagulation qualilty.18 We validated the performance of this score in AF and VTE populations separately and found consistent results. Nonetheless, we acknowledge the alternative approach to build separate models for different indications, which may increase specificity at the cost of simplicity and applicability. Last, the predictors identified in our study should not be interpreted as having causal effect on anticoagulation quality because they could be merely the markers or proxies of the real causal factors.

In conclusion, we developed and validated a prediction score for anticoagulation control quality quantified by TTR in the older adult population. It outperformed the published score, SAMe‐TT2R2, in patients aged ≥65 years when predicting TTR as well as thromboembolic and bleeding events. The full model of the geriatric TTR score can be used as an embedded algorithm within an EHR or for a research study. The simplified scoring system, PROSPER, had comparable performance and can be used in daily practice to help choose the best candidates to receive VKA therapy.

Sources of Funding

Lin received a stipend from the Pharmacoepidemiology program in the Department of Epidemiology, Harvard T.H. Chan School of Public Health and Department of Medicine, Brigham and Women's Hospital, Harvard Medical School. Singer was supported by the Eliot B. and Edith C. Shoolman Fund of the Massachusetts General Hospital (Boston, MA). Drs. Lin and Schneeweiss were supported by PCORI grant 282364.5077585.0007 (ARCH/SCILHS).


Oertel has occasionally participated on Advisory Boards for Roche Diagnostics and Alere. Dr. Schneeweiss is consultant to WHISCON, LLC and to Aetion, Inc., a software manufacturer of which he also owns equity. He is principal investigator of investigator‐initiated grants to the Brigham and Women’s Hospital from Bayer, Genentech, and Boehringer Ingelheim unrelated to the topic of this study. The remaining authors have no disclosures to report.

Supporting information

Data S1. Natural language processing to improve missing data.

Table S1. SAMe‐TT2R2 Original Model

Table S2. Definitions of Clinical Outcomes

Table S3. Definitions of Predictors for Anticoagulation Control Quality

Table S4. Sensitivity Analysis: Similar Performance With Composite Versus Specific Outcomes

Table S5. Hosmer–Lemeshow Goodness‐of‐Fit Table of Geriatric TTR Model in the Validation Set. TTR indicates time in therapeutic range.

Table S6. Sensitivity Analysis: Similar Performance With Different Analysis Strategies

Table S7. New Geriatric Prediction Model for Anticoagulation Control Quality* Based on Only Variables Available in an Insurance Claims Database

Figure S1. Similar distribution of combined comorbidity* score in those with vs without 5 INRs in the study EHR system.

Figure S2. The distribution of TTR in the training & validation sets.


(J Am Heart Assoc. 2017;6:e006814 DOI: 10.1161/JAHA.117.006814.)


1. Ansell J, Hirsh J, Hylek E, Jacobson A, Crowther M, Palareti G; American College of Chest P . Pharmacology and management of the vitamin K antagonists: American College of Chest Physicians Evidence‐Based Clinical Practice Guidelines (8th Edition). Chest. 2008;133:160S–198S. [PubMed]
2. Hart RG, Pearce LA, Aguilar MI. Meta‐analysis: antithrombotic therapy to prevent stroke in patients who have nonvalvular atrial fibrillation. Ann Intern Med. 2007;146:857–867. [PubMed]
3. Huisman MV, Rothman KJ, Paquette M, Teutsch C, Diener HC, Dubner SJ, Halperin JL, Ma CS, Zint K, Elsaesser A, Bartels DB, Lip GY; Investigators G‐A . The changing landscape for stroke prevention in AF: findings from the GLORIA‐AF Registry Phase 2. J Am Coll Cardiol. 2017;69:777–785. [PubMed]
4. Cancino RS, Hylek EM, Reisman JI, Rose AJ. Comparing patient‐level and site‐level anticoagulation control as predictors of adverse events. Thromb Res. 2014;133:652–656. [PubMed]
5. Rose AJ, Delate T, Ozonoff A, Witt DM. Comparison of the abilities of summary measures of international normalized ratio control to predict clinically relevant bleeding. Circ Cardiovasc Qual Outcomes. 2015;8:524–531. [PubMed]
6. Connolly SJ, Pogue J, Eikelboom J, Flaker G, Commerford P, Franzosi MG, Healey JS, Yusuf S; Investigators AW . Benefit of oral anticoagulant over antiplatelet therapy in atrial fibrillation depends on the quality of international normalized ratio control achieved by centers and countries as measured by time in therapeutic range. Circulation. 2008;118:2029–2037. [PubMed]
7. Ho CW, Ho MH, Chan PH, Hai JJ, Cheung E, Yeung CY, Lau KK, Chan KH, Lau CP, Lip GY, Leung GK, Tse HF, Siu CW. Ischemic stroke and intracranial hemorrhage with aspirin, dabigatran, and warfarin: impact of quality of anticoagulation control. Stroke. 2015;46:23–30. [PubMed]
8. Singer DE, Chang Y, Fang MC, Borowsky LH, Pomernacki NK, Udaltsova N, Go AS. Should patient characteristics influence target anticoagulation intensity for stroke prevention in nonvalvular atrial fibrillation? The ATRIA study. Circ Cardiovasc Qual Outcomes. 2009;2:297–304. [PubMed]
9. Granger CB, Alexander JH, McMurray JJ, Lopes RD, Hylek EM, Hanna M, Al‐Khalidi HR, Ansell J, Atar D, Avezum A, Bahit MC, Diaz R, Easton JD, Ezekowitz JA, Flaker G, Garcia D, Geraldes M, Gersh BJ, Golitsyn S, Goto S, Hermosillo AG, Hohnloser SH, Horowitz J, Mohan P, Jansky P, Lewis BS, Lopez‐Sendon JL, Pais P, Parkhomenko A, Verheugt FW, Zhu J, Wallentin L; Committees A and Investigators . Apixaban versus warfarin in patients with atrial fibrillation. N Engl J Med. 2011;365:981–992. [PubMed]
10. Connolly SJ, Ezekowitz MD, Yusuf S, Eikelboom J, Oldgren J, Parekh A, Pogue J, Reilly PA, Themeles E, Varrone J, Wang S, Alings M, Xavier D, Zhu J, Diaz R, Lewis BS, Darius H, Diener HC, Joyner CD, Wallentin L; Committee R‐LS and Investigators . Dabigatran versus warfarin in patients with atrial fibrillation. N Engl J Med. 2009;361:1139–1151. [PubMed]
11. Patel MR, Mahaffey KW, Garg J, Pan G, Singer DE, Hacke W, Breithardt G, Halperin JL, Hankey GJ, Piccini JP, Becker RC, Nessel CC, Paolini JF, Berkowitz SD, Fox KA, Califf RM; Investigators RA . Rivaroxaban versus warfarin in nonvalvular atrial fibrillation. N Engl J Med. 2011;365:883–891. [PubMed]
12. Wallentin L, Yusuf S, Ezekowitz MD, Alings M, Flather M, Franzosi MG, Pais P, Dans A, Eikelboom J, Oldgren J, Pogue J, Reilly PA, Yang S, Connolly SJ; Investigators R‐L . Efficacy and safety of dabigatran compared with warfarin at different levels of international normalised ratio control for stroke prevention in atrial fibrillation: an analysis of the RE‐LY trial. Lancet. 2010;376:975–983. [PubMed]
13. Hernandez I, Baik SH, Pinera A, Zhang Y. Risk of bleeding with dabigatran in atrial fibrillation. JAMA Intern Med. 2015;175:18–24. [PubMed]
14. Graham DJ, Reichman ME, Wernecke M, Zhang R, Southworth MR, Levenson M, Sheu TC, Mott K, Goulding MR, Houstoun M, MaCurdy TE, Worrall C, Kelman JA. Cardiovascular, bleeding, and mortality risks in elderly Medicare patients treated with dabigatran or warfarin for nonvalvular atrial fibrillation. Circulation. 2015;131:157–164. [PubMed]
15. Lauw MN, Eikelboom JW, Coppens M, Wallentin L, Yusuf S, Ezekowitz M, Oldgren J, Nakamya J, Wang J, Connolly SJ. Effects of dabigatran according to age in atrial fibrillation. Heart. 2017;103:1015–1023. [PubMed]
16. Stevens LA, Viswanathan G, Weiner DE. Chronic kidney disease and end‐stage renal disease in the elderly population: current prevalence, future projections, and clinical significance. Adv Chronic Kidney Dis. 2010;17:293–301. [PubMed]
17. Apostolakis S, Sullivan RM, Olshansky B, Lip GY. Factors affecting quality of anticoagulation control among patients with atrial fibrillation on warfarin: the SAMe‐TT(2)R(2) score. Chest. 2013;144:1555–1563. [PubMed]
18. Macedo AF, Bell J, McCarron C, Conroy R, Richardson J, Scowcroft A, Sunderland T, Rotheram N. Determinants of oral anticoagulation control in new warfarin patients: analysis using data from Clinical Practice Research Datalink. Thromb Res. 2015;136:250–260. [PubMed]
19. Paradise HT, Berlowitz DR, Ozonoff A, Miller DR, Hylek EM, Ash AS, Jasuja GK, Zhao S, Reisman JI, Rose AJ. Outcomes of anticoagulation therapy in patients with mental health conditions. J Gen Intern Med. 2014;29:855–861. [PubMed]
20. Dlott JS, George RA, Huang X, Odeh M, Kaufman HW, Ansell J, Hylek EM. National assessment of warfarin anticoagulation therapy for stroke prevention in atrial fibrillation. Circulation. 2014;129:1407–1414. [PubMed]
21. Efird LM, Mishkin DS, Berlowitz DR, Ash AS, Hylek EM, Ozonoff A, Reisman JI, Zhao S, Jasuja GK, Rose AJ. Stratifying the risks of oral anticoagulation in patients with liver disease. Circ Cardiovasc Qual Outcomes. 2014;7:461–467. [PubMed]
22. Kim EJ, Ozonoff A, Hylek EM, Berlowitz DR, Ash AS, Miller DR, Zhao S, Reisman JI, Jasuja GK, Rose AJ. Predicting outcomes among patients with atrial fibrillation and heart failure receiving anticoagulation with warfarin. Thromb Haemost. 2015;114:70–77. [PubMed]
23. Lip GY, Haguenoer K, Saint‐Etienne C, Fauchier L. Relationship of the SAMe‐TT(2)R(2) score to poor‐quality anticoagulation, stroke, clinically relevant bleeding, and mortality in patients with atrial fibrillation. Chest. 2014;146:719–726. [PubMed]
24. Gallego P, Roldan V, Marin F, Galvez J, Valdes M, Vicente V, Lip GY. SAMe‐TT2R2 score, time in therapeutic range, and outcomes in anticoagulated patients with atrial fibrillation. Am J Med. 2014;127:1083–1088. [PubMed]
25. Zhang H, Yang Y, Zhu J. The SAMe‐TT(2)R(2) score: far from clinical application. Chest. 2014;145:418–419. [PubMed]
26. Hennessy S. Use of health care databases in pharmacoepidemiology. Basic Clin Pharmacol Toxicol. 2006;98:311–313. [PubMed]
27. Johnson ES, Bartman BA, Briesacher BA, Fleming NS, Gerhard T, Kornegay CJ, Nourjah P, Sauer B, Schumock GT, Sedrakyan A, Sturmer T, West SL, Schneeweiss S. The incident user design in comparative effectiveness research. Pharmacoepidemiol Drug Saf. 2013;22:1–6. [PubMed]
28. Gagne JJ, Glynn RJ, Avorn J, Levin R, Schneeweiss S. A combined comorbidity score predicted mortality in elderly patients better than existing scores. J Clin Epidemiol. 2011;64:749–759. [PubMed]
29. Austin PC. Balance diagnostics for comparing the distribution of baseline covariates between treatment groups in propensity‐score matched samples. Stat Med. 2009;28:3083–3107. [PubMed]
30. Rosendaal FR, Cannegieter SC, van der Meer FJ, Briet E. A method to determine the optimal intensity of oral anticoagulant therapy. Thromb Haemost. 1993;69:236–239. [PubMed]
31. Go AS, Hylek EM, Chang Y, Phillips KA, Henault LE, Capra AM, Jensvold NG, Selby JV, Singer DE. Anticoagulation therapy for stroke prevention in atrial fibrillation: how well do randomized trials translate into clinical practice? JAMA. 2003;290:2685–2692. [PubMed]
32. Tibshirani R. Regression shrinkage and selection via the lasso. J R Stat Soc Series B. 1996;58:267–288.
33. Jones RH. Bayesian information criterion for longitudinal and clustered data. Stat Med. 2011;30:3050–3056. [PubMed]
34. Razouki Z, Ozonoff A, Zhao S, Jasuja GK, Rose AJ. Improving quality measurement for anticoagulation: adding international normalized ratio variability to percent time in therapeutic range. Circ Cardiovasc Qual Outcomes. 2014;7:664–669. [PubMed]
35. Wan Y, Heneghan C, Perera R, Roberts N, Hollowell J, Glasziou P, Bankhead C, Xu Y. Anticoagulation control and prediction of adverse events in patients with atrial fibrillation: a systematic review. Circ Cardiovasc Qual Outcomes. 2008;1:84–91. [PubMed]
36. DeLong ER, DeLong DM, Clarke‐Pearson DL. Comparing the areas under two or more correlated receiver operating characteristic curves: a nonparametric approach. Biometrics. 1988;44:837–845. [PubMed]
37. Friedman C, Hripcsak G. Natural language processing and its future in medicine. Acad Med. 1999;74:890–895. [PubMed]
38. Box GEP, Cox DR. An analysis of transformations revisited. J R Stat Soc. 1964;26:211–252.
39. Boulanger L, Kim J, Friedman M, Hauch O, Foster T, Menzin J. Patterns of use of antithrombotic therapy and quality of anticoagulation among patients with non‐valvular atrial fibrillation in clinical practice. Int J Clin Pract. 2006;60:258–264. [PubMed]
40. Tomita H, Kadokami T, Momii H, Kawamura N, Yoshida M, Inou T, Fukuizumi Y, Usui M, Funakoshi K, Yamada S, Aomori T, Yamamoto K, Uno T, Ando S; Group A‐Wr . Patient factors against stable control of warfarin therapy for Japanese non‐valvular atrial fibrillation patients. Thromb Res. 2013;132:537–542. [PubMed]
41. Kose E, Arai S, An T, Kikkawa A, Aoyama T, Matsumoto Y, Hayashi H. Analysis of factors affecting time in therapeutic range control after warfarin administration. Pharmazie. 2015;70:494–498. [PubMed]
42. Nelson WW, Desai S, Damaraju CV, Lu L, Fields LE, Wildgoose P, Schein JR. International normalized ratio stability in warfarin‐experienced patients with nonvalvular atrial fibrillation. Am J Cardiovasc Drugs. 2015;15:205–211. [PubMed]
43. Pignatelli P, Pastori D, Vicario T, Bucci T, Del Ben M, Russo R, Tanzilli A, Nardoni ML, Bartimoccia S, Nocella C, Ferro D, Saliola M, Cangemi R, Lip GY, Violi F. Relationship between Mediterranean diet and time in therapeutic range in atrial fibrillation patients taking vitamin K antagonists. Europace. 2015;17:1223–1228. [PubMed]
44. White RD, Riggs KW, Ege EJ, Petroski GF, Koerber SM, Flaker G. The effect of the amiodarone‐warfarin interaction on anticoagulation quality in a single, high‐quality anticoagulation center. Blood Coagul Fibrinolysis. 2016;27:147–150. [PubMed]
45. Yong C, Azarbal F, Abnousi F, Heidenreich PA, Schmitt S, Fan J, Than CT, Ullal AJ, Yang F, Phibbs CS, Frayne SM, Ho PM, Shore S, Mahaffey KW, Turakhia MP. Racial differences in quality of anticoagulation therapy for atrial fibrillation (from the TREAT‐AF study). Am J Cardiol. 2016;117:61–68. [PubMed]
46. Rose AJ, Hylek EM, Ozonoff A, Ash AS, Reisman JI, Berlowitz DR. Patient characteristics associated with oral anticoagulation control: results of the Veterans AffaiRs Study to Improve Anticoagulation (VARIA). J Thromb Haemost. 2010;8:2182–2191. [PubMed]
47. Nilsson H, Grove EL, Larsen TB, Nielsen PB, Skjoth F, Maegaard M, Christensen TD. Sex differences in treatment quality of self‐managed oral anticoagulant therapy: 6,900 patient‐years of follow‐up. PLoS One. 2014;9:e113627. [PubMed]
48. Kooistra HA, Gebel M, Sahin K, Lensing AW, Meijer K. Independent predictors of poor vitamin K antagonist control in venous thromboembolism patients. Data from the EINSTEIN‐DVT and PE studies. Thromb Haemost. 2015;114:1136–1143. [PubMed]
49. Newell KM, Hancock PA. Forgotten moments: a note on skewness and kurtosis as influential factors in inferences extrapolated from response distributions. J Mot Behav. 1984;16:320–335. [PubMed]
50. Wurster M, Doran T. Anticoagulation management: a new approach. Dis Manag. 2006;9:201–209. [PubMed]
51. Rudd KM, Dier JG. Comparison of two different models of anticoagulation management services with usual medical care. Pharmacotherapy. 2010;30:330–338. [PubMed]
52. Ansell JE. Optimizing the efficacy and safety of oral anticoagulant therapy: high‐quality dose management, anticoagulation clinics, and patient self‐management. Semin Vasc Med. 2003;3:261–270. [PubMed]
53. Chamberlain MA, Sageser NA, Ruiz D. Comparison of anticoagulation clinic patient outcomes with outcomes from traditional care in a family medicine clinic. J Am Board Fam Pract. 2001;14:16–21. [PubMed]
54. Pisters R, Lane DA, Nieuwlaat R, de Vos CB, Crijns HJ, Lip GY. A novel user‐friendly score (HAS‐BLED) to assess 1‐year risk of major bleeding in patients with atrial fibrillation: the Euro Heart Survey. Chest. 2010;138:1093–1100. [PubMed]
55. Lin KJ, Schneeweiss S. Considerations for the analysis of longitudinal electronic health records linked to claims data to study the effectiveness and safety of drugs. Clin Pharmacol Ther. 2016;100:147–159. [PubMed]

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