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Orthogonal Linear Contrasts
This is a technique for partitioning ANOVA sum of squares into individual degrees of freedom
Definition
Let x1, x2, ... , xp denote p numerical quantities computed from the data.
These could be statistics or the raw observations.
A linear combination of x1, x2, ... , xp is defined to be a quantity ,L ,computed in the following manner:
L = c1x1+ c2x2+ ... + cpxp
where the coefficients c1, c2, ... , cp are predetermined numerical values:
Definition
If the coefficients c1, c2, ... , cp satisfy:
c1+ c2 + ... + cp = 0,
Then the linear combination
L = c1x1+ c2x2+ ... + cpxp
is called a linear contrast.
Examples
p
xxxxL p
21
2354321 xxxxx
L
54321 2
1
2
1
3
1
3
1
3
1xxxxx
1.
pxp
xp
xp
11121
2.
3. L = x1 - 4 x2+ 6x3 - 4 x4 + x5
= (1)x1+ (-4)x2+ (6)x3 + (-4)x4 + (1)x5
A linear combination
A linear contrast
A linear contrast
Definition
Let A = a1x1+ a2x2+ ... + apxp and B= b1x1+ b2x2+ ... + bpxp be two linear contrasts of the quantities x1, x2, ... , xp. Then A and B are c called Orthogonal Linear Contrasts if in addition to:
a1+ a2+ ... + ap = 0 and
b1+ b2+ ... + bp = 0,
it is also true that:
a1b1+ a2b2+ ... + apbp = 0.
.
Example
Let
Note:
2354321 xxxxx
A
54321 2
1
2
1
3
1
3
1
3
1xxxxx
54321
2xxx
xxB
54321 1112
1
2
1xxxxx
01- 2
11
2
11-
3
1
2
1
3
1
2
1
3
1
Definition
Let A = a1x1+ a2x2+ ... + apxp,
B= b1x1+ b2x2+ ... + bpxp ,
..., and
L= l1x1+ l2x2+ ... + lpxp
be a set linear contrasts of the quantities x1, x2, ... , xp.
Then the set is called a set of Mutually Orthogonal Linear Contrasts if each linear contrast in the set is orthogonal to any other linear contrast..
Theorem:
The maximum number of linear contrasts in a set of Mutually Orthogonal Linear Contrasts of the quantities x1, x2, ... , xp is p - 1.
p - 1 is called the degrees of freedom (d.f.) for comparing quantities x1, x2, ... , xp .
Comments
1. Linear contrasts are making comparisons amongst the p values x1, x2, ... , xp
2. Orthogonal Linear Contrasts are making independent comparisons amongst the p values x1, x2, ... , xp .
3. The number of independent comparisons amongst the p values x1, x2, ... , xp is p – 1.
Definition
denotes a linear contrast of the p means
If each mean, , is calculated from n observations then:
The Sum of Squares for testing the Linear Contrast L, is defined to be:
pp xaxaxaL 2211
ixpxxx ,,2,1
222
21
2
= p
L +...+a+aa
n LSS
the degrees of freedom (df) for testing the Linear Contrast L, is defined to be
the F-ratio for testing the Linear Contrast L, is defined to be:
1Ldf
1
Error
L
MS
SS
F
Theorem:
Let L1, L2, ... , Lp-1 denote p-1 mutually orthogonal Linear contrasts for comparing the p means . Then the Sum of Squares for comparing the p means based on p – 1 degrees of freedom , SSBetween, satisfies:
121 p-L LLBetween + SS + ... + SS = SSSS
Comment
Defining a set of Orthogonal Linear Contrasts for comparing the p means
allows the researcher to "break apart" the Sum of Squares for comparing the p means, SSBetween, and make individual tests of each the Linear Contrast.
pxxx ,,2,1
The Diet-Weight Gain example
The sum of Squares for comparing the 6 means is given in the Anova Table:
,5.999.850.100 3 2 1 xxx ,,
7.789.832.79 6 5 4 xxx ,,
Five mutually orthogonal contrasts are given below (together with a description of the purpose of these contrasts) :
6543211 3
1
3
1xxxxxxL
(A comparison of the High protein diets with Low protein diets)
63412 2
1
2
1xxxxL
(A comparison of the Beef source of protein with the Pork source of protein)
(A comparison of the Meat (Beef - Pork) source of protein with the Cereal source of protein)
(A comparison representing interaction between Level of protein and Source of protein for the Meat source of Protein)
(A comparison representing interaction between Level of protein with the Cereal source of Protein)
5264313 2
1
4
1xxxxxxL
43614 2
1
2
1xxxxL
2645315 24
12
4
1xxxxxxL
The Anova Table for Testing these contrasts is given below:
Source: DF: Sum Squares: Mean Square: F-test:
Contrast L1 1 3168.267 3168.267 14.767
Contrast L2 1 2.500 2.500 0.012
Contrast L3 1 264.033 264.033 1.231
Contrast L4 1 0.000 0.000 0.000
Contrast L5 1 1178.133 1178.133 5.491
Error 54 11586.000 214.556
The Mutually Orthogonal contrasts that are eventually selected should be determine prior to observing the data and should be determined by the objectives of the experiment
Another Five mutually orthogonal contrasts are given below (together with a description of the purpose of these contrasts) :
63412 2
1
2
1xxxxL
(A comparison of the Beef source of protein with the Pork source of protein)
(A comparison of the Meat (Beef - Pork) source of protein with the Cereal source of protein)
5264311 2
1
4
1xxxxxxL
(A comparison of the high and low protein diets for the Beef source of protein)
(A comparison of the high and low protein diets for the Cereal source of protein)
(A comparison of the high and low protein diets for the Pork source of protein)
413 xxL
524 xxL
635 xxL
The Anova Table for Testing these contrasts is given below:
Source: DF: Sum Squares: Mean Square: F-test:
Beef vs Pork ( L1) 1 2.500 2.500 0.012
Meat vs Cereal ( L2) 1 264.033 264.033 1.231
High vs Low for Beef ( L3) 1 2163.200 2163.200 10.082
High vs Low for Cereal ( L4) 1 20.000 20.000 0.093
High vs Low for Pork ( L5) 1 2163.200 2163.200 10.082
Error 54 11586.000 214.556
Orthogonal Linear Contrasts
Polynomial Regression
Orthogonal Linear Contrasts for Polynomial Regression
k P o l y n o m i a l 1 2 3 4 5 6 7 8 9 1 0 a
i2
3 L i n e a r - 1 0 1 2 Q u a d r a t i c 1 - 2 1 6 4 L i n e a r - 3 - 1 1 3 2 0 Q u a d r a t i c 1 - 1 - 1 1 4 C u b i c - 1 3 - 3 1 2 0 5 L i n e a r - 2 - 1 0 1 2 1 0 Q u a d r a t i c 2 - 1 - 2 - 1 2 1 4 C u b i c - 1 2 0 - 2 1 1 0 Q u a r t i c 1 - 4 6 - 4 1 7 0 6 L i n e a r - 5 - 3 - 1 1 3 5 7 0 Q u a d r a t i c 5 - 1 - 4 - 4 - 1 5 8 4 C u b i c - 5 7 4 - 4 - 7 5 1 8 0 Q u a r t i c 1 - 3 2 2 - 3 1 2 8 7 L i n e a r - 3 - 2 - 1 0 1 2 3 2 8 Q u a d r a t i c 5 0 - 3 - 4 - 3 0 5 8 4 C u b i c - 1 1 1 0 - 1 - 1 1 6 Q u a r t i c 3 - 7 1 6 1 - 7 3 1 5 4
Orthogonal Linear Contrasts for Polynomial Regression
k P o l y n o m i a l 1 2 3 4 5 6 7 8 9 1 0 a
i2
8 L i n e a r - 7 - 5 - 3 - 1 1 3 5 7 1 6 8 Q u a d r a t i c 7 1 - 3 - 5 - 5 - 3 1 7 1 6 8 C u b i c - 7 5 7 3 - 3 - 7 - 5 7 2 6 4 Q u a r t i c 7 - 1 3 - 3 9 9 - 3 - 1 3 7 6 1 6 Q u i n t i c - 7 2 3 - 1 7 - 1 5 1 5 1 7 - 2 3 7 2 1 8 4 9 L i n e a r - 4 - 3 - 2 - 1 0 1 2 3 4 2 0 Q u a d r a t i c 2 8 7 - 8 - 1 7 - 2 0 - 1 7 - 8 7 2 8 2 7 7 2 C u b i c - 1 4 7 1 3 9 0 - 9 - 1 3 - 7 1 4 9 9 0 Q u a r t i c 1 4 - 2 1 - 1 1 9 1 8 9 - 1 1 - 2 1 1 4 2 0 0 2 Q u i n t i c - 4 1 1 - 4 - 9 0 9 4 - 1 1 4 4 6 8 1 0 L i n e a r - 9 - 7 - 5 - 3 - 1 1 3 5 7 9 3 3 0 Q u a d r a t i c 6 2 - 1 - 3 - 4 - 4 - 3 - 1 2 6 1 3 2 C u b i c - 4 2 1 4 3 5 3 1 1 2 - 1 2 - 3 1 - 3 5 - 1 4 4 2 8 5 8 0 Q u a r t i c 1 8 - 2 2 - 1 7 3 1 8 1 8 3 - 1 7 - 2 2 1 8 2 8 6 0 Q u i n t i c - 6 1 4 - 1 - 1 1 - 6 6 1 1 1 - 1 4 6 7 8 0
Example
Table Activation
Temperature 0 25 50 75 100 53 60 67 65 58 50 62 70 68 62 47 58 73 62 60 T.. Ti. 150 180 210 195 180 915 Mean 50 60 70 65 60
yij2 = 56545 Ti.2/n = 56475 T..2/nt = 55815
In this example we are measuring the “Life” of an electronic component and how it depends on the temperature on activation
The Anova Table
Source SS df MS FTreat 660 4 165.0 23.57
Linear 187.50 1 187.50 26.79Quadratic 433.93 1 433.93 61.99Cubic 0.00 1 0.00 0.00Quartic 38.57 1 38.57 5.51
Error 70 10 7.00Total 730 14
L = 25.00 Q2 = -45.00 C = 0.00 Q4 = 30.00
The Anova Tables for Determining degree of polynomial
Testing for effect of the factor
Source SS df MS F Treat 660 4 165 23.57 Error 70 10 7 Total 730 14
Testing for departure from Linear
S o u r c e S S d f M S F
L i n e a r 1 8 7 . 5 0 1 . 0 0 1 8 7 . 5 0 2 6 . 7 9 D e p a r t u r e f r o m L i n e a r 4 7 2 . 5 0 3 . 0 0 1 5 7 . 5 0 2 2 . 5 0 E r r o r 7 0 . 0 0 1 0 . 0 0 7 . 0 0
Testing for departure from Quadratic
S o u r c e S S d f M S F
L i n e a r 1 8 7 . 5 0 1 . 0 0 1 8 7 . 5 0 2 6 . 7 9 Q u a d r a t i c 4 3 3 . 9 3 1 . 0 0 4 3 3 . 9 3 6 1 . 9 9 D e p a r t u r e f r o m Q u a d r a t i c 3 8 . 5 7 2 . 0 0 1 9 . 2 9 2 . 7 6 E r r o r 7 0 . 0 0 1 0 . 0 0 7 . 0 0
y = 49.751 + 0.61429 x -0.0051429 x^2
40
45
50
55
60
65
70
0 20 40 60 80 100 120
Act. Temp
Lif
e
Multiple Testing
•Tukey’s Multiple comparison procedure•Scheffe’s multiple comparison procedure
Multiple Testing – a Simple Example
Suppose we are interested in testing to see if two parameters (1 and 2) are equal to zero.
There are two approaches
1. We could test each parameter separately
a) H0: 1 = 0 against HA: 1 ≠ 0 , then
b) H0: 2 = 0 against HA: 2 ≠ 0
2. We could develop an overall test
H0: 1 = 0, 2= 0 against HA: 1 ≠ 0 or 2 ≠ 0
1. To test each parameter separately
a)
then
b)
We might use the following test:
ˆ if Reject 1)1(
0 KH
0:against 0: 1)1(
1)1(
0 AHH
0:against 0: 2)2(
2)2(
0 AHH
ˆ if Reject 2)2(
0 KH
then
K is chosen so that the probability of a Type I errorof each test is .
2. To perform an overall test
H0: 1 = 0, 2= 0 against HA: 1 ≠ 0 or 2 ≠ 0
we might use the test
)(22
210
ˆˆ if Reject overallKH
)(overallK is chosen so that the probability of a Type I error is .
1̂ K 1̂
2̂
ˆ2 K
1̂
2̂
1̂ K
1̂
2̂
ˆ2 K
ˆ )(1
multipleK
1̂
2̂
ˆ )(2
multipleK
1̂
2̂
)(22
21
ˆˆ overallK
1̂
2̂
)(22
21
ˆˆ overallK
ˆ )(1
multipleK
ˆ )(2
multipleK
1̂
2̂
)(22
21
ˆˆ overallK
ˆˆ )(2211
ScheffeKcc
ˆˆ )(2211
ScheffeKcc
Post-hoc Tests
Multiple Comparison Tests
Post-hoc Tests
Multiple Comparison Tests
Suppose we have p means
An F-test has revealed that there are significant differences amongst the p means
We want to perform an analysis to determine precisely where the differences exist.
pxxx ,,2,1
Tukey’s Multiple Comparison Test
Let
Tukey's Critical Differences
Two means are declared significant if they differ by more than this amount.
n
MS
n
s Error
n
MSq
n
sqD Error
ixdenote the standard error of each
q = the tabled value for Tukey’s studentized range p = no. of means, = df for Error
Scheffe’s Multiple Comparison Test
Scheffe's Critical Differences (for Linear contrasts)
A linear contrast is declared significant if it exceeds this amount.
222
21,11 paaa
n
spFpS
222
21,11 p
Error aaan
MSpFp
= the tabled value for F distribution (p -1 = df for comparing p means, = df for Error)
,1pF
Scheffe's Critical Differences (for comparing two means)
ji xxL
2,11n
MSpFpS Error
Two means are declared significant if they differ by more than this amount.
Table 5: Critical Values for the multiple range Test , and the F-distribution
q.05 q.01 F.05 F.01
Length 3.84 4.80 2.92 4.51 Temp,Thickness,Dry 4.60 5.54 2.33 3.30
Table 6: Tukey's and Scheffe's Critical Differences Tukeys Scheffés
= .05 = .01 = .05 = .01 Length 1.59 1.99 2.05 2.16 Temp, Thickness, Dry 3.81 4.59 4.74 5.64
S u m m a r y o f t h e C o m p a r i s o n s : C o m p a r i s o n o f t h e m e a n f i l m L u s t r e f o r d i f f e r e n t c o m b i n a t i o n s o f l e v e l s o f t h e t h r e e f a c t o r s - T h i c k n e s s , T e m p e r a t u r e a n d D r y i n g p r o c e d u r e ( U s i n g T u k e y ' s c r i t i c a l D i f f e r e n c e w i t h = 0 . 0 1 ) :
C o m p a r i s o n o f t h e m e a n f i l m L u s t r e f o r d i f f e r e n t l e v e l s o f L e n g t h o f d r y i n g T i m e ( U s i n g T u k e y ' s c r i t i c a l D i f f e r e n c e w i t h = 0 . 0 1 ) :
4.25 4.44 5.66 15.45 17.43 28.76 29.95
4.25 0.19 1.41 11.2 13.18 24.51 25.74.44 1.22 11.01 12.99 24.32 25.515.66 9.79 11.77 23.1 24.29
15.45 1.98 13.31 14.517.43 11.33 12.5228.76 1.1929.95
Table of differences in means
Underlined groups have no significant differences
There are many multiple (post hoc) comparison procedures
1. Tukey’s
2. Scheffe’,
3. Duncan’s Multiple Range
4. Neumann-Keuls
etc
Considerable controversy:“I have not included the multiple comparison methods of D.B. Duncan because I have been unable to understand their justification” H. Scheffe, Analysis of Variance