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Construct a \(2_{\mathrm{IV}}^{7-2}\) design. Show how this design may be confounded in four blocks of eight runs each. Are any two-factor interactions confounded with blocks?

Short Answer

Expert verified
Yes, certain two-factor interactions are confounded with blocks, specifically through combinations involving the chosen generators.

Step by step solution

01

Understanding Design Details

We need to construct a fractionated factorial design with 7 factors at 2 levels each, designated as a \( 2_{\text{IV}}^{7-2} \) design. This implies creating a design of resolution IV, reducing from \( 2^7 = 128 \) runs to \( 2^{7-2} = 32 \) runs.
02

Choosing Generators for Fractionation

To create a \( 2_{\text{IV}}^{7-2} \) design, we introduce 2 generators. We choose the generators as \( G_1 = ABCD \) and \( G_2 = ABCE \), leading to the defining relation \( I = ABCD = ABCE \).
03

Creating Blocks

To divide into blocks, we need to use the generators to create blocks of 8 runs each. Since we have 32 runs initially, we will require 4 blocks of 8 since \( 32/8 = 4 \). We find the block generators using interactions such as \( G_3 = A(ABCD) = BCD \).
04

Identifying Confounded Interactions

Two-factor interactions confounded with blocks are given by the interactions of the generators. Here, the interactions \((AB \, AB) = B \), \((AC \, CD) = AD \), \((BE \, E) = B \), and other combinations can be used to determine which interactions are aliased with block generators.

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Key Concepts

These are the key concepts you need to understand to accurately answer the question.

Resolution IV Design
A Resolution IV design is a specific type of fractional factorial design where the main effects are not confounded with other main effects or two-factor interactions. However, two-factor interactions may be confounded with each other, but not with main effects. A fractional factorial design helps reduce the number of experimental runs needed, which is especially useful when handling multiple factors. In the case of a Resolution IV design, it strikes a balance between being economical and informative. In our example, a \(2_{\text{IV}}^{7-2}\) design signifies that we are working with a seven-factor system, but instead of running all \(2^7 = 128\) possible combinations, we reduce it to 32 runs. This resolution suggests that no single main effect is aliased with another main effect or any two-factor interactions, which is a crucial benefit when trying to decipher the real effects in complex experiments.
Confounding in Blocks
Confounding in Blocks is a technique in design of experiments where certain interactions, particularly two-factor interactions, are deliberately aliased with entire blocks to simplify the analysis. By analyzing blocks and interactions together, experiments can manage variability more effectively. In the exercise, to divide 32 runs into four blocks of 8, we use specific confounding patterns. Here, the generators like \(ABCD\) and \(ABCE\) help to form four distinct blocks. Confounding takes place intentionally to organize the runs within these blocks, making it easier to check for variability caused by block effects. By constructing these blocks, some two-factor interactions might be confounded within these blocks, meaning certain interactions cannot be distinguished from block effects. Identifying these is key to correctly interpreting experimental results.
Two-factor Interactions
Two-factor interactions occur when the effect of one factor depends on the level of another factor. In factorial experiments, they reveal how combinations of factors jointly affect the response variable, which is crucial to understanding complex phenomena in experiments. In a fractional factorial design like a Resolution IV, certain two-factor interactions can be aliased with each other or blocks, but not the main effects. In the exercise example, interactions such as \(B\), \(AD\), and others emerge from combinations like \(AB \, AB\), \(AC \, CD\), illustrating their role within blocks. Understanding two-factor interactions helps in determining the specific pairwise interactions that contribute significantly to the response, especially when designing and analyzing experiments involving multiple factors.
Generators in Design
Generators are the key to constructing fractional factorial designs. They determine which factor combinations to include, effectively reducing the trial size while maintaining information. Generators allow experimentalists to select and manage which interactions are aliased. In a \(2_{\text{IV}}^{7-2}\) design, choosing generators like \(ABCD\) and \(ABCE\) helps to produce essential equation sets known as defining relations. These ensuring particular interactions, like some two-factor interactions, become indistinguishable or aliased. With the introduction of generators, defining relations are established, outlining how factors and interactions relate to each other. This approach aids in the practical execution of experiments by minimizing runs, thereby saving time and resources while still capturing key effects.

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Most popular questions from this chapter

An article in Quality Engineering ["A Comparison of Multi-Response Optimization: Sensitivity to Parameter Selection" (1999, Vol. 11, pp. \(405-415\) ) ] conducted a half replicate of a \(2^{5}\) factorial design to optimize the retort process of beef stew MREs, a military ration. The design factors are \(x_{1}=\) sauce viscosity \(, x_{2}=\) residual gas, \(x_{3}=\) solid/liquid ratio, \(x_{4}=\) net weight, \(x_{5}=\) rotation speed. The response variable is the heating rate index, a measure of heat penetration, and there are two replicates. $$ \begin{array}{crrrrrrr} \hline && & & & & & {\text { Heating Rate }} \\ & & & & && &\ {\text { Index }} \\ \ \text { Run } & x_{1} & x_{2} & x_{3} & x_{4} & x_{5} & \text { I } & \text { II } \\ \ 1 & -1 & -1 & -1 & -1 & 1 & 8.46 & 9.61 \\ 2 & 1 & -1 & -1 & -1 & -1 & 15.68 & 14.68 \\ 3 & -1 & 1 & -1 & -1 & -1 & 14.94 & 13.09 \\ 4 & 1 & 1 & -1 & -1 & 1 & 12.52 & 12.71 \\ 5 & -1 & -1 & 1 & -1 & -1 & 17.0 & 16.36 \\ 6 & 1 & -1 & 1 & -1 & 1 & 11.44 & 11.83 \\ 7 & -1 & 1 & 1 & -1 & 1 & 10.45 & 9.22 \\ 8 & 1 & 1 & 1 & -1 & -1 & 19.73 & 16.94 \\ 9 & -1 & -1 & -1 & 1 & -1 & 17.37 & 16.36 \\ 10 & 1 & -1 & -1 & 1 & 1 & 14.98 & 11.93 \\ 11 & -1 & 1 & -1 & 1 & 1 & 8.40 & 8.16 \\ 12 & 1 & 1 & -1 & 1 & -1 & 19.08 & 15.40 \\ 13 & -1 & -1 & 1 & 1 & 1 & 13.07 & 10.55 \\ 14 & 1 & -1 & 1 & 1 & -1 & 18.57 & 20.53 \\ 15 & -1 & 1 & 1 & 1 & -1 & 20.59 & 21.19 \\ 16 & 1 & 1 & 1 & 1 & 1 & 14.03 & 11.31 \end{array} $$ (a) Estimate the factor effects. Based on a normal probability plot of the effect estimates, identify a model for the data from this experiment. (b) Conduct an ANOVA based on the model identified in part (a). What are your conclusions? (c) Analyze the residuals and comment on model adequacy. (d) Find a regression model to predict yield in terms of the coded factor levels. (e) This experiment was replicated, so an ANOVA could have been conducted without using a normal plot of the effects to tentatively identify a model. What model would be appropriate? Use the ANOVA to analyze this model and compare the results with those obtained from the normal probability plot approach.

A manufacturer of cutting tools has developed two empirical equations for tool life \(\left(y_{1}\right)\) and tool cost \(\left(y_{2}\right) .\) Both models are functions of tool hardness \(\left(x_{1}\right)\) and manufacturing time \(\left(x_{2}\right) .\) The equations are $$ \begin{array}{l} \hat{y}_{1}=10+5 x_{1}+2 x_{2} \\ \hat{y}_{2}=23+3 x_{1}+4 x_{2} \end{array} $$ and both are valid over the range \(-1.5 \leq x_{i} \leq 1.5 .\) Suppose that tool life must exceed 12 hours and cost must be below \(\$ 27.50\) (a) Is there a feasible set of operating conditions? (b) Where would you run this process?

An article in Solid State Technology (1984, Vol. 29, pp. \(281-284\) ) described the use of factorial experiments in photolithography, an important step in the process of manufacturing integrated circuits. The variables in this experiment (all at two levels) are prebake temperature \((A),\) prebake time \((B),\) and exposure energy \((C),\) and the response variable is delta line width, the difference between the line on the mask and the printed line on the device. The data are as follows: \((1)=-2.30, a=-9.87, b=-18.20\), \(a b=-30.20, c=-23.80, a c=-4.30, b c=-3.80,\) and \(a b c=-14.70\) (a) Estimate the factor effects. (b) Use a normal probability plot of the effect estimates to identity factors that may be important. (c) What model would you recommend for predicting the delta line width response based on the results of this experiment? (d) Analyze the residuals from this experiment, and comment on model adequacy.

Consider the first-order model $$ y=12+1.2 x_{1}-2.1 x_{2}+1.6 x_{3}-0.6 x_{4} $$ where \(-1 \leq x_{i} \leq 1\) (a) Find the direction of steepest ascent. (b) Assume that the current design is centered at the point \((0,\) 0,0,0)\(.\) Determine the point that is three units from the current center point in the direction of steepest ascent.

A two-level factorial experiment in four factors was conducted by Chrysler and described in the article "Sheet Molded Compound Process Improvement" by P. I. Hsieh and D. E. Goodwin (Fourth Symposium on Taguchi Methods, American Supplier Institute, Dearborn, MI, \(1986,\) pp. \(13-21\) ). The purpose was to reduce the number of defects in the finish of sheet-molded grill opening panels. A portion of the experimental design, and the resulting number of defects, \(y_{i}\) observed on each run is shown in the following table. This is a single replicate of the \(2^{4}\) design. (a) Estimate the factor effects and use a normal probability plot to tentatively identify the important factors. (b) Fit an appropriate model using the factors identified in part (a). (c) Plot the residuals from this model versus the predicted number of defects. Also prepare a normal probability plot of the residuals. Comment on the adequacy of these plots. (d) The following table also shows the square root of the number of defects. Repeat parts (a) and (c) of the analysis using the square root of the number of defects as the response. Does this change the conclusions? $$ \begin{array}{ccccccc} \hline & \ {\text { Grill Defects Experiment }} \\ \ \text { Run } & \text { A } & \text { B } & \text { C } & \text { D } & \text { y } & \sqrt{y} \\ \hline 1 & \- & \- & \- & \- & 56 & 7.48 \\ 2 & \+ & \- & \- & \- & 17 & 4.12 \\ 3 & \- & \+ & \- & \- & 2 & 1.41 \\ 4 & \+ & \+ & \- & \- & 4 & 2.00 \\ 5 & \- & \- & \+ & \- & 3 & 1.73 \\ 6 & \+ & \- & \+ & \- & 4 & 2.00 \\ 7 & \- & \+ & \+ & \- & 50 & 7.07 \\ 8 & \+ & \+ & \+ & \- & 2 & 1.41 \\ 9 & \- & \- & \- & \+ & 1 & 1.00 \\ 10 & \+ & \- & \- & \+ & 0 & 0.00 \\ 11 & \- & \+ & \- & \+ & 3 & 1.73 \\ 12 & \+ & \+ & \- & \+ & 12 & 3.46 \\ 13 & \- & \- & \+ & \+ & 3 & 1.73 \\ 14 & \+ & \- & \+ & \+ & 4 & 2.00 \\ 15 & \- & \+ & \+ & \+ & 0 & 0.00 \\ 16 & \+ & \+ & \+ & \+ & 0 & 0.00 \end{array} $$

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