ming t tan, phd university of maryland greenebaum cancer center email: [email protected]@umm.edu 2006...
TRANSCRIPT
Ming T Tan, PhD
University of Maryland Greenebaum Cancer Center
Email: [email protected]
2006 D.O.E. Presentation 7/11/2006
Optimized Experimental Optimized Experimental Design for Detecting Synergy Design for Detecting Synergy in Drug Combination Studiesin Drug Combination Studies
Combination StudiesCombination Studies Motivation:
achieve greater efficacy with lesser toxicity provide a firmer basis for potential clinical
trials
Joint action is divided into three types:
1. Independent joint action
2. Simple similar (additive) action
3. Synergistic/antagonistic action
Current Design MethodsCurrent Design Methods
Equally regression lines (Finney, 1971)
An optimal design by fixing the total dose for specific models (Abdelbasit & Plackett, 1982)
Fixed ratio design (Tallarida et al., 1992)
An optimal design for in vitro combination studies (Greco et al., 1994) but the sample size too large
Uniform design based on the log-linear single dose-response (Tan et al., 2003)
Model FormulationModel FormulationThe individual dose-response curves of drugs A and B are assumed: and
The potency of B relative to A is
For the additive action of A and B, the regression line for the mixture is
H0: f = 0 versus H1: f 0.
The general nonparametric model for the combinations of A and B is assumed
)( AA xfy )( BB xfy
)()( 1BBAB xffx
where the function is unspecified,
Then, testing the additive action of A and B is equivalent to testing
))(( BBAA xxxfy
( ) ( , )AA A B A B
B
Xy f x x f x x
X
),( BA xxf ),0(~ 2 N
Model AssumptionsModel Assumptions
With an invertible transformation: we have the additive structure
and the model becomes
where g1 and g2 are linearly independent,
and satisfies the orthogonal condition:
),(),,( 212211 zzxzzx BA
1 1 1 2 2 2( ) ( ) ( )AA A B
B
Xf x x g z g z
X
),()()( 21222111 zzgzgzgy
),(),( 21 BA xxfzzg
T
SzgzgzzGdzdzzzgzzG
)(),(),(,0),(),( 221121212121
Model Formulation (cont’)Model Formulation (cont’)
Hence, testing the additive action of A and B is equivalent to testing H0: g = 0 versus H1: g 0
if g = 0, additive action in the mixture of A and B is implied; if g > 0, synergism in the mixture of A and B is implied; if g < 0, antagonism in the mixture of A and B is implied.
The meaningful amount ( >0) of synergism or antagonism to be detected is specified by:
S
dzdzzzg 22121
2 ),(
Statistical InferenceStatistical InferenceSuppose that are m mixtures of A and B in domain S
ni experiments at the dose-level,
yij are the corresponding responses,
y: n 1 vector with elements yij ordered lexicographically,
I: the unit matrix, 1k: the k1 vector of one,
Z: m2 matrix with i-th row
Under H0, mnmT
T
FmnyJIy
myVJyF
,2~
)()(
)2()(
mww ,...,1
Szzw Tiii ),( 21
mi nnnminj ...;,...,1,,...,1 1
))(),(( 2211 ii zgzg
)1,...,1(1 mnndiagU
TTTT UZUZUZUZV 1)( TT UUUUJ 1)(
Statistical Inference (cont’)Statistical Inference (cont’)
S gTg bBbwdwg
n
,
1,
22
)()(
)()()(),()()( , wdwgwGbwdwGwGBSgS
T
)(~ ,2 mnmFF Under H1: with
where
is the design measure, which is a probability measure with mass pi = ni /n, i=1,2,…,m.
If is uniformly distributed on S, then
and is maximized,
Uniform design measure maximizes the minimum power of the F-test for the additive action of drugs A and B.
0, gb
S
wdwgn
)()(22
Uniform Scattered Points on Uniform Scattered Points on CC22
Fm(x) be the empirical distribution function of Pm,
F(x) be the uniform distribution function in C2.
Discrepancy:
Let Um,2=(uij) be an m 2 matrix, each column is a permutation
of {1,2,…,m}. Define vij=(uij - 0.5)/m, i=1,…,m; j=1,2,
and Vm,2 can be considered as m points on C2.
Then the uniform design is to choose the m points so that the discrepancy of Vm,2 is the smallest over all of possible Vm,2.
)1,0()1,0(,..., 21 CxxP mm
)()(sup)(2
xFxFPD mCx
m
Example: Example: Uniform Scattered Points on Uniform Scattered Points on CC22
A uniform design with 7 experimental units on C2:
Discrepancy: 0.1582
(smallest)
The 7 experiment units: (0.071, 0.643),
(0.214, 0.214),
(0.357,0.929),
(0.5, 0.5),
(0.643, 0.071),
(0.786, 0.786),
(0.929, 0.357).
T
U
3614725
76543212,7
v1
v2
0.0 0.2 0.4 0.6 0.8 1.0
0.0
0.2
0.4
0.6
0.8
1.0
Uniform Experimental DesignUniform Experimental DesignSuppose the experimental domain
(vi1, vi2)T, i=1,…,m; are m UD points on C2.
The m Uniform design points on S are
i=1,…,m
Then, m mixtures {(xAi, xBi): i=1,…,m} of drugs A and B for experiment can be obtained by the inverse transform.
HLHL ZzZZzZzzS 22211121 ,:),(
LLHii
LLHii
ZZZvz
ZZZvz
22222
11111
)(
)(
Sample Size DeterminationSample Size Determination The sample sizes (number of experimental units) to detect a
given meaningful synergism or antagonism can be calculated in term of the noncentral F-distribution.
When the alternative hypothesis H1 holds, the statistic
Given: type I error rate (), power level (1- ), measurement
variation (2), smallest meaningful difference (),
the sample sizes can be obtained by
22,2 ),(~ nFF mnm
km
xmFP
k
exFP mnkm
k
k
22
)2(
!
)2/()( ,22
0
2/
Typical Designs: # of ExperimentsTypical Designs: # of Experiments(( = 0.05, 1- = 0.05, 1- =0.80) =0.80)
Number of Replications
1 2 3 4 5 6
d = 0.2 --78
(234)42
(168)27
(135)19
(114)14 (98)
d = 0.3107
(214)40
(120)21 (84)
14 (70)
10(60)
7(49)
d = 0.468
(136)25 (75)
14 (56)
9 (45)
3 (18)
3 (21)
d = 0.548 (96)
18 (54)
10 (40)
6 (30)
3 (18)
3 (21)
d = 0.824 (48)
9 (27)
4 (16)
3 (15)
3 (18)
3 (21)
22 /d
Layout of Experimental DesignLayout of Experimental Design1. Analyze single agent data and estimate single agent dose
effects;2. Choose the meaningful difference (2) and calculate the
number of mixtures m; The variation (2) is estimated by the pooled variance from the two single agent experiments.
3. Define the domain S (e.g. ED20 to ED80) and find m mixtures of compounds A and B;
4. Upon completion of the experiment, use the F statistic to test the hypothesis of the additive action of A and B;
5. If p-value > 0.05, no detectable synergism;6. Otherwise, we conclude the two compounds are
synergistic or antagonistic.
Using regression model selection methods to further diagnose the type of joint action of the two compounds
Designs for Specific Dose-EffectsDesigns for Specific Dose-Effects(i) (i) Linear dose-response curvesLinear dose-response curves
The single dose-respose curves are E is the fractional effectThe curves are produced in the low dose/low effect region for many agents: ionising radiation, enzyme inhibitors, mutagens, agents causing chromosomal abnormalities and environmental carcinogens.
The potency of B relative to A: Model for the additive action:
In combination experiment, the m mixtures should be uniformly scattered in the domain
BBBAAA xxExxE )(,)(
AB /
BBAABA xxxxE ),(
mixx BiAi ,...,1),,(
21,21:),( bxbaxaxxS BABA
Designs for Specific Dose-EffectsDesigns for Specific Dose-Effects(ii) (ii) Linear-log dose-response curvesLinear-log dose-response curves
The single dose-respose curves are
The potency of B relative to A:
Model for the additive action:
In combination experiment, m combinations
should be uniformly scattered in the domain
Specially, when A=B, the total doses and the mixing
proportions scatter uniformly on the domain. (Tan, et al. 2003)
BBBAAA xyxy log,log
]/)exp[(,)( 0/
0 AABBBABxx
00 )1(loglog AAAA zy AB
AB
BA
AABA
xx
xxxz
/
/ ,
miz Aii ,...,1),,(
)1,0(),( HL ZZS
Designs for Specific Dose-EffectsDesigns for Specific Dose-Effects(iii) (iii) Sigmoid dose-response curvesSigmoid dose-response curves
The single dose-respose curve
or
where M is the median effective dose or concentration andm is a constant giving the order of sigmoidicity of the curve.The curves have been used in enzymology, also in studies ofdrugs causing muscle contraction, neuronal activators,inhibitorsof cell proliferation and tumor promoters, and in generaltoxicology. The experimental design is the same as in the case (ii).
mMxxExE )/())(1/()(
)log(log))](1/()(log[ MxmxExE
Designs for Specific Dose-EffectsDesigns for Specific Dose-Effects(iv) (iv) Simple exponential dose-response curves, Simple exponential dose-response curves,
survivor multiplicationsurvivor multiplication
The single dose-response curve
S is the survival rate.
Exponential dose-response curves are typically found in cell survival experiments with ionising and non-ionising radiation and other agents with dammage DNA, particularly alkylating agents.
Since the experimental design is same as in the case (i).
)exp()( xxS
xxS )(log
Example: SAHA+VP-16Example: SAHA+VP-16 Goal: to determine the effect of SAHA combined with VP-16 against the cell line HL-60
SAHA: 60 observations, dose range from 0.03 M to 10 M mean viability: 67.57%, standard deviation: 37.47 the dose-response curve
VP-16: 60 observations, dose range from 0.003 M to 3 M mean viability: 64.05%, standard deviation: 27.88
The potency of VP-16 relative to SAHA is 9.12.
)021.0log(9.1125.64 Sy
)0012.0log(9.1197.37 Vy
SAHA+VP-16: Experimental DesignSAHA+VP-16: Experimental DesignThe pooled variance: 836.176
the meaningful difference: 15% viability
type I error rate: 0.05, power: 80%.
Sample size: 90 (18 mixtures with 5 replications)
The U-type matrix with 18 experiments (discrepancy: 0.0779)
Dose range: 0.019M to 2.974M according to VP-16
(the viability is from 25% to 85%)
T
U
113146179112415718102135168
1817161514131211109876543212,18
SAHA+VP-16: SAHA+VP-16: Mixtures for combination experimentMixtures for combination experiment
Exper.# SAHA (M)
VP-16
(M)
Exper.# SAHA
(M)
VP-16
(M)
1 0.405 0.060 10 2.820 1.273
2 2.104 0.038 11 10.175 0.631
3 1.000 0.323 12 0.504 1.855
4 3.780 0.183 13 8.940 1.094
5 0.579 0.696 14 18.708 0.187
6 4.458 0.437 15 6.707 1.667
7 9.651 0.031 16 17.556 0.642
8 4.138 0.800 17 3.476 2.350
9 10.412 0.276 18 15.406 1.206
SAHA+VP-16:SAHA+VP-16:Results of Combination ExperimentResults of Combination Experiment
Dose ranges:
SAHA: 0.405~18.708M,
VP-16: 0.031~2.35M
90 observations:
viability: 16.27%~113.06%
mean:29.27%
standard error: 15.92
F-test: F(3, 85)=60.63
p-value<0.0001
We reject H0:
SAHA with VP-16 against HL-60 has the additive action
SAHA+VP-16: Synergy AnalysisSAHA+VP-16: Synergy AnalysisThe response regression model of combination study (1)
The expected response model for the additive action of SAHAand VP-16 should be
(2)
Compare the equations (1) and (2):· If (1)-(2) = 0, SAHA and VP-16 is additive;· If (1)-(2) < 0, SAHA and VP-16 is synergistic;· If (1)-(2) > 0, SAHA and VP-16 is antagonistic.
)log(12.6)log(14.795.33 VSy
12.90222.0
021.0)12.91(log4.5)0222.0log(9.11
VS
SVSy
SAHA+VP-16: Contour PlotSAHA+VP-16: Contour Plot
1 6 11 16
SAHA (uM)
0.1
0.6
1.1
1.6
2.1
VP
-16
(u
M)
Synergy
Synergy
ConclusionsConclusions Based on the single dose-effect curves, we proposed an
optimal design for testing the additive joint action of two compounds in vitro or in vivo.
under a general dose-response model, the maximum information is extracted by having the experimental points scattered uniformly on the two-dimensional experimental domain.
The design is optimal: Minimizing the variability in modeling synergism and extracting maximum information on the joint action of two compounds.
The number of experimental units (or runs) are quite feasible in vitro or in vivo.
AcknowledgementsAcknowledgements
Ming Tan, PhD Guoliang Tian, PhD Peter Houghton, PhD Douglas Ross, M.D., PhD Ken Shiozawa, PhD.