Factorial Experiments Analysis of Variance (ANOVA) Experimental Design
Jan 22, 2016
Factorial Experiments
Analysis of Variance (ANOVA)
Experimental Design
• Dependent variable Y
• k Categorical independent variables A, B, C, … (the Factors)
• Let– a = the number of categories (levels) of A– b = the number of categories (levels) of B– c = the number of categories (levels) of C– etc.
Example 1
• Dependent variable, Y, weight gain
• Independent variables– A, Level of Protein in the diet (High, Low)– B, Source of Protein (Beef, Cereal, Pork)
Example 2
• Dependent variable, Y, paint lustre
• Independent variables– A, Film Thickness - (1 or 2 mils)
– B, Drying conditions (Regular or Special) – C, Length of wash (10,30,40 or 60 Minutes)
– D, Temperature of wash (92 ˚C or 100 ˚C)
A Treatment Combination
• a combination levels of the k factors
• Total number of treatment combinations– t = abc….
The treatment combinations can thought to be arranged in a k-dimensional rectangular block
A
1
2
a
B1 2 b
A
B
C
or
A
B
C
The Completely Randomized Design
• We form the set of all treatment combinations – the set of all combinations of the k factors
• Total number of treatment combinations– t = abc….
• In the completely randomized design n experimental units (test animals , test plots, etc. are randomly assigned to each treatment combination.– Total number of experimental units N = nt=nabc..
• The Completely Randomized Design is called balanced
• If the number of observations per treatment combination is unequal the design is called unbalanced. (resulting mathematically more complex analysis and computations)
• If for some of the treatment combinations there are no observations the design is called incomplete. (some of the parameters - main effects and interactions - cannot be estimated.)
Example
In this example we are examining the effect of
We have n = 10 test animals randomly assigned to k = 6 diets
• tThe level of protein A (High or Low) and • tThe source of protein B (Beef, Cereal, or
Pork) on weight gains (grams) in rats.
The k = 6 diets are the 6 = 3×2 Level-Source combinations
1. High - Beef
2. High - Cereal
3. High - Pork
4. Low - Beef
5. Low - Cereal
6. Low - Pork
TableGains in weight (grams) for rats under six diets differing in level of protein (High or Low) and s
ource of protein (Beef, Cereal, or Pork)
Levelof Protein High Protein Low protein
Sourceof Protein Beef Cereal Pork Beef Cereal Pork
Diet 1 2 3 4 5 6
73 98 94 90 107 49102 74 79 76 95 82118 56 96 90 97 73104 111 98 64 80 86
81 95 102 86 98 81107 88 102 51 74 97100 82 108 72 74 106
87 77 91 90 67 70117 86 120 95 89 61111 92 105 78 58 82
Mean 100.0 85.9 99.5 79.2 83.9 78.7Std. Dev. 15.14 15.02 10.92 13.89 15.71 16.55
Example – Four factor experiment
Four factors are studied for their effect on Y (luster of paint film). The four factors are:
Two observations of film luster (Y) are taken for each treatment combination
1) Film Thickness - (1 or 2 mils)
2) Drying conditions (Regular or Special) 3) Length of wash (10,30,40 or 60 Minutes), and
4) Temperature of wash (92 ˚C or 100 ˚C)
The data is tabulated below:
Regular Dry Special Dry
92 °C 100 °C 92 °C 100 °C
Minutes 1-mil Thickness
20 3.4 3.4 19.6 14.5 2.1 3.8 17.2 13.4 30 4.1 4.1 17.5 17.0 4.0 4.6 13.5 14.3 40 4.9 4.2 17.6 15.2 5.1 3.3 16.0 17.8 60 5.0 4.9 20.9 17.1 8.3 4.3 17.5 13.9
Minutes 2-mil Thickness 20 5.5 3.7 26.6 29.5 4.5 4.5 25.6 22.5 30 5.7 6.1 31.6 30.2 5.9 5.9 29.2 29.8 40 5.5 5.6 30.5 30.2 5.5 5.8 32.6 27.4 60 7.2 6.0 31.4 29.6 8.0 9.9 33.5 29.5
NotationLet the single observations be denoted by a single letter and a number of subscripts
yijk…..l
The number of subscripts is equal to:(the number of factors) + 1
1st subscript = level of first factor 2nd subscript = level of 2nd factor …Last subsrcript denotes different observations on the same treatment combination
Notation for Means
When averaging over one or several subscripts we put a “bar” above the letter and replace the subscripts by
Example:
y241
Profile of a Factor
Plot of observations means vs. levels of the factor.
The levels of the other factors may be held constant or we may average over the other levels
Level of Protein Beef Cereal Pork Overall
Low 79.20 83.90 78.70 80.60
Source of Protein
High 100.00 85.90 99.50 95.13
Overall 89.60 84.90 89.10 87.87
Summary Table
70
80
90
100
110
Beef Cereal Pork
Wei
ght
Gai
n
High Protein
Low Protein
Overall
Profiles of Weight Gain for Source and Level of Protein
70
80
90
100
110
High Protein Low Protein
Wei
ght
Gai
nBeef
Cereal
Pork
Overall
Profiles of Weight Gain for Source and Level of Protein
Definition:
A factor is said to not affect the response if the profile of the factor is horizontal for all combinations of levels of the other factors:
No change in the response when you change the levels of the factor (true for all combinations of levels of the other factors)
Otherwise the factor is said to affect the response:
0
2
4
6
8
10
12
14
16
0 1 2 3 4 5 6 7
Levels of Factor
Profiles of a Factor that does not affect the response
0
2
4
6
8
10
12
14
16
0 1 2 3 4 5 6 7
Levels of Factor
Profiles of a Factor that does affect the response
Definition:• Two (or more) factors are said to interact if
changes in the response when you change the level of one factor depend on the level(s) of the other factor(s).
• Profiles of the factor for different levels of the other factor(s) are not parallel
• Otherwise the factors are said to be additive .
• Profiles of the factor for different levels of the other factor(s) are parallel.
0
2
4
6
8
10
12
14
16
0 1 2 3 4 5 6 7
Levels of Factor
Additive Factors
0
2
4
6
8
10
12
14
16
0 1 2 3 4 5 6 7
Levels of Factor
Interacting Factors
• If two (or more) factors interact each factor effects the response.
• If two (or more) factors are additive it still remains to be determined if the factors affect the response
• In factorial experiments we are interested in determining
– which factors effect the response and– which groups of factors interact .
The testing in factorial experiments 1. Test first the higher order interactions.2. If an interaction is present there is no need
to test lower order interactions or main effects involving those factors. All factors in the interaction affect the response and they interact
3. The testing continues with for lower order interactions and main effects for factors which have not yet been determined to affect the response.
Models for factorial experiments
The general model
yijk…lm = ijk…l + ijk…lm i = 1, 2, ... , a; j = 1, 2, ... , b; …m = 1,2, ... ,n;
ijk…l is the mean for the treatment combination (i, j, k, …,l )
ijk…lm is the random departure from the mean (assumed to be normal with mean 0 and variance 2)
The mean,, for the treatment combination (i, j, k, …,l ) can be broken into components.
For example if there is a single factor A, i , is the mean when factor A is at level i.
Then
i = • + (i - •) = + i
where
iii
i
a and
Note: i = i - is called the effect of treatment i, the
ith level of factor A
0i
iAlso
ii allfor 0and
if A has no effect on the response
For the two factor experiment, ij , is the mean when factor A is at level i and factor B is at level j.
Then
ij = •• + (i• - ••) + (•j - ••) + (ij - i• - •j + ••)
= + i + j + ()ij
where
baabj
ij
ji
ij
ii j
ij
and ,
Note:
i = i• - •• is the main effect for factor A.
j = •j - •• is the main effect for factor B.
and
()ij = (ij - i• - •j + ••) is the interaction effect for factors A and B.
0i
iNow
. and allfor 0 jiij Also
if A and B do not interact (are additive).
0j
j
0 and j
iji
ij
i.e. ij = + i + j
If A and B do not interact (are additive).
ii allfor 0 if then A has no effect on the response
jj allfor 0 if
In addition B has no effect on the response
Models for factorial Experiments
Single Factor:
yij = + i + ij i = 1,2, ... ,a; j = 1,2, ... ,n
Two Factor:
yijk = + i + j+ ij + ijk
i = 1,2, ... ,a ; j = 1,2, ... ,b ; k = 1,2, ... ,n
Three Factor:
yijkl = + i + j+ ij + k + (ik + (jk+ ijk + ijkl
= + i + j+ k + ij + (ik + (jk+ ijk + ijkl
i = 1,2, ... ,a ; j = 1,2, ... ,b ; k = 1,2, ... ,c; l = 1,2, ... ,n
Four Factor:
yijklm = + i + j+ ij + k + (ik + (jk+ ijk + l+ (il + (jl+ ijl + (kl + (ikl + (jkl+ ijkl + ijklm
= + i + j+ k + l+ ij + (ik + (jk + (il + (jl+ (kl + ijk+ ijl + (ikl + (jkl+ ijkl + ijklm
i = 1,2, ... ,a ; j = 1,2, ... ,b ; k = 1,2, ... ,c; l = 1,2, ... ,d; m = 1,2, ... ,n
where 0 = i = j= ij = k = (ik = (jk= ijk = l= (il = (jl = ijl = (kl = (ikl = (jkl = ijkl
and denotes the summation over any of the subscripts.
Estimation of Main Effects and Interactions • Estimator of Main effect of a Factor
• Estimator of k-factor interaction effect at a combination of levels of the k factors
= Mean at the combination of levels of the k factors - sum of all means at k-1 combinations of levels of the k factors +sum of all means at k-2 combinations of levels of the k factors - etc.
= Mean at level i of the factor - Overall Mean
Example:
• The main effect of factor B at level j in a four factor (A,B,C and D) experiment is estimated by:
• The two-factor interaction effect between factors B and C when B is at level j and C is at level k is estimated by:
yyˆjj
yyyy kjjkjk
• The three-factor interaction effect between factors B, C and D when B is at level j, C is at level k and D is at level l is estimated by:
• Finally the four-factor interaction effect between factors A,B, C and when A is at level i, B is at level j, C is at level k and D is at level l is estimated by:
yyyyyyyy lkjklljjkjkljkl
jklikiijjklklilijijkijkljkl yyyyyyyyy
yyyyyyy lkjikllj
Anova Table entries
• Sum of squares interaction (or main) effects being tested (product of sample size and levels of factors not included in the interaction)
• Degrees of freedom = df = product of (number of levels - 1) of factors included in the interaction.
Level of Protein Beef Cereal Pork Overall
Low 79.20 83.90 78.70 80.60
Source of Protein
High 100.00 85.90 99.50 95.13
Overall 89.60 84.90 89.10 87.87
Summary Table
Example: Diet, Source of Protein, Level of Protein
Mean
87.867
Main Effects for Factor A (Source of Protein)
Beef Cereal Pork
1.733 -2.967 1.233
21 ,533.266ˆ1
2
adfnbSSa
iiA
Main Effects for Factor B (Level of Protein)
High Low
7.267 -7.267
11 ,267.3168ˆ
1
2
bdfnaSSb
jjB
AB Interaction Effects
Source of Protein
Beef Cereal Pork
Level High 3.133 -6.267 3.133
of Protein Low -3.133 6.267 -3.133
a
i
b
jijAB nSS
1 1
2 = 1178.133, df =(a – 1)(b – 1) = (2)(1) = 2
The testing in factorial experiments 1. If an interaction is present there is no need
to test lower order interactions or main effects involving those factors. All factors in the interaction affect the response and they interact
2. Test first the higher order interactions.3. The testing continues with for lower order
interactions and main effects for factors which have not yet been determined to affect the response.
Table: Means and Cell Frequencies
Means and Frequencies for the AB Interaction (Temp - Drying)
0
5
10
15
20
25
92 100
Temperature
Lus
ter
Regular Dry
Special Dry
Overall
Profiles showing Temp-Dry Interaction
Means and Frequencies for the AD Interaction (Temp- Thickness)
0
5
10
15
20
25
30
92 100
Temperature
Lus
ter
1-mil
2-mil
Overall
Profiles showing Temp-Thickness Interaction
The Main Effect of C (Length)
7060504030201012
13
14
15
16
Profile of Effect of Length on Luster
Length
Lu
ster
ANOVA TABLE
Factorial Experiment
Completely Randomized Design
Anova table for the 3 factor Experiment
Source SS df MS F p -value
A SSA a - 1 MSA MSA/MSError
B SSB b - 1 MSB MSB/MSError
C SSC c - 1 MSC MSC/MSError
AB SSAB (a - 1)(b - 1) MSAB MSAB/MSError
AC SSAC (a - 1)(c - 1) MSAC MSAC/MSError
BC SSBC (b - 1)(c - 1) MSBC MSBC/MSError
ABC SSABC (a - 1)(b - 1)(c - 1) MSABC MSABC/MSError
Error SSError abc(n - 1) MSError
Sum of squares entries
a
ii
a
iiA yynbcnbcSS
1
2
1
2̂
Similar expressions for SSB , and SSC.
a
i
b
jjiij
a
iijAB yyyyncncSS
1 1
2
1
2
Similar expressions for SSBC , and SSAC.
Sum of squares entries
Finally
a
iikjABC nSS
1
2
a
i
b
j
c
kijkkiijijk yyyyyn
1 1 1 2 ikj yyy
a
i
b
j
c
k
n
lijkijklError yySS
1 1 1 1
2
The statistical model for the 3 factor Experiment
effectsmain effectmean kjiijk/y
error randomninteractiofactor 3nsinteractiofactor 2
ijk/ijkjkikij
Anova table for the 3 factor Experiment
Source SS df MS F p -value
A SSA a - 1 MSA MSA/MSError
B SSB b - 1 MSB MSB/MSError
C SSC c - 1 MSC MSC/MSError
AB SSAB (a - 1)(b - 1) MSAB MSAB/MSError
AC SSAC (a - 1)(c - 1) MSAC MSAC/MSError
BC SSBC (b - 1)(c - 1) MSBC MSBC/MSError
ABC SSABC (a - 1)(b - 1)(c - 1) MSABC MSABC/MSError
Error SSError abc(n - 1) MSError
The testing in factorial experiments 1. Test first the higher order interactions.2. If an interaction is present there is no need
to test lower order interactions or main effects involving those factors. All factors in the interaction affect the response and they interact
3. The testing continues with lower order interactions and main effects for factors which have not yet been determined to affect the response.
Random Effects and Fixed Effects Factors
• So far the factors that we have considered are fixed effects factors
• This is the case if the levels of the factor are a fixed set of levels and the conclusions of any analysis is in relationship to these levels.
• If the levels have been selected at random from a population of levels the factor is called a random effects factor
• The conclusions of the analysis will be directed at the population of levels and not only the levels selected for the experiment
Example - Fixed Effects
Source of Protein, Level of Protein, Weight GainDependent
– Weight Gain
Independent– Source of Protein,
• Beef• Cereal• Pork
– Level of Protein,• High• Low
Example - Random Effects
In this Example a Taxi company is interested in comparing the effects of three brands of tires (A, B and C) on mileage (mpg). Mileage will also be effected by driver. The company selects b = 4 drivers at random from its collection of drivers. Each driver has n = 3 opportunities to use each brand of tire in which mileage is measured.Dependent
– Mileage
Independent– Tire brand (A, B, C),
• Fixed Effect Factor
– Driver (1, 2, 3, 4),• Random Effects factor
The Model for the fixed effects experiment
where , 1, 2, 3, 1, 2, ()11 , ()21 , ()31 , ()12 , ()22 , ()32 , are fixed unknown constants
And ijk is random, normally distributed with mean 0 and variance 2.
Note:
ijkijjiijky
01111
b
jij
a
iij
n
jj
a
ii
The Model for the case when factor B is a random effects factor
where , 1, 2, 3, are fixed unknown constants
And ijk is random, normally distributed with mean 0 and variance 2.
j is normal with mean 0 and varianceand
()ij is normal with mean 0 and varianceNote:
ijkijjiijky
01
a
ii
2B
2AB
This model is called a variance components model
The Anova table for the two factor model
ijkijjiijky
Source SS df MS
A SSAa -1 SSA/(a – 1)
B SSAb - 1 SSB/(a – 1)
AB SSAB(a -1)(b -1) SSAB/(a – 1) (a – 1)
Error SSError ab(n – 1) SSError/ab(n – 1)
The Anova table for the two factor model (A, B – fixed)
ijkijjiijky
Source SS df MS EMS F
A SSA a -1 MSA MSA/MSError
B SSA b - 1 MSB MSB/MSError
AB SSAB (a -1)(b -1) MSAB MSAB/MSError
Error SSError ab(n – 1) MSError2
a
iia
nb
1
22
1
b
jjb
na
1
22
1
a
i
b
jijba
n
1 1
22
11
EMS = Expected Mean Square
The Anova table for the two factor model (A – fixed, B - random)
ijkijjiijky
Source SS df MS EMS F
A SSA a -1 MSA MSA/MSAB
B SSA b - 1 MSB MSB/MSError
AB SSAB (a -1)(b -1) MSAB MSAB/MSError
Error SSError ab(n – 1) MSError2
a
iiAB a
nbn
1
222
1
22Bna
22ABn
Note: The divisor for testing the main effects of A is no longer MSError but MSAB.
Rules for determining Expected Mean Squares (EMS) in an Anova
Table
1. Schultz E. F., Jr. “Rules of Thumb for Determining Expectations of Mean Squares in Analysis of Variance,”Biometrics, Vol 11, 1955, 123-48.
Both fixed and random effects
Formulated by Schultz[1]
1. The EMS for Error is 2.2. The EMS for each ANOVA term contains
two or more terms the first of which is 2.3. All other terms in each EMS contain both
coefficients and subscripts (the total number of letters being one more than the number of factors) (if number of factors is k = 3, then the number of letters is 4)
4. The subscript of 2 in the last term of each EMS is the same as the treatment designation.
5. The subscripts of all 2 other than the first contain the treatment designation. These are written with the combination involving the most letters written first and ending with the treatment designation.
6. When a capital letter is omitted from a subscript , the corresponding small letter appears in the coefficient.
7. For each EMS in the table ignore the letter or letters that designate the effect. If any of the remaining letters designate a fixed effect, delete that term from the EMS.
8. Replace 2 whose subscripts are composed entirely of fixed effects by the appropriate sum.
2
2 1 by 1
a
ii
A a
2
2 1 by 1 1
a
iji
AB a b
Example: 3 factors A, B, C – all are random effects
Source EMS F
A
B
C
AB
AC
BC
ABC
Error
2 2 2 2 2ABC AB AC An nc nb nbc
2 2 2 2 2ABC AB BC Bn nc na nac
2 2 2 2 2ABC BC AC Cn na nb nab
2 2 2ABC ABn nc
2 2 2ABC ACn nb
2 2 2ABC BCn na
2 2ABCn
2
AB ABCMS MS
AC ABCMS MS
BC ABCMS MS
ABC ErrorMS MS
Example: 3 factors A fixed, B, C random
Source EMS F
A
B
C
AB
AC
BC
ABC
Error
2 2 2 2 2
1
1a
ABC AB AC ii
n nc nb nbc a
2 2 2
BC Bna nac
2 2 2BC Cna nab
2 2 2ABC ABn nc
2 2 2ABC ACn nb
2 2BCna
2 2ABCn
2
AB ABCMS MS
AC ABCMS MS
BC ErrorMS MS
ABC ErrorMS MS
C BCMS MS
B BCMS MS
Example: 3 factors A , B fixed, C random
Source EMS F
A
B
C
AB
AC
BC
ABC
Error
2 2 2
1
1a
AC ii
nb nbc a
2 2Cnab
2 2ACnb
2 2BCna
2 2ABCn
2
AB ABCMS MS
AC ErrorMS MS
BC ErrorMS MS
ABC ErrorMS MS
C ErrorMS MS
B BCMS MS 2 2 2
1
1a
BC ji
na nac b
22 2
1 1
1 1a b
ABC iji j
n nc a b
A ACMS MS
Example: 3 factors A , B and C fixed
Source EMS F
A
B
C
AB
AC
BC
ABC
Error
2 2
1
1a
ii
nbc a
2
AB ErrorMS MS
AC ErrorMS MS
BC ErrorMS MS
ABC ErrorMS MS
C ErrorMS MS
B ErrorMS MS 2 2
1
1a
ji
nac b
22
1 1
1 1a b
iji j
nc a b
A ErrorMS MS
2 2
1
1c
kk
nbc c
22
1 1
1 1a c
iji k
nb a c
22
1 1
1 1b c
ijj k
na b c
22
1 1 1
1 1 1a b c
ijki j k
n a b c
Example - Random Effects
In this Example a Taxi company is interested in comparing the effects of three brands of tires (A, B and C) on mileage (mpg). Mileage will also be effected by driver. The company selects at random b = 4 drivers at random from its collection of drivers. Each driver has n = 3 opportunities to use each brand of tire in which mileage is measured.Dependent
– Mileage
Independent– Tire brand (A, B, C),
• Fixed Effect Factor
– Driver (1, 2, 3, 4),• Random Effects factor
The DataDriver Tire Mileage Driver Tire Mileage
1 A 39.6 3 A 33.91 A 38.6 3 A 43.21 A 41.9 3 A 41.31 B 18.1 3 B 17.81 B 20.4 3 B 21.31 B 19 3 B 22.31 C 31.1 3 C 31.31 C 29.8 3 C 28.71 C 26.6 3 C 29.72 A 38.1 4 A 36.92 A 35.4 4 A 30.32 A 38.8 4 A 352 B 18.2 4 B 17.82 B 14 4 B 21.22 B 15.6 4 B 24.32 C 30.2 4 C 27.42 C 27.9 4 C 26.62 C 27.2 4 C 21
Asking SPSS to perform Univariate ANOVA
Select the dependent variable, fixed factors, random factors
The Output
Tests of Between-Subjects Effects
Dependent Variable: MILEAGE
28928.340 1 28928.340 1270.836 .000
68.290 3 22.763a
2072.931 2 1036.465 71.374 .000
87.129 6 14.522b
68.290 3 22.763 1.568 .292
87.129 6 14.522b
87.129 6 14.522 2.039 .099
170.940 24 7.123c
SourceHypothesis
Error
Intercept
Hypothesis
Error
TIRE
Hypothesis
Error
DRIVER
Hypothesis
Error
TIRE * DRIVER
Type IIISum ofSquares df
MeanSquare F Sig.
MS(DRIVER)a.
MS(TIRE * DRIVER)b.
MS(Error)c.
The divisor for both the fixed and the random main effect is MSAB
This is contrary to the advice of some texts
The Anova table for the two factor model (A – fixed, B - random)
ijkijjiijky
Source SS df MS EMS F
A SSA a -1 MSA MSA/MSAB
B SSA b - 1 MSB MSB/MSError
AB SSAB (a -1)(b -1) MSAB MSAB/MSError
Error SSError ab(n – 1) MSError2
a
iiAB a
nbn
1
222
1
22Bna
22ABn
Note: The divisor for testing the main effects of A is no longer MSError but MSAB.
References Guenther, W. C. “Analysis of Variance” Prentice Hall, 1964
The Anova table for the two factor model (A – fixed, B - random)
ijkijjiijky
Source SS df MS EMS F
A SSA a -1 MSA MSA/MSAB
B SSA b - 1 MSB MSB/MSAB
AB SSAB (a -1)(b -1) MSAB MSAB/MSError
Error SSError ab(n – 1) MSError2
a
iiAB a
nbn
1
222
1
222BAB nan
22ABn
Note: In this case the divisor for testing the main effects of A is MSAB . This is the approach used by SPSS.
References Searle “Linear Models” John Wiley, 1964
Crossed and Nested Factors
The factors A, B are called crossed if every level of A appears with every level of B in the treatment combinations.
Levels of B
Levels of A
Factor B is said to be nested within factor A if the levels of B differ for each level of A.
Levels of B
Levels of A
Example: A company has a = 4 plants for producing paper. Each plant has 6 machines for producing the paper. The company is interested in how paper strength (Y) differs from plant to plant and from machine to machine within plant
Plants
Machines
Machines (B) are nested within plants (A)
The model for a two factor experiment with B nested within A.
error random within ofeffect factor ofeffect mean overall
ijkAB
ijA
iijky
The ANOVA table
Source SS df MS F p - value
A SSA a - 1 MSA MSA/MSError
B(A) SSB(A) a(b – 1) MSB(A) MSB(A) /MSError
Error SSError ab(n – 1) MSError
Note: SSB(A ) = SSB + SSAB and a(b – 1) = (b – 1) + (a - 1)(b – 1)
Example: A company has a = 4 plants for producing paper. Each plant has 6 machines for producing the paper. The company is interested in how paper strength (Y) differs from plant to plant and from machine to machine within plant.
Also we have n = 5 measurements of paper strength for each of the 24 machines
The Data
Plant 1 2 machine 1 2 3 4 5 6 7 8 9 10 11 12
98.7 59.2 84.1 72.3 83.5 60.6 33.6 44.8 58.9 63.9 63.7 48.1 93.1 87.8 86.3 110.3 89.3 84.8 48.2 57.3 51.6 62.3 54.6 50.6
100.0 84.1 83.4 81.6 86.1 83.6 68.9 66.5 45.2 61.1 55.3 39.9 Plant 3 4 machine 13 14 15 16 17 18 19 20 21 22 23 24
83.6 76.1 64.2 69.2 77.4 61.0 64.2 35.5 46.9 37.0 43.8 30.0 84.6 55.4 58.4 86.7 63.3 81.3 50.3 30.8 43.1 47.8 62.4 43.0
90.6 92.3 75.4 60.8 76.6 73.8 32.1 36.3 40.8 41.0 60.8 56.9
Anova Table Treating Factors (Plant, Machine) as crossed
Tests of Between-Subjects Effects
Dependent Variable: STRENGTH
21031.065a 23 914.394 7.972 .000
298531.4 1 298531.4 2602.776 .000
18174.761 3 6058.254 52.820 .000
1238.379 5 247.676 2.159 .074
1617.925 15 107.862 .940 .528
5505.469 48 114.697
325067.9 72
26536.534 71
SourceCorrected Model
Intercept
PLANT
MACHINE
PLANT * MACHINE
Error
Total
Corrected Total
Type IIISum of
Squares dfMean
Square F Sig.
R Squared = .793 (Adjusted R Squared = .693)a.
Anova Table: Two factor experiment B(machine) nested in A (plant)
Source Sum of Squares df Mean Square F p - valuePlant 18174.76119 3 6058.253731 52.819506 0.00000 Machine(Plant) 2856.303672 20 142.8151836 1.2451488 0.26171 Error 5505.469467 48 114.6972806