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Brief Review
Complete Factorial Experiments Completely Randomized Designs Main Effects Interactions Analysis of Variance
Sums of Squares Degrees of Freedom Tests of Factor Effects
Multiple Comparisons of Means Orthogonal polynomials Fractional Factorial Experiments
Half Fractions, Higher-Order Fractions Aliases (Confounding), Design Resolution
Screening experiments
Extra Sum of Squares
Hierarchy PrincipleHierarchy Principle
An interaction is included only if ALL main effects An interaction is included only if ALL main effects and lower-order interactions involving the interaction factorsand lower-order interactions involving the interaction factors
are included in the model and analysisare included in the model and analysis
Full ModelFull Model All hierarchical model terms
Reduced ModelReduced Model One or more model terms deleted All remaining model terms are hierarchical
Hierarchical Models
ey
ey
ey
Models alHierarchic
ijklikkiijkl
ijklikkjiijkl
ijklikijkjiijkl
ey
ey
ey
Models alhierarchic-Non
ijklikiijkl
ijklijkkjiijkl
ijklikijjiijkl
Extra Sum of Squares F-Testfor Hierarchical Models
FullMS
ESS/dfF
Statistic F
dfdfdf
Freedom of Degrees Extra
(Full)SS(Reduced)SSESS
Squares of Sum Extra
E
ESS
FullReducedESS
EE
For Balanced Designs, F Tests for Fixed Effects Derived from QF, Mean Squares, and ESS are Identical
General Method for Quantifying Factor Main Effects and Interactions
Main Effects for Factor A
Main Effects for Factor B
Interaction Effects for Factors A & B
y i y
y j y
(y - y ) - (y
y - y - y
ij
ij i
j i
j
y
y
)
Change in Average Response Due toChanges in the Levels of Factor A
Change in Average Response Due toChanges in the Levels of Factor B
Change in Average Response DueJoint Changes in Factors A & Bin Excess of Changes in the MainEffects
Individual Prespecified Comparisons(Single-factor Model Used for Illustration)
E2e
2ie
ii
ii
MSˆ
r/cˆSE
ycˆ
c
Ho: = 0 vs Ha: 0
Reject Ho if | t | > t /2
SE
-ˆ=t 0
Very general resultVery general result
MGH Sec 6.2.2
Pairwise Comparisons
E2e
e
ii
iiii
MSˆ
r/2ˆSE
yyˆ
Specific
application
Specificapplication
ii,j 0c
-1,c 1,c :Note
j
ii
Ho: i i’ vs Ha: ii’
Reject Ho if | t | > t /2
SE
yy=t .i.i
Ordinary t-Test
Algebraic Main Effects Representation
M(A) = y - y
(y + y ) / 2 - (y + y ) / 2
= (-y - y + y + y ) / 2
= / 2
2 1
21 22 11 12
11 12 21 22
A
m 'y
y = (y11 y12 y21 y22)
m A= ( -1 -1 +1 +1)
M(B) = mB’y/2 m B= ( -1 +1 -1 +1)
Two Factors, Two Levels (No Repeats for Simplicity)Two Factors, Two Levels (No Repeats for Simplicity)
Algebraic Interaction Effects Representation
I(AB) = {M(A) - M(A)
= {(y - y ) - (y - y )} / 2
= (+y - y - y + y ) / 2
= / 2
B=2 B=1
22 12 21 11
11 12 21 22
AB
} / 2
m 'y
y = (y11 y12 y21 y22)
m AB= ( +1 -1 -1 +1)
Two Factors, Two Levels (No Repeats for Simplicity)Two Factors, Two Levels (No Repeats for Simplicity)
Effects Representation :Two-Level, Two-Factor Factorial
Factor Levels: Lower = - 1 Upper = +1
Factor Levels Effects RepresentationFactor A Factor B A B AB
LowerLowerUpperUpper
LowerUpperLowerUpper
-1-1 1 1
-1 1-1 1
1-1-1 1
Note: AB = A x B
MGH Table 5.6
MutuallyOrthogonalContrasts
MutuallyOrthogonalContrasts
Calculated Effects
y = Vector of Averages Across Repeats (Response Vector if r = 1)
m = Effects RepresentationVector
Effect = m’ y / 2k-1
s2rm/m(Effect) SE e
1/221-k
tF ,
Effect Estimated SEEffect Estimated
t
0m:H Under
2
0
Pilot Plant Chemical-Yield Study
MGH Table 6.4
Source dfSum ofSquares
MeanSquares F
pValue
Temperature 1 2,116 2,116 264.50 .000Concentration 1 100 100 12.50 .008Catalyst 1 9 9 1.13 .320Temp x Conc 1 9 9 1.13 .320Temp x Cat 1 400 400 50.00 .000Conc x Cat 1 0 0 0 1.000T x Co x Ca 1 1 1 0.13 .733Error 8 64 8Total 15 2699 Conclusion ?Conclusion ?
2
E Effect Estimated SEEffect Estimated
MSMS
F
Multiple Comparisons
Several comparisons of factor meansor of factor effects using procedures that control
the overall significance or confidence level
Several comparisons of factor meansor of factor effects using procedures that control
the overall significance or confidence level
Comparisonwise Error RateC = Pr(Type 1 Error) for one statistical test
Experimentwise Error RateE = Pr(One or More Type 1 Errors) for two or more rests
Experimentwise Error Rate :k Independent Statistical Tests
j if ) - (1 - 1
) - (1 - 1
Cjk
C
k
1=jjE
Experimentwise & Comparisonwise Error Rates
k 1 2 3 4 5 10 20
E .050 .098 .143 .185 .226 .401 .642
Dependent Tests
kCE ) - (1 - 1 Common MSE
Lack of Orthogonality
Common MSE
Lack of Orthogonality
C
Assumes IndependenceAssumes Independence
Fisher’s Least Significant Difference (LSD)
2/11-2
11E/2
21
21
)}n + n(MS){( t= LSD
where
LSD > | y - y |
ifdifferent tly significan are y and y
C
Protected: Preceded by an F Test for Overall SignificanceUnprotected: Not Preceded by an F Test – Individual t Tests
MGH Exhibit 6.9
Least Significant Interval (LSI) Plot
2/11-2
11E/2
21
21
)}n + n(MS){( t= LSD
where
LSD > | y - y |
ifdifferent tly significan are y and y
C
LSI Plot Plot the averages, with bars extending LSD/2 above & below each average. Bars that do NOT overlap indicate significantly different averages.
If Unequal ni : Use 1-ink / =n MGH Exhibit 6.13
Studentized Range Statistic
Assume
y i = 1,2, . . . ,k ; j= 1,2, . . . , rij ~ { , )NID yy
Studentized Range
qy y
k rij i
max{ ( )
( )
| y - y | }
s / r , s
i j 22
1
qn j
max{
) / } /
| y - y | }
s{(n
i j
i-1 1 1 22 unequal ni
Tukey’s “Honest” Significant Difference (HSD or TSD)
y and y are significantly different if
| y - y | > TSD
where
TSD = q + n
1 2
1 2
2-1
( ; , ){( )
} / E Ek MSn1
11 2
2
MGH Exhibit 6.11
Bonferroni Method
CCE
C
C
C
kCE
k
k/
toRateError wiseComparison Set the
k
k11
)1(1
Tests,t Independenk For
Bonferroni Multiple Comparisons (BSD)
y and y are significantly different if
| y - y | > BSD
where
BSD = t + n
1 2
1 2
2-1
E( / )//( ){ ( )} 2 1
1 1 2m EMS n
Number of Pairwise Comparisons
m =k(k - 1)
2
Contrasts of Effects
c c c
c
i i i i i
i i c i 0
Estimable Factor Effects
ContrastsContrasts
Elimination of the Overall Mean Requires Contrasts of Main Effect Averages.(Note: Want to Compare Factor Effects.)
Elimination of Main Effects from Interaction Comparisons Requires Contrasts of the Interaction Averages.
(Note: Want Interaction Effects to Measure Variability that is Unaccounted for by or in Addition to the Main Effects.)
Statistical Independence
0cc t independenlly statistica are ˆ and ˆ
ycˆ
ycˆ
)I , N(X~y
2121
22
11
2
Orthogonal Linear Combinationsare Statistically Independent
Orthogonal Linear Combinationsare Statistically Independent
Orthogonal Contrastsare Statistically Independent
Orthogonal Contrastsare Statistically Independent
Main Effects Contrasts :Qualitative Factor Levels
c , c , c1 2 3
1
2
1
1
0
0
1
6
1
1
2
0
1
12
1
1
1
3
Three statistically independent contrasts of the response averages
A partitioning of the main effects degrees of freedom into single degree-of-freedom contrasts (a = 4: df = 3)
Sums of Squares and Contrasts
SS y - yA i
r
ry I a J y
ry CC y
r c y
a a
i
2
1
2
( )
( ) Single Degree-of-Freedom Contrasts
Single Degree-of-Freedom Contrasts
SimultaneousTest
SimultaneousTest
C = c c ... c
P : C
a x (a-1) 1 2 a-1
a x a
a
PP I a J CC
CC I a J
a
a a
a a
1 2
1
1
1/
a-1 MutuallyOrthonormal Contrast
Vectors
a-1 MutuallyOrthonormal Contrast
VectorsOrthonormal
Basis Set
OrthonormalBasis Set
ANY Set ofOrthonormal Contrast
Vectors
ANY Set ofOrthonormal Contrast
Vectors
yijk = + i + j+ij+eijk
where
yij = warping measurement for the kth repeat at the ith temperature using a plate having the jth amount of copper
= overall mean warping measurement
i = fixed effect of the ith temperature on the mean warping
i = fixed effect of the jth copper content on the mean warping
(ij = fixed effect of the interaction between the ith temperature and the jth copper content on the mean warping
eij = random experimental error, NID(0,2)
Model and Assumptions
,0)()(j
iji
ijj
ji
i
Warping of Copper Plates
Source df SS MS F p-ValueCopper Content 3 698.34 232.78 34.33 0.000Temperature 3 156.09 52.03 7.67 0.002C x T 9 113.78 12.64 1.86 0.134Error 16 108.50 6.78Total 31 1076.71
MGH Table 6.7
Quantitative Factor LevelsHOW Does Mean Warping Change with the Factor Levels ?
Quantitative Factor LevelsHOW Does Mean Warping Change with the Factor Levels ?
Warping of Copper Plates
0 50 75 100 125 150
Temperature (deg F)
10
15
20
25
30
35
AverageWarping
Are There Contrast VectorsThat Quantify Curvature ?
Are There Contrast VectorsThat Quantify Curvature ?
Warping of Copper Plates
0 20 40 60 80 100
Copper Content (%)
10
15
20
25
30
35
AverageWarping
Are There Contrast VectorsThat Quantify Curvature ?
Are There Contrast VectorsThat Quantify Curvature ?
Main Effects Contrasts :Equally Spaced Quantitative Factor Levels
c , c , c1 2 3
1
20
3
1
1
3
1
2
1
1
1
1
1
20
1
3
3
1
= Linear = Quadratic = Cubic
n=4
Linear Combinations of Parameters
Estimable Functions of Parameters
iic
Estimator
Standard Error
iiycˆ
2/12iˆ r/cse
t Statistic 2
ˆtF ,
se
ˆt
Same for ContrastsSame for Contrasts
Warping of Copper Plates
Temperature Linear Quadratic Cubic Average50 -3 1 -1 21.8875 -1 -1 3 17.38100 1 -1 -3 21.00125 3 1 1 23.38
Normalized Contrast 1.82 3.44 -2.09Single df S.S. 26.41 94.53 35.16 156.10
2j
2/14
1i
4
1i
2ijiijj
ˆbr :Squares of Sum df Single
c/ycˆ :Contrast Normalized
Scaled Contrasts
Note: Need Scaling to Make Polynomial Contrasts Comparable
2es
2/1k
1i
2i
k
1iiis
k
1i
2i
2e
k
1iii
ˆ var, /n ayaˆ
n/aˆ var, yaˆ
Design Resolution
Resolution REffects involving s Factors are unconfoundedwith effects involving fewer than R-s factors
Resolution III (R = 3)
Main Effects (s = 1) are unconfounded withother main effects (R - s = 2)
Example : Half-Fraction of 23 (23-1)
Designing a 1/2 Fraction of a 2k Complete Factorial
Write the effects representation for the main effects and the highest-order interaction for a complete factorial in k factors
Randomly choose the +1 or -1 level for the highest-order interaction (defining contrast, defining equation)
Eliminate all rows except those of the chosen level (+1 or -1) in the highest-order interaction
Add randomly chosen repeat tests, if possible Randomize the test order or assignment to
experimental units
Resolution = kResolution = k
Designing Higher-Order Fractions
Total number of factor-level combinations = 2k
Experiment size desired = 2k/2p = 2k-p
Choose p defining contrasts (equations) For each defining contrast randomly decide which
level will be included in the design Select those combinations which simultaneously
satisfy all the selected levels Add randomly selected repeat test runs Randomize
Design Resolution for Fractional Factorials
Determine the p defining equations Determine the 2p - p - 1 implicit defining equations:
symbolically multiply all of the defining equations
Resolution = Smallest “word’ length in the defining & implicit equations
Each effect has 2p aliases
26-2 Fractional Factorials :Confounding Pattern
Build From 1/4 Fraction
I = ABCDEF = ABC = DEFA = BCDEF = BC = BDEFB = ACDEF = AC = ADEF . . .
RIIIRIII
(I + ABCDEF)(I + ABC) = I + ABCDEF + ABC + DEF
Defining ContrastsImplicit Contrast
26-2 Fractional Factorials :Confounding Pattern
Build From 1/2 Fraction
I = ABCDEF = ABC = DEFA = BCDEF = BC = BDEFB = ACDEF = AC = ADEF . . .
RIIIRIII
Optimal 1/4 Fraction
I = ABCD = CDEF = ABEFA = BCD = ACDEF = BEFB = ACD = BCDEF = AEF . . .
RIVRIV
Screening Experiments
Very few test runs Ability to assess main effects only Generally leads to a comprehensive
evaluation of a few dominant factors Potential for bias
Highly effective for isolating vital few strong effectsshould be used ONLY under the proper circumstancesHighly effective for isolating vital few strong effects
should be used ONLY under the proper circumstances
Plackett-Burman Screening Designs
Any number of factors, each having 2 levels Interactions nonexistent or negligible Relative
to main effectsNumber of test runs is a multiple of 4 At least 6 more test runs than factors should
be used