Luca Pozzi JSM 2011
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A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
A Bayesian Adaptive Dose SelectionProcedure with Overdispersed Count
Endpoint
Luca Pozzi
University of California, Berkeley
August 1st, 2011 - Joint Statistical Meeting, Miami Beach, FL
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Motivating Example: Problem Setting
Objective: Lowest Effective Dose (LED), i.e. dose whose efficacyis at least 50% better than Placebo (Dose 1) andat most 20% worse than the highest dose (Dose 5);
Design of the Study: Start with initial allocation 1:a:b:c:1 then atinterim stop or select the most promising dose d for asecond phase with only Placebo, Dose d and Dose 5;
Endpoint: Overdispersed count data Y modeled by the negativebinomial distribution (gamma-poisson mixture):{
Y |λ ∼ Pois(λ)λ|(α, β) ∼ Gamma(α, β)
Dose-Response Relationship: Sigmoidal relationship
e.g. EMAX -model: E(d) = E0
(1 − EMAX d
ED50+d
).
Strong prior information available for Placebo (E0) andhighest dose (EMAX );
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Modeling Dose-Response Relationship
1st challenge: Modeling
Too few doses to adopt Parametric Dose-Response model.(Adaptive design will start with only one lower dose)
Strategy: Semiparametric Specification
The mode of action of the drug and Ph.III outcomes suggestthat a monotonicity constraint holds for the dose-responserelationship:
Mm ={µj ≡ E[Yij] : E0 = µ1 ≥ µ2 ≥ µ3 ≥ µ4 ≥ µ5 = EMAX
}
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Modeling Approach
Bayesian Model Averaging: Ingredients
1 A set of mutually exclusive modelsM = {M1, ...,MM}.To each model corresponds a probability distributionf(y |θ(m),Mm);
2 One set of priors g(θ(m)|Mm) on θ(m) for eachMm;
3 A vector of prior model probabilitiesπ = (π1, ..., πM), πm = P{Mm}, (e.g. πm = 1
M ), ∀m = 1, ...,M.
We have then
P{success|y} =M∑
m=1
P{success|Mm, y}P{Mm |y}
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Bayesian model
Gamma-Poisson mixture
Yij |λij ∼ dpois(λij) (i-th patient-j-th dose group);λij |αj , β ∼ dgamma(αj , β)
So Yij marginal distribution is a dnegbin(αj , β)
Priors
log(α1) ∼ N(µα, σ2α);
α|m ∼ fm � λd(m)
log(β) ∼ N(0, σ2β)
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Monotonicity Constraints
We introduce the jump variables
δk = log(αk ) − log(αk−1) ≥ 0
δk , 0 iff αk > αk+1
and we put a truncated normal prior on
δsum =4∑1
δk = log(α1) − log(α5) ∼ TN(µsum, σ2sum)
being TN a normal distribution folded around its mean:formally if Z ∼ N(0, 1) then X ∼ TN(ν, τ2)⇐⇒ X = ν + τ|Z |
α1 ≥︸︷︷︸δ1,m
α2 ≥︸︷︷︸δ2,m
α3 ≥︸︷︷︸δ3,m
α4 ≥︸︷︷︸δ4,m
α5
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Jump×Model Matrix
∆ =
δ1,1 0 δ1,3 δ1,4 0 0 0 0 0 δ1,3
δ2,1 δ2,2 δ2,3 δ2,4 0 δ2,6 0 δ2,8 0 0δ3,1 δ3,2 δ3,3 0 δ3,5 δ3,6 0 0 δ3,9 0δ4,1 δ4,2 0 0 δ4,5 0 δ4,7 0 0 0
e.g. M5: µ1 = µ2 = µ3 > µ4 > µ5
α1 = α2 = α3 >︸︷︷︸δ3,5
α4 >︸︷︷︸δ4,5
α5
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Criteria
Futility-Success
Exclusion criterion P{µd/µ1 ≥ 0.7|data} ≥ 50%, i.e. Dose d is notsuperior to Placebo.
Efficacy criterion is the intersection of the following events:
(i) the dose is far enough from Dose 1
P{µd/µ1 < 1|data} ≥ 95%
(ii) the dose is either at least 50% betterthan Dose 1, or at most 20% worsethan Dose 5.
max{P{µd/µ1 ≤ 0.5|data}P{µd/µ5 ≤ 1.2|data}
}≥ 50%
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Interim decision
At Interim
• if Dose 4 meets Exclusion criterion stop for futility: nodose lower than Dose 5 is effective;
• if Dose 2 meets Efficacy criteria stop for success: Dose 2is the LED;
• otherwise, for each not futile Dose d calculate thePredictive Probability of Success (PPS) and allocate tothe lowest dose for which
P{{(i)|Ad ,Y∗,Y } ∩ {(ii)|Ad ,Y∗,Y } > 50%|Y } ≥ t (1)
with Ad = {allocate to Dose d}.
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Decision Tree
Begin Trial
A3
A2
�LED = d2
A4
�LED = d4
�LED = d3
�LED = d3
�LED = d2
�LED = d2
�LED = d4
�LED = d4
�LED = d3
�LED�
�LED�
�LED�
�LED�
�LED = d2
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Performing Predictive Probability Calculations
2nd challenge: Computational
Not feasible to use WinBUGS for Predictive calculations
Stategy: Importance Sampling
Sample from the posterior sample using weighted resampling:{(α, β)(1), ..., (α, β)(N)
}→ (α, β)∗
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Algorithm: Predictive Resample
1 Sample (α, β)(1), ..., (α, β)(k), ..., (α, β)(N);2 Select Dose d;3 for l = 1, ..., L draw (α, β)(l) from the posterior sample at
interim of size N;4 simulate one dataset Y∗(l)
d |(α, β)(l),Ad ;
SIR
5 compute p(Y (l)
d |(α, β)(k)), k = 1, ...,N;
6 compute wk =l(θk ;Y∗)∑j l(θj ;Y∗)
=p(Y∗(l)
d |(α,β)(k))∑j p(Y∗(l)
d |(α,β)(j));
7 compute by resampling PP(l)d [criterion] for each criteria;
In the end
PPd = mean
(1{ ⋂{criteria}
{PP(l)d [criterion] > c}
})L
l=1
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Posterior Probability of Success
Instead of the above predictive criterion we could require a dose tosatisfy an upper bound on the posterior power. By an argument ofconditional probability we can show it equivalent to a smoothedversion of the predictive criterion:
P{θ ∈ ΘE |Aj ,Y } = EY∗
[P
{θ ∈ ΘE |Aj ,Y ∗,Y
}|Aj ,Y
](2)
beingPPS = PY∗ {P{θ ∈ ΘE |Y ∗,Y ,Aj} ≥ c |Aj ,Y }
Markov inequality gives us the following:
Posterior Lower Bound
PPS ≤EY∗
[P
{θ ∈ ΘE |Aj ,Y∗,Y
}|Aj ,Y
]c
=P{θ ∈ ΘE |Aj ,Y }
c(3)
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Dose-Response Relationships
Optimistic Scenario
dose
α
0.00.2
0.40.6
0.81.0
d1 d2 d3 d4 d5
Flat a
dose
α
0.00.2
0.40.6
0.81.0
d1 d2 d3 d4 d5
Flat b
dose
α
0.00.2
0.40.6
0.81.0
d1 d2 d3 d4 d5
Pessimistic Scenario
dose
α
0.00.2
0.40.6
0.81.0
d1 d2 d3 d4 d5
Moderate Scenario
dose
α
0.00.2
0.40.6
0.81.0
d1 d2 d3 d4 d5
Borderline Moderate Scenario
dose
α
0.00.2
0.40.6
0.81.0
d1 d2 d3 d4 d5
red represents the real LED (“right” dose).
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Simulation Setup
Initial Allocation: assuming we start with 1 : a : b : c : 1:• a = 0, b = 1, c = 0, i.e. 1:0:1:0:1;• a = 1, b = 1, c = 1, i.e. 1:1:1:1:1;• a = 1, b = 2, c = 1, i.e. 1:1:2:1:1.
Predictive Probability Threshold: t =
0.40.50.6
Number of Patients: split the 250 patients between the firstand the second phase:• 1/3 at interim and 2/3 for the next phase;• half at interim and half for the next phase.
Size: 500 simulations with 500 simulated studies forprediction and N = 104 for the resampling.
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Operation Characteristics (Adaptive Design)
Moderate scenario
Let us consider P{ “right” dose} in the Moderate Scenario:
1:0:1:0:1 1:1:1:1:1 1:1:2:1:10.4 0.5 0.6 0.4 0.5 0.6 0.4 0.5 0.6
1/2 0.818 0.878 0.996 0.774 0.818 0.768 0.730 0.794 0.8481/3 0.860 0.860 0.996 0.818 0.858 0.814 0.734 0.780 0.864
1/2 0.670 0.762 0.894 0.658 0.732 0.722 0.670 0.724 0.7301/3 0.516 0.772 0.896 0.702 0.750 0.748 0.688 0.746 0.744
Performances of not-adaptive design
Optimistic Moderate Flat(a) Flat(b) PessimisticP{right dose} 0.982 0.84 0.26675 0.3924688 0.94P{Success} 1.000 1.00 0.36775 0.6775810 0.06
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Operation Characteristics: Cheaper Solution
Expected number of patients (total sample size = 250)
1:0:1:0:1 1:1:1:1:1 1:1:2:1:150%-50% 30%-70% 50%-50% 30%-70% 50%-50% 30%-70%
Optimistic 250 250 137.75 129.67 144.5 149.67Moderate 250 250 232.25 236.67 237.75 238.67
Flat (a) 191.88 178 180.5 151.17 168.12 151.5Flat (b) 231.88 216.17 216.5 191.33 216.5 195.33
Pessimistic 250 250 183 177.33 188.67 188.33
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Operation Characteristics: Effect of Thresholds
2 3
Optimistic 010−30 (t=0.4)
PPS LED
0.0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
2 3
Optimistic 010−30 (t=0.5)
PPS LED
0.0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
2 3
Optimistic 010−30 (t=0.6)
PPS LED
0.0
0.2
0.4
0.6
0.8
2 3 5
Optimistic 010−30 (t=0.4)
Posterior LED
0.0
0.1
0.2
0.3
0.4
0.5
2 3 5
Optimistic 010−30 (t=0.5)
Posterior LED
0.0
0.1
0.2
0.3
0.4
0.5
2 3 5
Optimistic 010−30 (t=0.6)
Posterior LED
0.0
0.1
0.2
0.3
0.4
0.5
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Operation Characteristics: Posterior vs. Predictive
2 3
Moderate 111−50 (t=0.4)
PPS LED
0.0
0.2
0.4
0.6
2 3
Moderate 111−50 (t=0.5)
PPS LED
0.0
0.2
0.4
0.6
0.8
2 3 4
Moderate 111−50 (t=0.6)
PPS LED
0.0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
2 3 5
Moderate 111−50 (t=0.4)
Posterior LED
0.0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
2 3 5
Moderate 111−50 (t=0.5)
Posterior LED
0.0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
2 3 4 5
Moderate 111−50 (t=0.6)
Posterior LED
0.0
0.1
0.2
0.3
0.4
0.5
0.6
0.7
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Summarizing
1 The procedure succeeds in detecting the properties ofdifferent Scenarios.
2 The Adaptive Design, when using an appropriatethreshold, is more efficient than the non-adaptive one interms of number of patients and not inferior in terms ofsensitivity and specificity.
3 The BMA allows for correction of suboptimal interimdecisions about the allocation.
4 Increasing the threshold we require the dose to have ahigher margin of superiority (0.6 too strict).
5 The 1/3 - 2/3 proportion and the 1:0:1:0:1 allocation aredefinitely less efficient than the other configurations.
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Some References
1 D.Ohlssen, A.Racine, A Flexible Bayesian Approach forModeling Monotonic Dose-Response Relationships inClinical Trials with Applications in Drug Development,Computational Statistics and Data Analysis,(UnderRevision);
2 A.F.M Smith, A.E. Gelfand, Bayesian Statistics withoutTears, The American Statistician, (1992);
3 J.A.Hoeting, D.Madigan, A.E.Raftery , C.T.Volinsky,Bayesian Model Averaging: a Tutorial (with Discussion).Statistical Science, (1999);
4 A.Doucet, A.M.Johansen et al., A Tutorial on ParticleFiltering and Smoothing: Fifteen Years Later. Tech.Report U.B.C., (2008)
A BayesianAdaptive Dose
SelectionProcedure withOverdispersed
CountEndpoint
Luca Pozzi
Introduction
BayesianModelAveragingDose-Response
Framework
Application
Study LayoutDecision Rules
Computations
Simulations
ResultsConclusions
References
Thanks
Acknowledgements
Thank you for your attention!!!
Authors
Luca Pozzi, U.C. BerkeleyAmy Racine, NovartisHeinz Schmidli, NovartisMauro Gasparini, Politecnico di Torino
Special Thanks to
David Ohlssen, NovartisJouni Kerman, Novartis
Funding
American Statistical Association, San Francisco-Bay Area ChapterTravel Award.MIUR (Italian Ministry for University and Research), PRIN 2007prot. 2007AYHZWC ”Statistical methods for learning in clinicalresearch”.