Adjusting for possibly misclassified causes of death in cause-specific survival analysis
|
|
- Rafe Arnold
- 5 years ago
- Views:
Transcription
1 Adjusting for possibly misclassified causes of death in cause-specific survival analysis Bart Van Rompaye Els Goetghebeur Department of Applied Mathematics and Computer Sciences Ghent University, BE 1 / 21
2 Problem description Drugs developed against disease-specific mortality exposure affects cause-specific mortality interest in reduction of cause-specific mortality need good assessment of cause of death ICD-guidelines death registries: little control, little motivation to do it right? clinical trials: more motivation, but sometimes practical constraints 2 / 21
3 Problem description Drugs developed against disease-specific mortality exposure affects cause-specific mortality interest in reduction of cause-specific mortality need good assessment of cause of death ICD-guidelines death registries: little control, little motivation to do it right? clinical trials: more motivation, but sometimes practical constraints 2 / 21
4 Problem description Motivating study: Jaffar et al., I.J.E Effects of misclassification of causes of death on the power of a trial to assess the efficacy of a pneumococcal conjugate vaccine in The Gambia phase III randomized, placebo controlled trial impact of a vaccine on mortality from airway infections in Gambian children need for post-mortem questionnaires or verbal autopsy misclassification of causes dilution of treatment effect power loss 3 / 21
5 Problem description Motivating study: Jaffar et al., I.J.E CODs: λ doc = py, λ dfd = py expected treatment effect: 31.5% reduction of λ dfd misclassification of causes p 1 =0.6 sensitivity=0.4=1 p 1 p 0 =0.1 specificity=0.9=1 p 0 power loss? 4 / 21
6 Impact of misclassification: Jaffar et al. - naive logrank p 0 = 0.1 p 1 = 0.6 power = 21% 5 / 21
7 Problem description Motivating study: Jaffar et al., I.J.E cause-specific mortality: power loss all-cause mortality: sample size radiological pneumonia ITT-result: significant reduction (Cutts et al., Lancet 2005) 6 / 21
8 Problem description Motivating study: Jaffar et al., I.J.E cause-specific mortality: power loss all-cause mortality: sample size radiological pneumonia ITT-result: significant reduction (Cutts et al., Lancet 2005) misclassification determines design and analysis! 6 / 21
9 Our approach derive adapted logrank test model true and observed cause-specific hazards acknowledging misclassification rates input this in likelihood-based weighting evaluate the power that is regained compare efficiencies for endpoint selection: all-cause vs. naive vs. improved cause-specific testing derive adjusted sample size formula estimate effect of treatment (on cause-specific hazard): ongoing 7 / 21
10 Our approach derive adapted logrank test model true and observed cause-specific hazards acknowledging misclassification rates input this in likelihood-based weighting evaluate the power that is regained compare efficiencies for endpoint selection: all-cause vs. naive vs. improved cause-specific testing derive adjusted sample size formula estimate effect of treatment (on cause-specific hazard): ongoing 7 / 21
11 Design assumptions treatment Z: 0 or 1 (1= treatment) observation time T failure indicator δ: 0=censored, 1=failure true cause-of-death COD true : doc or dfd misclassification indicator M: 0 or 1 (1=misclassified) observed COD = COD obs observed data: (Z, T, δ, COD obs ) Z T,δ, COD obs t 8 / 21
12 Design assumptions Assumptions: similar to Goetghebeur and Ryan, Biometrika 1990 misclassification probabilities depend on true COD and on time: p 0 (t) and p 1 (t) failure patterns from proportional cause-specific hazards: COD other cause disease control treatment Null H 0 : φ = 0 h dfd (t) h dfd (t)e φ 9 / 21
13 Design assumptions Assumptions: similar to Goetghebeur and Ryan, Biometrika 1990 misclassification probabilities depend on true COD and on time: p 0 (t) and p 1 (t) failure patterns from proportional cause-specific hazards: COD other cause disease control treatment Null H 0 : φ = 0 h dfd (t) h dfd (t)e φ 9 / 21
14 Design assumptions Assumptions: similar to Goetghebeur and Ryan, Biometrika 1990 misclassification probabilities depend on true COD and on time: p 0 (t) and p 1 (t) failure patterns from proportional cause-specific hazards: COD other cause disease control treatment Null H 0 : φ = 0 h dfd (t) h dfd (t)e φ 9 / 21
15 Design assumptions Assumptions: similar to Goetghebeur and Ryan, Biometrika 1990 misclassification probabilities depend on true COD and on time: p 0 (t) and p 1 (t) failure patterns from proportional cause-specific hazards: COD other cause disease control h doc (t) = h dfd (t)e ξ h dfd (t) treatment h doc (t) = h dfd (t)e ξ h dfd (t)e φ Null H 0 : φ = 0 9 / 21
16 Partial likelihood no misclassification: L p (observed data) = i:cod true,i =dfd h dfd (t i )e φz i j R i h dfd (t i )e φz j 10 / 21
17 Partial likelihood no misclassification: L p (observed data) = misclassification: i:cod true,i =dfd h dfd (t i )e φz i j R i h dfd (t i )e φz j L p (observed data) h dfd (t i )(e ξ (1 p 0 (t i )) + e φz i p 1 (t i )) = j R i h dfd (t i )(e ξ (1 p 0 (t i )) + e φz j p 1 (t i )) i:cod obs =doc i:cod obs =dfd h dfd (t i )(e φz i (1 p 1 (t i )) + e ξ p 0 (t i )) j R i h dfd (t i )(e φz j (1 p 1 (t i )) + e ξ p 0 (t i )) 10 / 21
18 Partial likelihood no misclassification: L p (observed data) = misclassification: i:cod true,i =dfd h dfd (t i )e φz i j R i h dfd (t i )e φz j L p (observed data) h dfd (t i )(e ξ (1 p 0 (t i )) + e φz i p 1 (t i )) = j R i h dfd (t i )(e ξ (1 p 0 (t i )) + e φz j p 1 (t i )) i:cod obs =doc i:cod obs =dfd h dfd (t i )(e φz i (1 p 1 (t i )) + e ξ p 0 (t i )) j R i h dfd (t i )(e φz j (1 p 1 (t i )) + e ξ p 0 (t i )) 10 / 21
19 Partial likelihood no misclassification: L p (observed data) = misclassification: i:cod true,i =dfd h dfd (t i )e φz i j R i h dfd (t i )e φz j L p (observed data) h dfd (t i )(e ξ (1 p 0 (t i )) + e φz i p 1 (t i )) = j R i h dfd (t i )(e ξ (1 p 0 (t i )) + e φz j p 1 (t i )) i:cod obs =doc i:cod obs =dfd h dfd (t i )(e φz i (1 p 1 (t i )) + e ξ p 0 (t i )) j R i h dfd (t i )(e φz j (1 p 1 (t i )) + e ξ p 0 (t i )) 10 / 21
20 Partial likelihood no misclassification: L p (observed data) = misclassification: i:cod true,i =dfd h dfd (t i )e φz i j R i h dfd (t i )e φz j L p (observed data) h dfd (t i )(e ξ (1 p 0 (t i )) + e φz i p 1 (t i )) = j R i h dfd (t i )(e ξ (1 p 0 (t i )) + e φz j p 1 (t i )) i:cod obs =doc i:cod obs =dfd h dfd (t i )(e φz i (1 p 1 (t i )) + e ξ p 0 (t i )) j R i h dfd (t i )(e φz j (1 p 1 (t i )) + e ξ p 0 (t i )) 10 / 21
21 Score statistic with: w i = and variance: 1 1+e ξ 1 p 0 (t i ) p 1 (t i ) 1 1+e ξ p 0 (t i ) 1 p 1 (t i ) V n = δ i =1 T n = δ i =1 w i (t i, COD obs )(Z i Z i ) w 2 COD obs = doc 1 negative predictive value COD obs = dfd i (t i, COD obs ) positive predictive value Zj 2 /n i j R i Z 2 i 11 / 21
22 Score statistic with: w i = and variance: 1 1+e ξ 1 p 0 (t i ) p 1 (t i ) 1 1+e ξ p 0 (t i ) 1 p 1 (t i ) V n = δ i =1 T n = δ i =1 w i (t i, COD obs )(Z i Z i ) w 2 COD obs = doc 1 negative predictive value COD obs = dfd i (t i, COD obs ) positive predictive value Zj 2 /n i j R i Z 2 i 11 / 21
23 Score statistic with: w i = and variance: 1 1+e ξ 1 p 0 (t i ) p 1 (t i ) 1 1+e ξ p 0 (t i ) 1 p 1 (t i ) V n = δ i =1 T n = δ i =1 w i (t i, COD obs )(Z i Z i ) w 2 COD obs = doc 1 negative predictive value COD obs = dfd i (t i, COD obs ) positive predictive value Zj 2 /n i j R i Z 2 i 11 / 21
24 T Some features of n V n standard normal under the null no misclassification: standard logrank test time-constant misclassification T n V n = w doct n doc + w dfdt n dfd w 2 doc V n doc + w 2 dfd V n dfd 12 / 21
25 Impact of misclassification: Jaffar et al. - corrected logrank p 0 = 0.1 p 1 = 0.6 power = 27% 13 / 21
26 Impact of misclassification: Jaffar et al. - corrected logrank p 0 = 0.1 p 1 = 0.6 power = 27% 27% 21% = / 21
27 Impact of misclassification Asymptotic relative efficiencies General statistic: three possible tests w doc Tdoc n + w dfd Tdfd n (w doc ) 2 Vdoc n + (w dfd ) 2 Vdfd n the all-cause mortality logrank test: w doc = 1,w dfd = 1 the naive statistic (observed-cause-specific logrank test): w doc = 0,w dfd = 1 the corrected statistic (time-constant weighted logrank test): w doc = w doc,w dfd = w dfd 14 / 21
28 Impact of misclassification Asymptotic relative efficiencies n Pitman efficiencies: compare are(1, 2) = lim φ,2 φ n φ,1 naive 1 naive corrected all-cause corrected 1 + w doc p 1 w dfd (1 p 1 ) 1 all-cause 1 (1+e ξ )w dfd (1 p 1 ) 1 (1+e ξ )(w doc p 1 +w dfd (1 p 1 )) 1 15 / 21
29 are(all-cause, naive) = 1 (1+e ξ )w dfd (1 p 1 ) favour naive > 1 at low p 0, p 1 < 1 at high p 0, p 1 favour allcause 16 / 21
30 are(naive, corrected) = ( ) w docp 1 w dfd (1 p 1 ) equal 1 = 1 when p 1 = 0 favour corrected 17 / 21
31 are(all-cause, corrected) = 1 (1+e ξ )(w doc p 1 +w dfd (1 p 1 )) equal < 1 when p 0 and p 1 extreme 1 when p 0 + p 1 1 w doc w dfd weighted test equals all-cause test never > 1 favour corrected 18 / 21
32 are(all-cause, corrected) = 1 (1+e ξ )(w doc p 1 +w dfd (1 p 1 )) equal < 1 when p 0 and p 1 extreme 1 when p 0 + p 1 1 w doc w dfd weighted test equals all-cause test never > 1 favour corrected 18 / 21
33 are(all-cause, corrected) = 1 (1+e ξ )(w doc p 1 +w dfd (1 p 1 )) equal + p 0 = 0.1 p 1 = 0.6 are = 0.68 favour corrected 18 / 21
34 Impact of misclassification Asymptotic relative efficiencies example: Jaffar et al., I.J.E remember: p 0 = 0.1, p 1 = 0.6 naive 1 naive corrected all-cause corrected all-cause Sample size implications? naive: 84,841 corrected: 60,171 all-cause: 88,487 n = 1 w doc p 1 + w dfd (1 p 1 ) n standard 19 / 21
35 Impact of misclassification Asymptotic relative efficiencies example: Jaffar et al., I.J.E remember: p 0 = 0.1, p 1 = 0.6 naive 1 naive corrected all-cause corrected all-cause Sample size implications? naive: 84,841 corrected: 60,171 all-cause: 88,487 n = 1 w doc p 1 + w dfd (1 p 1 ) n standard 19 / 21
36 Impact of misclassification Asymptotic relative efficiencies example: Jaffar et al., I.J.E remember: p 0 = 0.1, p 1 = 0.6 naive 1 naive corrected all-cause corrected all-cause Sample size implications? naive: 84,841 corrected: 60,171 all-cause: 88,487 n = 1 w doc p 1 + w dfd (1 p 1 ) n standard 19 / 21
37 Impact of misclassification Asymptotic relative efficiencies example: Jaffar et al., I.J.E remember: p 0 = 0.1, p 1 = 0.6 naive 1 naive corrected all-cause corrected all-cause Sample size implications? naive: 84,841 corrected: 60,171 all-cause: 88,487 n = 1 w doc p 1 + w dfd (1 p 1 ) n standard 19 / 21
38 What to remember misclassification occurs in many settings it leads to loss of power under some general assumptions, we can partly correct the logrank test for this this can lead to much smaller sample sizes choice of endpoint can be affected, cause-specific analysis becomes more attractive! fundamental correction, otherwise bias (estimation!) 20 / 21
39 What to remember misclassification occurs in many settings it leads to loss of power under some general assumptions, we can partly correct the logrank test for this this can lead to much smaller sample sizes choice of endpoint can be affected, cause-specific analysis becomes more attractive! fundamental correction, otherwise bias (estimation!) 20 / 21
40 What to remember misclassification occurs in many settings it leads to loss of power under some general assumptions, we can partly correct the logrank test for this this can lead to much smaller sample sizes choice of endpoint can be affected, cause-specific analysis becomes more attractive! fundamental correction, otherwise bias (estimation!) 20 / 21
41 Goetghebeur E. and Ryan L. A Modified Log Rank Test for Competing Risks with Missing Failure Types, Biometrika, 77: , 1990 Jaffar S., Leach A., Smith P.G., Cutts F. and Greenwood B. Effects of misclassification of causes of death on the power of a trial to assess the efficacy of a pneumococcal conjugate vaccine in The Gambia, International Journal of Epidemiology, 32: , 2003 Cutts F.T., Zaman S.M.A., Enwere G., Jaffar S., Levine O.S., Okoko J.B. et al. Efficacy of nine-valent pneumococcal conjugate vaccine against pneumonia and invasive pneumococcal disease in The Gambia: randomised, double-blind, placebo-controlled trial, Lancet, 365: , / 21
Linear rank statistics
Linear rank statistics Comparison of two groups. Consider the failure time T ij of j-th subject in the i-th group for i = 1 or ; the first group is often called control, and the second treatment. Let n
More informationSTAT331. Cox s Proportional Hazards Model
STAT331 Cox s Proportional Hazards Model In this unit we introduce Cox s proportional hazards (Cox s PH) model, give a heuristic development of the partial likelihood function, and discuss adaptations
More informationSample size re-estimation in clinical trials. Dealing with those unknowns. Chris Jennison. University of Kyoto, January 2018
Sample Size Re-estimation in Clinical Trials: Dealing with those unknowns Christopher Jennison Department of Mathematical Sciences, University of Bath, UK http://people.bath.ac.uk/mascj University of Kyoto,
More informationA Generalized Global Rank Test for Multiple, Possibly Censored, Outcomes
A Generalized Global Rank Test for Multiple, Possibly Censored, Outcomes Ritesh Ramchandani Harvard School of Public Health August 5, 2014 Ritesh Ramchandani (HSPH) Global Rank Test for Multiple Outcomes
More informationPart III. Hypothesis Testing. III.1. Log-rank Test for Right-censored Failure Time Data
1 Part III. Hypothesis Testing III.1. Log-rank Test for Right-censored Failure Time Data Consider a survival study consisting of n independent subjects from p different populations with survival functions
More informationSurvival Analysis. Lu Tian and Richard Olshen Stanford University
1 Survival Analysis Lu Tian and Richard Olshen Stanford University 2 Survival Time/ Failure Time/Event Time We will introduce various statistical methods for analyzing survival outcomes What is the survival
More informationEstimating the Mean Response of Treatment Duration Regimes in an Observational Study. Anastasios A. Tsiatis.
Estimating the Mean Response of Treatment Duration Regimes in an Observational Study Anastasios A. Tsiatis http://www.stat.ncsu.edu/ tsiatis/ Introduction to Dynamic Treatment Regimes 1 Outline Description
More informationAnalysing Survival Endpoints in Randomized Clinical Trials using Generalized Pairwise Comparisons
Analysing Survival Endpoints in Randomized Clinical Trials using Generalized Pairwise Comparisons Dr Julien PERON October 2016 Department of Biostatistics HCL LBBE UCBL Department of Medical oncology HCL
More informationImproving Efficiency of Inferences in Randomized Clinical Trials Using Auxiliary Covariates
Improving Efficiency of Inferences in Randomized Clinical Trials Using Auxiliary Covariates Anastasios (Butch) Tsiatis Department of Statistics North Carolina State University http://www.stat.ncsu.edu/
More informationarxiv: v2 [stat.me] 25 Feb 2011
arxiv:112.588v2 [stat.me] 25 Feb 211 Estimation of the relative risk following group sequential procedure based upon the weighted log-rank statistic Grant Izmirlian National Cancer Institute; Executive
More informationChapter 4 Fall Notations: t 1 < t 2 < < t D, D unique death times. d j = # deaths at t j = n. Y j = # at risk /alive at t j = n
Bios 323: Applied Survival Analysis Qingxia (Cindy) Chen Chapter 4 Fall 2012 4.2 Estimators of the survival and cumulative hazard functions for RC data Suppose X is a continuous random failure time with
More informationApproximation of Survival Function by Taylor Series for General Partly Interval Censored Data
Malaysian Journal of Mathematical Sciences 11(3): 33 315 (217) MALAYSIAN JOURNAL OF MATHEMATICAL SCIENCES Journal homepage: http://einspem.upm.edu.my/journal Approximation of Survival Function by Taylor
More informationImpact of covariate misclassification on the power and type I error in clinical trials using covariate-adaptive randomization
Impact of covariate misclassification on the power and type I error in clinical trials using covariate-adaptive randomization L I Q I O N G F A N S H A R O N D. Y E A T T S W E N L E Z H A O M E D I C
More informationPower and Sample Size Calculations with the Additive Hazards Model
Journal of Data Science 10(2012), 143-155 Power and Sample Size Calculations with the Additive Hazards Model Ling Chen, Chengjie Xiong, J. Philip Miller and Feng Gao Washington University School of Medicine
More informationMultistate models and recurrent event models
Multistate models Multistate models and recurrent event models Patrick Breheny December 10 Patrick Breheny Survival Data Analysis (BIOS 7210) 1/22 Introduction Multistate models In this final lecture,
More informationSurvival Analysis for Case-Cohort Studies
Survival Analysis for ase-ohort Studies Petr Klášterecký Dept. of Probability and Mathematical Statistics, Faculty of Mathematics and Physics, harles University, Prague, zech Republic e-mail: petr.klasterecky@matfyz.cz
More informationPublished online: 10 Apr 2012.
This article was downloaded by: Columbia University] On: 23 March 215, At: 12:7 Publisher: Taylor & Francis Informa Ltd Registered in England and Wales Registered Number: 172954 Registered office: Mortimer
More informationApplication of Time-to-Event Methods in the Assessment of Safety in Clinical Trials
Application of Time-to-Event Methods in the Assessment of Safety in Clinical Trials Progress, Updates, Problems William Jen Hoe Koh May 9, 2013 Overview Marginal vs Conditional What is TMLE? Key Estimation
More informationLecture 7 Time-dependent Covariates in Cox Regression
Lecture 7 Time-dependent Covariates in Cox Regression So far, we ve been considering the following Cox PH model: λ(t Z) = λ 0 (t) exp(β Z) = λ 0 (t) exp( β j Z j ) where β j is the parameter for the the
More informationThe Design of a Survival Study
The Design of a Survival Study The design of survival studies are usually based on the logrank test, and sometimes assumes the exponential distribution. As in standard designs, the power depends on The
More informationTGDR: An Introduction
TGDR: An Introduction Julian Wolfson Student Seminar March 28, 2007 1 Variable Selection 2 Penalization, Solution Paths and TGDR 3 Applying TGDR 4 Extensions 5 Final Thoughts Some motivating examples We
More informationStatistical Analysis of Binary Composite Endpoints with Missing Data in Components
Statistical Analysis of Binary Composite Endpoints with Missing Data in Components Daowen Zhang zhang@stat.ncsu.edu http://www4.ncsu.edu/ dzhang Joint work with Hui Quan, Ji Zhang & Laure Devlamynck Sanofi-Aventis
More informationExercises. (a) Prove that m(t) =
Exercises 1. Lack of memory. Verify that the exponential distribution has the lack of memory property, that is, if T is exponentially distributed with parameter λ > then so is T t given that T > t for
More informationSurvival Analysis. Stat 526. April 13, 2018
Survival Analysis Stat 526 April 13, 2018 1 Functions of Survival Time Let T be the survival time for a subject Then P [T < 0] = 0 and T is a continuous random variable The Survival function is defined
More informationLongitudinal + Reliability = Joint Modeling
Longitudinal + Reliability = Joint Modeling Carles Serrat Institute of Statistics and Mathematics Applied to Building CYTED-HAROSA International Workshop November 21-22, 2013 Barcelona Mainly from Rizopoulos,
More informationMultistate models and recurrent event models
and recurrent event models Patrick Breheny December 6 Patrick Breheny University of Iowa Survival Data Analysis (BIOS:7210) 1 / 22 Introduction In this final lecture, we will briefly look at two other
More informationCausal Hazard Ratio Estimation By Instrumental Variables or Principal Stratification. Todd MacKenzie, PhD
Causal Hazard Ratio Estimation By Instrumental Variables or Principal Stratification Todd MacKenzie, PhD Collaborators A. James O Malley Tor Tosteson Therese Stukel 2 Overview 1. Instrumental variable
More informationGroup sequential designs with negative binomial data
Group sequential designs with negative binomial data Ekkehard Glimm 1 Tobias Mütze 2,3 1 Statistical Methodology, Novartis, Basel, Switzerland 2 Department of Medical Statistics, University Medical Center
More informationInference for the dependent competing risks model with masked causes of
Inference for the dependent competing risks model with masked causes of failure Radu V. Craiu and Benjamin Reiser Abstract. The competing risks model is useful in settings in which individuals/units may
More informationSample Size Determination
Sample Size Determination 018 The number of subjects in a clinical study should always be large enough to provide a reliable answer to the question(s addressed. The sample size is usually determined by
More informationSimple techniques for comparing survival functions with interval-censored data
Simple techniques for comparing survival functions with interval-censored data Jinheum Kim, joint with Chung Mo Nam jinhkim@suwon.ac.kr Department of Applied Statistics University of Suwon Comparing survival
More informationFrailty Modeling for clustered survival data: a simulation study
Frailty Modeling for clustered survival data: a simulation study IAA Oslo 2015 Souad ROMDHANE LaREMFiQ - IHEC University of Sousse (Tunisia) souad_romdhane@yahoo.fr Lotfi BELKACEM LaREMFiQ - IHEC University
More informationDefinitions and examples Simple estimation and testing Regression models Goodness of fit for the Cox model. Recap of Part 1. Per Kragh Andersen
Recap of Part 1 Per Kragh Andersen Section of Biostatistics, University of Copenhagen DSBS Course Survival Analysis in Clinical Trials January 2018 1 / 65 Overview Definitions and examples Simple estimation
More informationA Bayesian Nonparametric Approach to Causal Inference for Semi-competing risks
A Bayesian Nonparametric Approach to Causal Inference for Semi-competing risks Y. Xu, D. Scharfstein, P. Mueller, M. Daniels Johns Hopkins, Johns Hopkins, UT-Austin, UF JSM 2018, Vancouver 1 What are semi-competing
More informationSurvival Analysis I (CHL5209H)
Survival Analysis Dalla Lana School of Public Health University of Toronto olli.saarela@utoronto.ca January 7, 2015 31-1 Literature Clayton D & Hills M (1993): Statistical Models in Epidemiology. Not really
More informationUNIVERSITY OF CALIFORNIA, SAN DIEGO
UNIVERSITY OF CALIFORNIA, SAN DIEGO Estimation of the primary hazard ratio in the presence of a secondary covariate with non-proportional hazards An undergraduate honors thesis submitted to the Department
More informationREGRESSION ANALYSIS FOR TIME-TO-EVENT DATA THE PROPORTIONAL HAZARDS (COX) MODEL ST520
REGRESSION ANALYSIS FOR TIME-TO-EVENT DATA THE PROPORTIONAL HAZARDS (COX) MODEL ST520 Department of Statistics North Carolina State University Presented by: Butch Tsiatis, Department of Statistics, NCSU
More informationLecture 8 Stat D. Gillen
Statistics 255 - Survival Analysis Presented February 23, 2016 Dan Gillen Department of Statistics University of California, Irvine 8.1 Example of two ways to stratify Suppose a confounder C has 3 levels
More informationLecture 3. Truncation, length-bias and prevalence sampling
Lecture 3. Truncation, length-bias and prevalence sampling 3.1 Prevalent sampling Statistical techniques for truncated data have been integrated into survival analysis in last two decades. Truncation in
More information42. EXTENSIONS AND APPLICATIONS OF COMPARE: WEB PLATFORM TO SELECT THE PRIMARY ENDPOINT IN A RANDOMIZED CLINICAL TRIAL
42. EXTENSIONS AND APPLICATIONS OF COMPARE: WEB PLATFORM TO SELECT THE PRIMARY ENDPOINT IN A RANDOMIZED CLINICAL TRIAL M. Gómez-Mateu and G. Gómez Melis Universitat Politècnica de Catalunya, Department
More informationStatistical Analysis of Competing Risks With Missing Causes of Failure
Proceedings 59th ISI World Statistics Congress, 25-3 August 213, Hong Kong (Session STS9) p.1223 Statistical Analysis of Competing Risks With Missing Causes of Failure Isha Dewan 1,3 and Uttara V. Naik-Nimbalkar
More informational steps utilized well as tables
Global malaria mortality between 1980 and 2010: a systematic analysis WEBAPPENDIX Authors: Christopher J L Murray, Lisa C Rosenfeld, Stephen S Lim, Kathryn G Andrews, Kyle J Foreman, Diana Haring, Nancy
More informationOverrunning in Clinical Trials: a Methodological Review
Overrunning in Clinical Trials: a Methodological Review Dario Gregori Unit of Biostatistics, Epidemiology and Public Health Department of Cardiac, Thoracic and Vascular Sciences dario.gregori@unipd.it
More informationA Bayesian Nonparametric Approach to Monotone Missing Data in Longitudinal Studies with Informative Missingness
A Bayesian Nonparametric Approach to Monotone Missing Data in Longitudinal Studies with Informative Missingness A. Linero and M. Daniels UF, UT-Austin SRC 2014, Galveston, TX 1 Background 2 Working model
More informationEstimating direct effects in cohort and case-control studies
Estimating direct effects in cohort and case-control studies, Ghent University Direct effects Introduction Motivation The problem of standard approaches Controlled direct effect models In many research
More informationDependence structures with applications to actuarial science
with applications to actuarial science Department of Statistics, ITAM, Mexico Recent Advances in Actuarial Mathematics, OAX, MEX October 26, 2015 Contents Order-1 process Application in survival analysis
More informationTechnical Track Session I: Causal Inference
Impact Evaluation Technical Track Session I: Causal Inference Human Development Human Network Development Network Middle East and North Africa Region World Bank Institute Spanish Impact Evaluation Fund
More informationADVANCED STATISTICAL ANALYSIS OF EPIDEMIOLOGICAL STUDIES. Cox s regression analysis Time dependent explanatory variables
ADVANCED STATISTICAL ANALYSIS OF EPIDEMIOLOGICAL STUDIES Cox s regression analysis Time dependent explanatory variables Henrik Ravn Bandim Health Project, Statens Serum Institut 4 November 2011 1 / 53
More informationMulti-state Models: An Overview
Multi-state Models: An Overview Andrew Titman Lancaster University 14 April 2016 Overview Introduction to multi-state modelling Examples of applications Continuously observed processes Intermittently observed
More informationPubH 7470: STATISTICS FOR TRANSLATIONAL & CLINICAL RESEARCH
PubH 7470: STATISTICS FOR TRANSLATIONAL & CLINICAL RESEARCH The First Step: SAMPLE SIZE DETERMINATION THE ULTIMATE GOAL The most important, ultimate step of any of clinical research is to do draw inferences;
More informationEstimation for Modified Data
Definition. Estimation for Modified Data 1. Empirical distribution for complete individual data (section 11.) An observation X is truncated from below ( left truncated) at d if when it is at or below d
More informationAn approximate randomisation-respecting adjustment to the hazard ratio for time-dependent treatment switches in clinical trials.
An approximate randomisation-respecting adjustment to the hazard ratio for time-dependent treatment switches in clinical trials. Ian R. White 1 A. Sarah Walker 2 Abdel G. Babiker 2 1 MRC Biostatistics
More information4. Comparison of Two (K) Samples
4. Comparison of Two (K) Samples K=2 Problem: compare the survival distributions between two groups. E: comparing treatments on patients with a particular disease. Z: Treatment indicator, i.e. Z = 1 for
More informationGroup Sequential Tests for Delayed Responses. Christopher Jennison. Lisa Hampson. Workshop on Special Topics on Sequential Methodology
Group Sequential Tests for Delayed Responses Christopher Jennison Department of Mathematical Sciences, University of Bath, UK http://people.bath.ac.uk/mascj Lisa Hampson Department of Mathematics and Statistics,
More informationMonitoring clinical trial outcomes with delayed response: incorporating pipeline data in group sequential designs. Christopher Jennison
Monitoring clinical trial outcomes with delayed response: incorporating pipeline data in group sequential designs Christopher Jennison Department of Mathematical Sciences, University of Bath http://people.bath.ac.uk/mascj
More informationCorrection for classical covariate measurement error and extensions to life-course studies
Correction for classical covariate measurement error and extensions to life-course studies Jonathan William Bartlett A thesis submitted to the University of London for the degree of Doctor of Philosophy
More informationEstimation of Conditional Kendall s Tau for Bivariate Interval Censored Data
Communications for Statistical Applications and Methods 2015, Vol. 22, No. 6, 599 604 DOI: http://dx.doi.org/10.5351/csam.2015.22.6.599 Print ISSN 2287-7843 / Online ISSN 2383-4757 Estimation of Conditional
More informationSupport Vector Hazard Regression (SVHR) for Predicting Survival Outcomes. Donglin Zeng, Department of Biostatistics, University of North Carolina
Support Vector Hazard Regression (SVHR) for Predicting Survival Outcomes Introduction Method Theoretical Results Simulation Studies Application Conclusions Introduction Introduction For survival data,
More informationGroup Sequential Methods. for Clinical Trials. Christopher Jennison, Dept of Mathematical Sciences, University of Bath, UK
Group Sequential Methods for Clinical Trials Christopher Jennison, Dept of Mathematical Sciences, University of Bath, UK http://wwwbathacuk/ mascj University of Malaysia, Kuala Lumpur March 2004 1 Plan
More informationInference on Treatment Effects from a Randomized Clinical Trial in the Presence of Premature Treatment Discontinuation: The SYNERGY Trial
Inference on Treatment Effects from a Randomized Clinical Trial in the Presence of Premature Treatment Discontinuation: The SYNERGY Trial Marie Davidian Department of Statistics North Carolina State University
More informationEffects of a Misattributed Cause of Death on Cancer Mortality
Effects of a Misattributed Cause of Death on Cancer Mortality by Jinkyung Ha A dissertation submitted in partial fulfillment of the requirements for the degree of Doctor of Philosophy (Biostatistics) in
More informationarxiv: v1 [stat.me] 5 Nov 2017
Biometrics 99, 1 24 December 2010 DOI: 10.1111/j.1541-0420.2005.00454.x Likelihood Based Study Designs for Time-to-Event Endpoints arxiv:1711.01527v1 [stat.me] 5 Nov 2017 Jeffrey D. Blume Department of
More informationStatistical Methods for Alzheimer s Disease Studies
Statistical Methods for Alzheimer s Disease Studies Rebecca A. Betensky, Ph.D. Department of Biostatistics, Harvard T.H. Chan School of Public Health July 19, 2016 1/37 OUTLINE 1 Statistical collaborations
More informationβ j = coefficient of x j in the model; β = ( β1, β2,
Regression Modeling of Survival Time Data Why regression models? Groups similar except for the treatment under study use the nonparametric methods discussed earlier. Groups differ in variables (covariates)
More informationConstruction and statistical analysis of adaptive group sequential designs for randomized clinical trials
Construction and statistical analysis of adaptive group sequential designs for randomized clinical trials Antoine Chambaz (MAP5, Université Paris Descartes) joint work with Mark van der Laan Atelier INSERM
More informationRobust estimates of state occupancy and transition probabilities for Non-Markov multi-state models
Robust estimates of state occupancy and transition probabilities for Non-Markov multi-state models 26 March 2014 Overview Continuously observed data Three-state illness-death General robust estimator Interval
More informationChapter 7 Fall Chapter 7 Hypothesis testing Hypotheses of interest: (A) 1-sample
Bios 323: Applied Survival Analysis Qingxia (Cindy) Chen Chapter 7 Fall 2012 Chapter 7 Hypothesis testing Hypotheses of interest: (A) 1-sample H 0 : S(t) = S 0 (t), where S 0 ( ) is known survival function,
More informationSTAT331. Combining Martingales, Stochastic Integrals, and Applications to Logrank Test & Cox s Model
STAT331 Combining Martingales, Stochastic Integrals, and Applications to Logrank Test & Cox s Model Because of Theorem 2.5.1 in Fleming and Harrington, see Unit 11: For counting process martingales with
More informationData Analysis and Statistical Methods Statistics 651
Data Analysis and Statistical Methods Statistics 651 http://www.stat.tamu.edu/~suhasini/teaching.html Lecture 26 (MWF) Tests and CI based on two proportions Suhasini Subba Rao Comparing proportions in
More informationPSI Journal Club March 10 th, 2016
PSI Journal Club March 1 th, 1 The analysis of incontinence episodes and other count data in patients with Overactive Bladder (OAB) by Poisson and negative binomial regression Martina R, Kay R, van Maanen
More informationPhilosophy and Features of the mstate package
Introduction Mathematical theory Practice Discussion Philosophy and Features of the mstate package Liesbeth de Wreede, Hein Putter Department of Medical Statistics and Bioinformatics Leiden University
More informationTwo-stage Adaptive Randomization for Delayed Response in Clinical Trials
Two-stage Adaptive Randomization for Delayed Response in Clinical Trials Guosheng Yin Department of Statistics and Actuarial Science The University of Hong Kong Joint work with J. Xu PSI and RSS Journal
More informationStatistical Issues in the Use of Composite Endpoints in Clinical Trials
Statistical Issues in the Use of Composite Endpoints in Clinical Trials Longyang Wu and Richard Cook Statistics and Actuarial Science, University of Waterloo May 14, 2010 Outline Introduction: A brief
More informationLarge sample inference for a win ratio analysis of a composite outcome based on prioritized components
Biostatistics (2016), 17, 1,pp. 178 187 doi:10.1093/biostatistics/kxv032 Advance Access publication on September 8, 2015 Large sample inference for a win ratio analysis of a composite outcome based on
More informationLecture 12. Multivariate Survival Data Statistics Survival Analysis. Presented March 8, 2016
Statistics 255 - Survival Analysis Presented March 8, 2016 Dan Gillen Department of Statistics University of California, Irvine 12.1 Examples Clustered or correlated survival times Disease onset in family
More informationIntroduction to Statistical Analysis
Introduction to Statistical Analysis Changyu Shen Richard A. and Susan F. Smith Center for Outcomes Research in Cardiology Beth Israel Deaconess Medical Center Harvard Medical School Objectives Descriptive
More informationStatistics 360/601 Modern Bayesian Theory
Statistics 360/601 Modern Bayesian Theory Alexander Volfovsky Lecture 5 - Sept 12, 2016 How often do we see Poisson data? 1 2 Poisson data example Problem of interest: understand different causes of death
More informationComparative effectiveness of dynamic treatment regimes
Comparative effectiveness of dynamic treatment regimes An application of the parametric g- formula Miguel Hernán Departments of Epidemiology and Biostatistics Harvard School of Public Health www.hsph.harvard.edu/causal
More informationEfficiency Comparison Between Mean and Log-rank Tests for. Recurrent Event Time Data
Efficiency Comparison Between Mean and Log-rank Tests for Recurrent Event Time Data Wenbin Lu Department of Statistics, North Carolina State University, Raleigh, NC 27695 Email: lu@stat.ncsu.edu Summary.
More informationStatistical Methods in Clinical Trials Categorical Data
Statistical Methods in Clinical Trials Categorical Data Types of Data quantitative Continuous Blood pressure Time to event Categorical sex qualitative Discrete No of relapses Ordered Categorical Pain level
More informationLecture 4: Generalized Linear Mixed Models
Dankmar Böhning Southampton Statistical Sciences Research Institute University of Southampton, UK S 3 RI, 11-12 December 2014 An example with one random effect An example with two nested random effects
More informationTypical Survival Data Arising From a Clinical Trial. Censoring. The Survivor Function. Mathematical Definitions Introduction
Outline CHL 5225H Advanced Statistical Methods for Clinical Trials: Survival Analysis Prof. Kevin E. Thorpe Defining Survival Data Mathematical Definitions Non-parametric Estimates of Survival Comparing
More informationFactor Analytic Models of Clustered Multivariate Data with Informative Censoring (refer to Dunson and Perreault, 2001, Biometrics 57, )
Factor Analytic Models of Clustered Multivariate Data with Informative Censoring (refer to Dunson and Perreault, 2001, Biometrics 57, 302-308) Consider data in which multiple outcomes are collected for
More informationCTDL-Positive Stable Frailty Model
CTDL-Positive Stable Frailty Model M. Blagojevic 1, G. MacKenzie 2 1 Department of Mathematics, Keele University, Staffordshire ST5 5BG,UK and 2 Centre of Biostatistics, University of Limerick, Ireland
More informationIndividualized Treatment Effects with Censored Data via Nonparametric Accelerated Failure Time Models
Individualized Treatment Effects with Censored Data via Nonparametric Accelerated Failure Time Models Nicholas C. Henderson Thomas A. Louis Gary Rosner Ravi Varadhan Johns Hopkins University July 31, 2018
More informationNonparametric Model Construction
Nonparametric Model Construction Chapters 4 and 12 Stat 477 - Loss Models Chapters 4 and 12 (Stat 477) Nonparametric Model Construction Brian Hartman - BYU 1 / 28 Types of data Types of data For non-life
More informationSample Size and Power I: Binary Outcomes. James Ware, PhD Harvard School of Public Health Boston, MA
Sample Size and Power I: Binary Outcomes James Ware, PhD Harvard School of Public Health Boston, MA Sample Size and Power Principles: Sample size calculations are an essential part of study design Consider
More informationIntegrated likelihoods in survival models for highlystratified
Working Paper Series, N. 1, January 2014 Integrated likelihoods in survival models for highlystratified censored data Giuliana Cortese Department of Statistical Sciences University of Padua Italy Nicola
More informationCompeting risks data analysis under the accelerated failure time model with missing cause of failure
Ann Inst Stat Math 2016 68:855 876 DOI 10.1007/s10463-015-0516-y Competing risks data analysis under the accelerated failure time model with missing cause of failure Ming Zheng Renxin Lin Wen Yu Received:
More informationEvidence synthesis for a single randomized controlled trial and observational data in small populations
Evidence synthesis for a single randomized controlled trial and observational data in small populations Steffen Unkel, Christian Röver and Tim Friede Department of Medical Statistics University Medical
More informationStatistics in medicine
Statistics in medicine Lecture 4: and multivariable regression Fatma Shebl, MD, MS, MPH, PhD Assistant Professor Chronic Disease Epidemiology Department Yale School of Public Health Fatma.shebl@yale.edu
More informationPoisson regression: Further topics
Poisson regression: Further topics April 21 Overdispersion One of the defining characteristics of Poisson regression is its lack of a scale parameter: E(Y ) = Var(Y ), and no parameter is available to
More informationMeei Pyng Ng 1 and Ray Watson 1
Aust N Z J Stat 444), 2002, 467 478 DEALING WITH TIES IN FAILURE TIME DATA Meei Pyng Ng 1 and Ray Watson 1 University of Melbourne Summary In dealing with ties in failure time data the mechanism by which
More informationCHL 5225 H Crossover Trials. CHL 5225 H Crossover Trials
CHL 55 H Crossover Trials The Two-sequence, Two-Treatment, Two-period Crossover Trial Definition A trial in which patients are randomly allocated to one of two sequences of treatments (either 1 then, or
More informationSymmetric Tests and Condence Intervals for Survival Probabilities and Quantiles of Censored Survival Data Stuart Barber and Christopher Jennison Depar
Symmetric Tests and Condence Intervals for Survival Probabilities and Quantiles of Censored Survival Data Stuart Barber and Christopher Jennison Department of Mathematical Sciences, University of Bath,
More informationIntegrated approaches for analysis of cluster randomised trials
Integrated approaches for analysis of cluster randomised trials Invited Session 4.1 - Recent developments in CRTs Joint work with L. Turner, F. Li, J. Gallis and D. Murray Mélanie PRAGUE - SCT 2017 - Liverpool
More informationUsing Geographic Information Systems for Exposure Assessment
Using Geographic Information Systems for Exposure Assessment Ravi K. Sharma, PhD Department of Behavioral & Community Health Sciences, Graduate School of Public Health, University of Pittsburgh, Pittsburgh,
More information4 Testing Hypotheses. 4.1 Tests in the regression setting. 4.2 Non-parametric testing of survival between groups
4 Testing Hypotheses The next lectures will look at tests, some in an actuarial setting, and in the last subsection we will also consider tests applied to graduation 4 Tests in the regression setting )
More informationModule 16: Evaluating Vaccine Efficacy
Module 16: Evaluating Vaccine Efficacy Instructors: Dean Follmann, Peter Gilbert, Erin Gabriel, Michael Sachs Session 6: Effect Modifier Methods for Assessing Immunological Correlates of VE (Part I) Summer
More informationRelative-risk regression and model diagnostics. 16 November, 2015
Relative-risk regression and model diagnostics 16 November, 2015 Relative risk regression More general multiplicative intensity model: Intensity for individual i at time t is i(t) =Y i (t)r(x i, ; t) 0
More information