A new series of affine resolvable PBIB(4) designs in two replicates

1. Introduction

Partially balanced incomplete block (PBIB) designs form an important class of block designs. If the experimenter is constrained of resources, PBIB designs with higher associate classes in minimum replications are an alternative to the more popular class of block designs, i.e., balanced incomplete block (BIB) designs or two-associate class PBIB designs. Furthermore, it is advisable to opt for a resolvable block design for situations where experimentation is to be done, one complete replication at one location/season, considering spatial/temporal variations. Some distinguished classes of resolvable PBIB designs are available in the literature (Rao [3]; Williams et al. [5]; Kageyama [2]; Varghese and Sharma [4]; Agrawal et al. [1]). Again, equally sized blocks may not always be feasible in every experimental situation. Hence, it might be of interest to the experimenters to have resolvable PBIB designs in fewer replications with unequal block sizes.

We define a new association scheme in Section 2. A general method of constructing resolvable PBIB designs in unequal block sizes based on this association scheme is given in Section 3. In Section 4, an outline of the analysis of these designs is given.

2. Association scheme

Let the number of treatments be v = 2mt(t-1) where, m $\ge$ 1, t $\ge$ 3. Arrange these treatments in a rectangular array consisting of t-1 groups, each group containing t rows and two columns and each row-column intersection having m treatments is shown in Table 1.

For any given treatment $\theta$ appearing in the i${}^{th}$ row of any group, remaining treatments appearing in the same row of the same group are first associates, treatments appearing in all other rows of the same group are second associates, treatments belonging to the i${}^{th}$ row of the other groups are third associates and the rest are fourth associates. The parameters of the association scheme are derived as follows:

$\mathit{\text{v}}=2\mathit{\text{mt}}(\mathit{\text{t}}-1),\mathit{\text{n}}$_1$=2\mathit{\text{m}}-1,\mathit{\text{n}}$_2$=2\mathit{\text{m}}(\mathit{\text{t}}-1),\mathit{\text{n}}$_3$=2\mathit{\text{m}}(\mathit{\text{t}}-2),\mathit{\text{n}}$_4$=2\mathit{\text{m}}(\mathit{\text{t}}-1)(\mathit{\text{t}}-2),$

$$\begin{array}{rl}{\mathrm{P}}_1=& \left[\begin{array}{cccc}2(m-1)& 0& 0& 0\\ 0& 2(t-1)m& 0& 0\\ 0& 0& 2(t-2)m& 0\\ 0& 0& 0& 2(t-1)(t-2)m\end{array}\right],\\ {\mathrm{P}}_2=& \left[\begin{array}{cccc}0& 2m-1& 0& 0\\ 2m-1& 2(t-2)m& 0& 0\\ 0& 0& 0& 2(t-2)m\\ 0& 0& 2(t-2)m& 2m(t-2{)}^2\end{array}\right],\\ {\mathrm{P}}_3=& \left[\begin{array}{cccc}0& 0& 2m-1& 0\\ 0& 0& 0& 2(t-1)m\\ 2m-1& 0& 2(t-3)m& 0\\ 0& 2(t-1)m& 0& 2(t-1)(t-3)m\end{array}\right],\end{array}$$ and $$\begin{array}{rl}{\mathrm{P}}_4=& \left[\begin{array}{cccc}0& 0& 0& 2m-1\\ 0& 0& 2m& 2(t-2)m\\ 0& 2m& 0& 2(t-3)m\\ 2m-1& 2(t-2)m& 2(t-3)m& 2(t-2)(t-3)m\end{array}\right].\end{array}$$

The method of construction is summarized below:

3. Method of construction

The first b${}_1$ = t-1 blocks of size k${}_1$ = 2mt can be obtained by treating the t-1 groups of the above array as blocks. The i${}^{th}$ block of remaining b${}_2$ = t blocks of size k${}_2$ = 2m(t-1) can be obtained by appending the i${}^{th}$ (1 $<$ i $\le$ t) row of each group of the above array one after another. This will yield a class of affine resolvable block designs having unequal block sizes with parameters: $$\begin{array}{}\text{(1)}& \{\begin{array}{rl}v& =2mt(t-1),b_1=t-1,b_2=t,r=2,\\ k_1& =2mt,k_2=2m(t-1),\\ {\lambda }_1& =2,{\lambda }_2=1,{\lambda }_3=1,{\lambda }_4=0,\\ n_1& =2m-1,n_2=2m(t-1),n_3=2m(t-2),n_4=2m(t-1)(t-2).\end{array}\end{array}$$

Here, the blocks of the design can be divided into two groups such that in each group, every treatment appears precisely once, and any two blocks belonging to two different groups have $\frac{k_1{k}_2}{v}$ = 2m treatments in common. These designs are partially variance balanced with an underlying association scheme defined above.

It has been verified that all the parametric relationships of the association scheme and designs are satisfied for the above class of designs. $$\begin{array}{}\text{(2)}& \{\begin{array}{rl}1.& \sum _{i=1}^4{n}_i=v–1,\\ 2.& \sum _{k=1}^4{p}_{jk}^i=n_j–{\delta }_{ij},{\delta }_{ij}=\{\begin{array}{ll}0,& i\ne j=1,2,3,4,\\ 1,& i=j=1,2,3,4,\end{array}\\ 3.& n_i{p}_{jk}^i=n_j{p}_{ik}^j=n_k{p}_{ij}^k,i,j,k=1,2,3,4,\\ 4.& vr=\sum _{j=1}^2{b}_j{k}_j,j=1,2,3,4,\\ 5.& \sum _{i=1}^4{n}_i{\lambda }_i=\sum _{l=1}^2(k_l–1).\end{array}\end{array}$$

4. Outline of analysis

The analysis of these designs may be carried out using the same approach as PBIB designs. However, as the proposed designs are resolvable, the following nested model is appropriate for a set-up of v treatments in b (=2t-1) blocks where t-1 blocks are of size 2mt and t blocks are of size 2m(t-1): $$\begin{array}{}\text{(3)}& y_{\mathrm{i}\mathrm{j}\mathrm{m}}=\mu +{\tau }_i+R_m+{\beta }_{j(m)}+e_{\mathrm{i}\mathrm{j}\mathrm{m}}.\end{array}$$

Here, $y_{ijm}$ is the response on plot $i$ ($i=1,2,\dots ,v$) in block $j$ ($j=1,2,\dots ,b$), nested within the $m$th ($m=1,2,\dots ,r$) replication. $\mu$ is the general mean, ${\tau }_i$ is the effect of the $i$th treatment, $R_m$ is the effect of the $m$th replicate, ${\beta }_{j(m)}$ is the effect of the $j$th block in the $m$th replicate, and $e_{ijm}$ are independent random errors normally distributed with mean zero and variance ${\sigma }^2$.

Solving the normal equations, obtained by minimizing the residual sum of squares, will lead to the following general expressions for variances of elementary contrasts between two estimated treatment effects:

$$\mathrm{V}\mathrm{a}\mathrm{r}({\hat{\tau }}_i–{\hat{\tau }}_{i^{\prime }})=\{\begin{array}{ll}{v}_1={\sigma }^2,& \text{if }i\text{ and }{i}^{\prime }\text{ arefirst associates;}\\ v_2=\frac{2m(t-1)+1}{2m(t-1)}{\sigma }^2,& \text{if }i\text{ and }{i}^{\prime }\text{ are second associates;}\\ v_3=\frac{2mt+1}{2mt}{\sigma }^2,& \text{if }i\text{ and }{i}^{\prime }\text{ are third associates;}\\ v_4=\frac{2mt(t-1)+2t-1}{2mt(t-1)}{\sigma }^2,& \text{otherwise.}\end{array}$$

The average variance of elementary contrasts between two estimated treatment effects is then calculated as: $$\overline{V}=\frac{n_1{v}_1+n_2{v}_2+n_3{v}_3+n_4{v}_4}{n_1+n_2+n_3+n_4}=\frac{2(m{t}^2–mt+t–2)}{2m{t}^2–mt–1}{\sigma }^2.$$

Acknowledgements

The first author is thankful to the P.G. School, ICAR-IARI for the financial assistance. The authors are grateful to the editor and reviewers for their valuable comments that helped improve our manuscript’s quality.