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# Analysis of Complex Survey Data - PowerPoint PPT Presentation

Analysis of Complex Survey Data. Day 4: Survival analysis and Cox proportional hazards models. Nonparametric Survival Analysis. Kaplan-Meier Method (also called Product-Limit Method) Life Table Method (also called Actuarial Method). Nonparametric Survival Analysis.

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### Analysis of Complex Survey Data

Day 4: Survival analysis and

Cox proportional hazards models

• Kaplan-Meier Method (also called Product-Limit Method)

• Life Table Method (also called Actuarial Method)

A statistical method to study time to an event

Divide risk period into many small time intervals

2) Treat each interval as a small cohort analysis

3) Combine the results for the intervals

• Censoring

• Time to an event

• Survival Function

• At the end of study, subjects did not experience the event (outcome). Or subjects withdrew from a study (lost to follow up or died from other diseases).

• Survival analysis assumes LTF and competing cause censoring is random (independent of exposure and outcome)

• When using longitudinal complex surveys (e.g., PSID, AddHealth), survival analysis is most useful

• We can also use it in cross-sectional studies when incorporating retrospective age of onset information.

28

= .0284

=

985

1,000 - 15

28

= .0280

1,000

28

28

=

= .0282

992.5

1,000 – 7.5

Censoring

Example:

Cohort Size at Start : 1,000 for 1 year

Number with disease : 28

Number LTF: 15

If assume all dropped out on 1st day of study, rate of disease/y

=

If assume all dropped out on last day of study, probability of disease

=

If drop out rate is constant over the period best estimate of when dropped out is midpoint : probability of disease then is

=

The probability of surviving beyond a specific time [i.e., S(t) = 1 – F(t)]

F(t) = cumulative probability distribution for endpoint (e.g., death)

Probability at that time period conditioned “surviving” to that interval

S4

q

S3

p

F

S2

o

F

S1

Probability survival to S4 =

n

n * o * p * q

F

Failures (F) = deaths or cases or losses to follow up

F

• Time is partitioned into a fixed sequence of intervals (not necessarily of equal lengths)

A classical method of estimating the survival function in epidemiology and actuarial science

Interval lengths (arbitrary)

Larger the interval, larger the bias

Useful for large samples

• The LIFETEST Procedure

• Stratum 1: platelet = 0

• Life Table Survival Estimates

• Conditional

• Effective Conditional Probability

• Interval Number NumberSample Probability Standard

• [Lower, Upper) Failed Censored Size of Failure Error Survival Failure

• 0 10 4 0 9.0 0.4444 0.1656 1.0000 0

• 10 20 2 1 4.5 0.4444 0.2342 0.5556 0.4444

• 20 30 0 0 2.0 0 0 0.3086 0.6914

• 30 40 1 0 2.0 0.5000 0.3536 0.3086 0.6914

• 40 50 0 0 1.0 0 0 0.1543 0.8457

• 50 60 1 0 1.0 1.0000 0 0.1543 0.8457

N*

Effective sample size: whenever there is censoring (withdrawal or loss), we assume that, on average, those individuals who became lost or withdrawn during the interval were at risk for half the interval.

Thus, effective sample size (n*)= n – ½ (censoring #)

E.g., effective sample size (1st interval) = 9 – ½ (0) = 9

E.g., effective sample size (2nd interval) = 5 – ½ (1) = 4.5

• The LIFETEST Procedure

• Stratum 1: platelet = 0

• Life Table Survival Estimates

• Conditional

• Effective Conditional Probability

• Interval Number Number Sample Probability Standard

• [Lower, Upper) Failed Censored Size of Failure Error Survival Failure

• 0 10 4 0 9.0 0.4444 0.1656 1.0000 0

• 10 20 2 1 4.5 0.4444 0.2342 0.5556 0.4444

• 20 30 0 0 2.0 0 0 0.3086 0.6914

• 30 40 1 0 2.0 0.5000 0.3536 0.3086 0.6914

• 40 50 0 0 1.0 0 0 0.1543 0.8457

• 50 60 1 0 1.0 1.0000 0 0.1543 0.8457

P(F)

Conditional Probability of Failure: Number failed / Effective Sample Size

e.g., P(F) (1st interval) = 4/9 = .44

e.g., P(F) (2nd interval) = 2/4.5 = .44

Survival probability (in each interval) = 1- failure probability (in each interval)

Cum Survival Prob (S(t)) = S (t-1) * S(t)

e.g., S(1) = 1 * (1-.4444) = 1* 0.5556 =.5556

e.g., S(2) = S(0)* S(1) * S(2)

S(2) =1*(1-.4444)* (1-.4444) =1 * .5556 * .5556 = .3086

• Time is partitioned into variable intervals

Whenever a case arises, set up a time interval. Use the actual censored and event times

If censored times > last event time, then the average duration will be underestimated using KM method

Patient 1

died

Patient 2

Lost to follow-up

Patient 3

died

Patient 4

died

Patient 5

Lost to follow-up

Patient 6

died

4

10

14

24

Months Since Enrollment

% Surviving

100

.833

80

.625

60

.417

40

20

.0

0

0

4

10

14

24

Months After Enrollment

.

Tort

No Fault 1

No Fault 2

“Effect of eliminating compensation for pain and suffering on the outcome of insurance claims for whiplash injury” Cassidy JD et al., N Engl J Med 2000;342:1179-1186

Tort

No Fault 1

No Fault 2

• Not required to choose some particular probability distribution to represent survival time

• Incorporate time-dependent covariates

Example: exposure increases over time as with drug dosage or with workers in hazardous occupations

• 1. Proportional Hazards Model

Basic Model of the hazard for individual i at time t

hi(t) = 0(t) exp{β1xi1 + ….. + βkxik}

Linear function of fixed covariates

Baseline hazard function

Non-negative

Take the logarithm of both sides,

log hi(t) = (t) +β1xi1 + ….. + βkxik

No need to specify the functional form of baseline hazard function

log 0(t)

• 1. Proportional Hazards Model

Consider the hazard ratio of two individuals i and j

hi(t) = 0(t) exp{β1xi1 + ….. + βkxik}

hi(t) = 0(t) exp{β1xj1 + ….. + βkxjk}

Hazard ratio = exp{β1(xi1 -xj1) ….. + βk(xik-xjk)}

• Hazard functions are multiplicatively related, hazard ratio is constant over survival time.

• Hazards of any two individuals are proportional.

• 2. Partial Likelihood Estimation

Estimate the β coefficients of the Cox model without having to specify the baseline hazard function 0(t)

Partial likelihood depends only on the order in which events occur, not on the exact times of occurrence.

Partial likelihood estimates are not fully efficient because of loss of information about exact times of event occurrence

• No intercept h0(t): an arbitrary function of time. Cancel out of the estimating equations

eβ: Hazard ratio

Indicator variables (coded as 0 and 1)

Hazard ratio of the estimated hazard for those with a value of 1 in X to the estimated hazard for those with a value of 0 in X (controlling for other covariates)

Quantitative (Continuous) variables

Estimated percent change in the hazard for each one-unit increase in X. For example, variable AGE, eβ=1.5, which yields 100(1.5 - 1) =50. For each one-year increase in the age at diagnosis, the hazard of death goes up by an estimated 50 percent, controlling for other covariates.