# The relationship of excitement, importance and entropy to the efficiency of statistical hypothesis tests

#### Abstract

Sports scoring systems can be seen as statistical hypothesis tests, and the tennis scoring system in particular can be viewed as a particular sequential 2-sample binomial test. Thus, the excitement of a point (or observation) within a scoring system can be seen to have a place within hypothesis testing. The 2-sample binomial tests known to be the most efficient are shown to have related characteristics with respect to the measures of excitement and importance in sport and with Shannon entropy in information theory. This paper also includes several new, interesting and quite general scoring systems theorems.

## 1Introduction

Miles (1984), in his very elegant paper, showed that *a scoring system in sport could be considered to be identical to a hypothesis test in statistics*. In particular, he considered tennis which is an application of comparing two binomial probabilities. In tennis there are essentially two types of points, a-points (player A serves) and b-points (B serves), as described for example in Pollard (1983). Thus, tennis scoring is a ‘bi-points’ scoring system. Player A is the better player if pa >pb, where pa is player A’s probability of winning a point on his service and pb is player B’s probability of winning a point on his service. Assuming pa and pb are unknowns and the objective of playing a match is to efficiently identify the better player by reducing as much as possible the error probability (the better player loses or worse player wins) for a given expected number of points played, Miles set up symmetrical statistical hypotheses, for 0 <pb’ <pa’ <1,

Ho: (pa, pb) = (pa’, pb’) (or A better than B) and

H1: (pa, pb) = (pb’, pa’) (or B better than A),

and considered ‘fair’ bipoints scoring systems with sensible properties. He called these scoring systems ‘biformats’. Thus, a scoring system is a statistical test, and a biformat is a statistical test of the above hypothesis in which the two types of error are equal, i.e. *α*=*β*. Thus, the tennis scoring system is essentially a statistical test of the above hypothesis.

Miles (1984) also set up unipoints for the situation where serving is essentially neither an advantage or a disadvantage, as is typically the situation in squash. In unipoints, player A is the better player if *p* > 0.5, where p is player A’s probability of winning a point.

Returning to bipoints, Miles (1984) used ‘point-pairs’ (consisting of an a-point and a b-point) to set up a ‘standard family of biformats’ Wn(point-pairs) to represent a scoring system in which the winner is the first player to win n more point-pairs than his opponent (or equivalently 2n points). This standard family of biformats was given an efficiency of unity. He showed that the efficiency *ρ* of a general biformat with key characteristics P and *μ* relative to this standard family is given by

##### (1)

*Q*= 1 – P, and

*μ*is the expected number of points played. Thus, for given (pa, pb), the efficiency is a function of P and

*μ*.

A way to thinking about the efficiency of scoring systems is this ... if you are given two scoring systems with the same value of *μ* for a given pair (pa, pb), then the more efficient scoring system at (pa, pb) is the one with the larger value of P (and hence the larger value of P/Q).

Miles (1984) setup families of scoring systems based on alternating (AL), play-the-winner (PW) and play-the-loser (PL) service exchange mechanisms, and which used the Wn stopping rule in which the winner is the first player to be n points ahead of his opponent. Play-the-winner, for example, is the service exchange mechanism in which a point won by player A is followed by an a-point, and a point won by player B is followed by a b-point. Thus, he set up the scoring systems W1(WnAL^{a}, WnAL^{b}) (*n* = 1, 2, 3, ...) which consist of two parts. Play starts with an a-point (player A serves), and service alternates until one player is n points ahead, when that part of play ceases and the second part of the scoring system begins with a b-point, and points again alternate until one player is n points ahead. If this player is the same player as the one who was n points ahead on the first part of the play, then that player is the winner. Otherwise, the scoring system starts over again. Although this seems complicated, it isn’t. The two parts of the scoring system are needed to create fairness. Miles (1984) showed that this scoring system had unit efficiency, and Pollard (1986, 1992) noted that it was in fact stochastically identical to Wn(point-pairs). Using the same two-part structure but with the play-the-loser service exchange mechanism in which a point won by player A is followed by a b-point and a point won by B is followed by an a-point, Miles (1984) set up the scoring systems W1(WnPL^{a}, WnPL^{b}) (*n* = 2, 3, 4, ...). He showed that they have efficiencies very slightly greater than unity when pa +pb >1, and correspondingly that the play-the-winner (PW) scoring systems W1(WnPW^{a}, WnPW^{b}) (*n* = 2, 3, 4, ...) have efficiencies less than unity when pa + pb >1. By identifying (n-2) “partial-PL” Wn scoring systems “between” W1(WnPL^{a}, WnPL^{b}) and W1(WnAL^{a}, WnAL^{b}) when *n* = 3, 4, 5, ... , Pollard (1986, 1992) showed that the (full) PL family of scoring systems W1(WnPL^{a}, WnPL^{b}) was in fact the *most efficient scoring system possible (i.e. was optimally efficient)* when pa + pb >1 (i.e. the tennis context, for example, where serving is an advantage). The corresponding PW family W1(WnPW^{a}, WnPW^{b}) (*n* = 2, 3, 4, ...) is optimal when pa + pb <1 (i.e. the volleyball context, for example, where serving is a disadvantage).

Pollard (1986, 1992) noted that the above optimal biformats for the 2-sample binomial test when *α* = *β* (i.e. the symmetric case) are such that the biformats (or tests) pass through non-symmetrical situations and yet the 1-step PL (or PW) rule remains optimal. These non-symmetrical situations, as a starting point, correspond to the *α* ≠ *β* case in hypothesis testing and the handicap situation in sport. Thus, using the principle of optimality (dynamic programming), he concluded that the PL (PW) rule used with W(n1, n2) systems is optimally efficient for the 2-sample binomial statistical test when *α* ≠ *β* provided pa + pb >1 (pa + pb <1). Note that here W(n1, n2) represents the stopping rule for the handicap sporting situation in which player A needs to win n1 more points than player B in order to win, and player B needs to win n2 more points than player A inorder win.

It has remained a challenge to describe why these PL (PW) rules lead to optimal tests when used with Wn stopping rules. Further, it would appear that a greater insight into why such tests are very efficient or optimal might give researchers an increased capacity in designing very good statistical tests for other situations. Pollard (1986, pp.30 and 1992, pp.282) gave an intuitive explanation for the super-efficiency of these PL and PW scoring systems. It was that ‘in each case, under the most efficient rule, a greater number of points with the more variable (Bernoulli) distribution is expected to be selected; and this is an approach used in efficient estimation theory’. Pollard (1986, 1990) gave an alternative explanation for the case in which the value of n in the above PL and PW scoring systems is very large, and this explanation is outlined in the following paragraph.

Pollard (1990, pp.191) described ‘a method for decomposing many sequential probability ratio [statistical] tests [including the PL and PW systems described above] into smaller independent components called “modules”. A function of some characteristics of modules can be used to determine the asymptotically most efficient of a set of statistical tests...’, and he ‘used the “module” method to give an explanation for the super-efficiency of the play-the-winner (when pa + pb <1) and play-the-loser rules (when pa + pb >1) in two sample binomial sampling’. In the context of Wm systems and denoting player A as the better player, he defined the random variable S as the increase (or shift) in player A’s score during one module and the random variable D as the duration (i.e. number of points played) of the module. He compared W1(WmPL^{a}, WmPL^{b}) and W1(WmPW^{a}, WmPW^{b}) when p = (pa + pb)/2, q = 1 – p, m = nq for the PL case, m = np for the PW case, and n is large, noting that these two systems have the same asymptotic durations. The value of the variance of S, Var(S) for the PL module was then ‘scaled’ so that it can be *directly* compared with the value of Var(S) for the PW module. The purpose of this scaling was to allow for (i) the different values of E(D) for the two modules, and (ii) the different values of m in Wm for the two systems. He concluded (pp.197) that ‘for the same asymptotic expected durations [of the two Wm systems], the smaller scaled (or “relative”) variance for the PL module (when pa≠pb and pa + pb >1) results in the better player having a higher probability of winning and hence the PL system has greater efficiency’. Using this ‘module’ approach to the asymptotic case he also concluded that if pa + pb <1 and pa≠pb, the PW structure is the more efficient.

The major aim of this paper is to give further insights into why the PL or the PW structure, when combined with the Wn stopping rule, produces optimally efficient scoring systems. Unlike the results described in the previous paragraph, in this paper we do not restrict consideration to the situations in which the n in Wn is very large. We gain insight into this by considering the ‘importance’ of a point within a scoring system, the ‘excitement’ of a point within a scoring system, and the ‘information’ or ‘entropy’ of a Bernoulli trial. These concepts are described in the following paragraphs.

In an elegant paper Morris (1977) defined the ‘importance’ of a point within a game as the probability player A wins the game given he wins that point minus the probability he wins the game given he loses the point. Pollard (1986, 1992) noted that the very efficient Wn scoring systems (using AL, PL and PW) had equally important points when the players were equal (pa = pb).

In information theory, Shannon (1948) defined the entropy of a Bernoulli observation with probability p to be equal to pln(1/p) + (1 – p)ln(1/(1 – p)).

In the paper by Pollard (2016) a mathematical measure for the excitement of a point in various sports was devised. In this paper we give a second excitement measure, similar in concept but one based on squared values rather than absolutevalues.

Pollard (1986, 1992) considered two equal players and found an expression for the increased probability player A has of winning a game given that he increases his probability of winning the point in state i by *δ*_{i} (*i* = 1, 2, 3, ...). He showed that player A’s increased probability of winning the game is given by *Δ*P =** Σ**N

_{i}*I

_{i}*

*δ*

_{i}, where I

_{i}is the importance of the point at state i when the players are equal and N

_{i}is the expected number of times state i is entered in one realization of the game with player A’s increased point probabilities. An extension of this result is given in Section 2. This paper also includes several new and quite general scoring systems theorems, including a second relationship between player A’s probability of winning under a scoring system and the importances of the points within that system. Indeed, these theorems are of general interest in their ownright.

## 2Method

Pollard (2016) noted that there are several factors that can contribute to the excitement of a situation in sport. Indeed, he focused on a mathematical approach based on outcome probabilities for the point. He noted that the excitement of a particular point within a scoring system can be measured by the expected value of the absolute size of the change in a player’s probability of an overall win as a result of that point being played. It follows that the excitement of a point is related to the importance of the point (Morris (1976)). Namely, if p is player A’s probability of winning a point with importance I, the excitement of that point is equal to 2pqI, where q = 1 - p.

We begin by considering two simple and very similar scoring systems that are particularly relevant to this paper. They are W2AL^{a} and W2AL^{b} when pa = 0.9 and pb = 0.5. It can be shown that when the score is -1 (player A trailing by 1 point), player A’s probability of winning is 0.81 under W2AL^{b} and that it is 0.45 under W2AL^{a}, whilst his probability of winning at the score of 0 is 0.9 under both systems, and it is clearly zero at the score of – 2 for both systems. Thus, the point played at the score of – 1 has an importance of 0.9 under both scoring systems. However, the point played at the score of – 1 is more exciting under scoring system W2AL^{a} than it is under the scoring system W2AL^{b}. The expectation of the absolute value of the change in player A’s probability of winning the game at the score of – 1 is equal to 0.5*|0.9 – 0.45| + 0.5*|0.45 – 0| = 0.45 for W2AL^{a}, whereas it is 0.9*|0.9 – 0.81| + 0.1*|0.81 – 0.0| = 0.162 for W2AL^{b}. The excitement at the score of – 1 is greater under W2AL^{a} because player A’s (and hence also player B’s) probability of winning is about to experience a greater expected absolute change under that system. This example highlights the difference between the importance of a point and the excitement of a point. It is easy to show that the excitement of a point is in fact equal to the importance of that point multiplied by 2pq where p is the probability that player A wins the point, and q = 1 – p.

Continuing briefly with the above example, for W2AL^{a} the excitement at the score of +1 can be shown to be 0.05 and the excitement at the score of 0 to be 0.09. Thus, starting from a score of 0, the expected total excitement for the first two points is equal to 1*0.09 + 0.9*0.05 + 0.1*0.45 = 0.18. For the system W2AL^{b} the excitement at the score of +1 is equal to 0.018 and the excitement at the score of 0 is equal to 0.09. Thus, starting from a score of 0 in W2AL^{b}, the expected total excitement for the first two points is equal to 1*0.09 + 0.5*0.018 + 0.5*0.162 = 0.18, interestingly the same as for W2AL^{a}.

In the above paragraph the excitement of a point has been defined as the expectation of the absolute value of the change in player A’s probability of winning the game as a result of the playing of that point. It can be seen that this is a measure of ‘probability variation’ resulting from the playing of that point. As in other areas of statistics it is possible to devise other measures of variation, and the squared measure is a standard one. Thus, we might define a second measure of excitement based on the square of changes in probability. The second measure of excitement is the expected value of the square of the change in player A’s probability of winning as a result of the playing of that point. This measure is called Ex2, and the first measure Ex1. It is straightforward to show that Ex2 is equal to pqI^{2} where I is the importance of the point, p is the probability player A wins the point, and q = 1 - p. We note here that, just as the measure Ex1 can be used in the situation where there are more than just the two outcomes, win or loss, this second measure Ex2 can also be used where there are three or more outcomes (e.g. win, draw or loss).

Four new and quite general scoring system theorems that are needed for this study are now presented.

**Theorem 1.** Consider a scoring system in which player A’s probability of winning is P and the importance of the point in state i is I_{i}, when player A has a probability p_{i} of winning the point in state i and a probability q_{i} (= 1 – p_{i}) of losing the point (*i* = 1, 2, ...). Suppose he modifies his probabilities of winning the points in states i by an amount *δ*_{i} (*i* = 1, 2, ...). Then his overall probability of winning is modified by an amount *Δ*P =** Σ**n

_{i}*I

_{i}*

*δ*

_{i}, where n

_{i}is the expected number of times state i is entered in one realization of the scoring system with player A’s modified point probabilities pi +

*δ*

_{i}. Note that I

_{i}is the importance of the point in state i before the probabilities are modified.

**Proof.** We note firstly (before any modifications in player A’s point probabilities) that by playing the point in state i, player A’s overall probability of winning increases by q_{i}*I_{i} with probability p_{i} or decreases by p_{i}*I_{i} with probability q_{i}. This increase or decrease in Player A’s probability of winning can be considered a positive or negative step (resulting from the playing of this point) along the P axis which goes from 0 (A loses) to 1 (A wins). As the expected number of times state i is entered is n_{i} after he modifies his point probabilities by *δ*_{i}, the expected value of the sum of these step values is equal to ** Σ**n

_{i}*((p

_{i}+

*δ*

_{i})*q

_{i}*I

_{i}+ (q

_{i}–

*δ*

_{i})(– p

_{i}*I

_{i})), and this equals

**n**

*Σ*_{i}*

*δ*

_{i}*I

_{i}. The sum of these steps is also given by P’(1–P) – Q’P where P’ is player A’s overall probability of winning with the modified point probabilities, and Q’ = 1 - P’. Further, P’(1 - P) - Q’P =

*Δ*P, where

*Δ*P = P’ – P, and this completes the proof.

**Corollary 1.** Consider two equal players (with p = 0.5 on every point in unipoints or pa = pb in bipoints) playing a fair game (namely, one in which the probability player A wins the game is 0.5, and the probability player B wins it is also 0.5). Suppose player A increases his probability of winning each point by *δ*. Then, if P is now player A’s probability of winning the game given his increased probability of winning each point, P/Q = (1 + 2*Δ*P)/(1 - 2*Δ*P), where *Δ*P =** Σ** n

_{i}*I

_{i}*

*δ*, I

_{i}is the importance of the point at state i when the players are equal and n

_{i}is the expected number of times state i is entered in one realization of the game with player A’s increased point probabilities.

**Proof.** This result follows from Theorem 1.

**Theorem 2.** For any scoring system which results in a win to player A with probability P or a loss to player A with probability Q (where P + Q = 1), suppose the sum S is defined by *S* =** Σ** n

_{i}p

_{i}q

_{i}I

_{i}

^{2}where the summation is over all the transient states i, n

_{i}is the expected number of times state i is entered, p

_{i}is the probability player A wins the point in that state, I

_{i}is the importance of that state, and q

_{i}= 1 - p

_{i}. Thus S is the weighted sum of the values of Ex2 for each state. Then S is equal to PQ.

**Proof.** We use backward induction, and consider without loss of generality, the movement from any transient state 1 to transient state 2 with probability p1 or transient state 3 with probability q1, where q1 = 1 – p1. We assume the result is true for states 2 and 3. Thus, this sum from state 1 onwards is equal to

1 1*p1*q1*I

_{1}^{2}+ p1*n*Σ*_{j}p_{j}q_{j}I_{j}^{2}+ q1*n*Σ*_{k}p_{k}q_{k}I_{k}^{2}2 = p1*q1*(P

_{2}-P_{3})^{2}+ p1*P_{2}*Q_{2}+ q1*P_{3}*Q_{3}, using an obvious notation3 = p1*q1*(P

_{2}- P_{3})*(Q_{3}- Q_{2}) + p1*P_{2}*Q_{2}+ q1*P_{3}*Q_{3}4 = (p1*P

_{2}+ q1*P_{3})*(p1*Q_{2}+ q1*Q_{3})5 = P

_{1}*Q_{1}, using the same notation, and this completes the proof.

**Corollary 2.** For the scoring system in Theorem 2, *P* = (1 + SQRT(1 – 4*S))/2, *Q* = (1 - SQRT(1 – 4*S))/2, and P/Q = (1 + SQRT(1 – 4*S))/(1 - SQRT(1 – 4*S)).

**Proof.** This result follows from Theorem 2.

The above two theorems are applicable in a very general sense, and two examples are given in the Appendix to demonstrate this.

**Theorem 3.** Given two equal players (with p = 0.5 on every point in unipoints or pa = pb in bipoints) playing a fair game (one in which the probability player A wins the game is 0.5 and the probability player B wins it is 0.5), suppose player A increases his probability of winning each point by *δ*. Then, P*Q + (*δ**** Σ** n

_{i}*I

_{i})

^{2}= 0.25, where I

_{i}is the importance of the point at state i when the players are equal and n

_{i}is the expected number of times state i is entered in one realization of the game with player A’s increased point probabilities.

**Proof.** This result follows from Corollaries 1 and 2.

**Theorem 4.** Suppose the two systems W1(WkAL^{a}, WkAL^{b}) and W1(WmPW^{a}, WmPW^{b}) have the same expected durations, and the same importances I for every point when pa = pb = p. Now suppose player A increases his probability of winning every point by *δ*. Then P_{AL}*Q_{AL} = 0.25 – I^{2}**δ*^{2}**μ*_{AL}^{2} and P_{PW}*Q_{PW} = 0.25 – I^{2}**δ*^{2}**μ*_{PW}^{2} for the two systems, where *μ*_{AL} and *μ*_{PW} are the expected durations of the two systems with player A’s increased probability of winning each point.

**Proof.** This result follows from Theorem 3.

**Corollary 3.** The corresponding equation to that in Theorem 4 also holds when the two systems are W1(WkAL^{a}, WkAL^{b}) and W1(WnPL^{a}, WnPL^{b}), and when the two systems are W1(WnPL^{a}, WnPL^{b}) and W1(WmPW^{a}, WmPW^{b}).

Returning to the major focus of this study, we note that Pollard (1986, 1992) showed that the scoring systems W1(WnSS^{a}, WnSS^{b}), where SS is AL, PL or PW, all have the constant probability ratio property (cpr). That is, the ratio of the probability that player A wins in n + 2 m points divided by the probability that he loses in n + 2 m points (m = 0, 1, 2, ...) is a constant, and is equal to the value of P/Q for that scoring system. In particular, for the systems Wn(point-pairs) and W1(WnAL^{a}, WnAL^{b}), the cpr is P/Q = (pa^{n}*qb^{n})/(pb^{n}*qa^{n}) and (P-Q)/*μ*= (pa-pb)/2n. The values of these expressions for the systems W1(WnPL^{a}, WnPL^{b}) and W1(WnPW^{a}, WnPW^{b}) are given in Table 1.

##### Table 1

System | cpr, P/Q | (P-Q)/μ |

W1(WnAL^{a}, WnAL^{b}) | (pa^{n}*qb^{n})/(pb^{n}*qa^{n}) | (pa-pb)/2n |

W1(WnPL^{a}, WnPL^{b}) | (pa*qb^{2n - 1})/(pb*qa^{2n - 1}) | (pa-pb)/(2(1+(n-1)(pa+pb))) |

W1(WnPW^{a}, WnPW^{b}) | (pa^{2n - 1}*qb)/(pb^{2n - 1}*qa) | (pa-pb)/(2(1+(n-1)(qa+qb))) |

The expressions in Table 1 allow us to compare these efficient W-systems for their efficiency and other aspects. The efficiency of scoring system is a function of P and *μ* (see equation (1)). It can also be seen as a function of (P-Q)/*μ* and P/Q. It is clear that the average importance and the average excitement of points within a scoring system are typically smaller when the expected duration of a scoring system is larger. It is typically not possible to compare two scoring systems with exactly the same expected duration. However, with the systems in Table 1 we can compare two systems with the same value of (P-Q)/*μ*, that is, with very similar values of *μ*. We next show how this can be done.

The first two very efficient systems we compare are an AL one and a PW one. We suppose pa = l/(l+m) + *δ* and pb = l/(l+m) – *δ*, where l and m are integers, and *δ* is such that pa and pb are legitimate probabilities. For the scoring system W1(Wn1PW^{a}, Wn1PW^{b}), we have (P–Q)/*μ*=*δ*/(1+(n1–1)*(2 m/(l+m))), and for the scoring system W1(Wn2AL^{a}, Wn2AL^{b}), we have (P–Q)/*μ*=*δ*/n2. Thus, the values for (P–Q)/*μ* for these two scoring systems are equal if n2 = 1+(n1–1)*2 m/(l+m). Hence, for example, if l = 3 and m = 1, these two systems have the same values for (P-Q)/*μ* when (n1, n2) are (3, 2), or (5, 3), or (7, 4), ... . It follows from the form of equation (1) above that, for these values of l, m, n1 and n2, the ratio of the efficiencies of these two systems is simply the ratio of the natural logarithms their P/Q (or cpr) values.

The first of the specific examples in the previous paragraph (n1 = 3 and n2 = 2), namely W1(W2AL^{a}, W2AL^{b}) and W1(W3PW^{a}, W3PW^{b}) when l = 3 and m = 1, is now considered in detail. It is known from earlier work described in the introduction that the system W1(W2AL^{a}, W2AL^{b}) is the more efficient of these two systems when pa + pb >1. Standard numerical markov chain methods were used to find the expected number of points played and the probability player A wins using the scoring system W1(W2AL^{a}, W2AL^{b}). This scoring system starts with an a-point played at state (0, a), and the first section of it is completed when the score reaches +2 when state W, 0b is reached (and the W2AL^{b} section commences with the b-point) or when the score reaches – 2 when the state L, 0b is reached (and the W2AL^{b} section commences). It can be seen that there are nine transient states (or scores) in this formulation, and of course two absorbing states (‘A wins’ and ‘A loses’). The numerical markov chain approach that was used is described for example in the text by Kemeny and Snell (1960, pp.43-49). This numerical approach was taken as it appeared that, in general for the various systems under consideration, explicit expressions for the importance of each point and the expected number of times each point is played, and thus the average weighted importance and the average weighted excitement would be either very complicated or not achievable. Note that this numerical approach required matrix inversion, and the matrix became quite large as the n in Table 1 becamelarge.

When pa = pb = 0.75 (i.e. l = 3, m = 1 and *δ*= 0) the two systems W1(W2AL^{a}, W2AL^{b}) and W1(W3PW^{a}, W3PW^{b}) can be shown to have the same expected duration of 64/3 points, and every point within each of the two systems has an importance of 0.25. Table 2 gives, for the W1(W2AL^{a}, W2AL^{b}) system, the probability that player A wins from each of the nine transient states, the importance of each state, and n_{i}, the number of times each state is entered in one realization of W1(W2AL^{a}, W2AL^{b}).

##### Table 2

State | Probability | Importance, I_{i} | n_{i} | n_{i} * I_{i} |

W, 1a | 15/16 | 1/4 | 2/3 | 1/6 |

W, 0b | 12/16 | 1/4 | 8/3 | 2/3 |

W, – 1a | 11/16 | 1/4 | 2 | 1/2 |

1, b | 9/16 | 1/4 | 4 | 1 |

0, a | 8/16 | 1/4 | 16/3 | 4/3 |

–1, b | 5/16 | 1/4 | 4/3 | 1/3 |

L, 1a | 7/16 | 1/4 | 2/3 | 1/6 |

L, 0b | 4/16 | 1/4 | 8/3 | 2/3 |

L, –1a | 3/16 | 1/4 | 2 | 1/2 |

Total a, Na | 32/3 | 8/3 | ||

Total b, Nb | 32/3 | 8/3 | ||

Total or Average | 64/3 | 0.25 |

Table 3 gives the same information as Table 2, but for the parameter values pa = 0.76 and pb = 0.74 (i.e. *δ*= 0.01). It also gives an additional column. The mean duration of W1(W2AL^{a}, W2AL^{b}) when pa = 0.76 and pb = 0.74 is equal to 21.2615 and the average weighted importance of the points is 0.2483. Note that values are given to 4 decimal places, unless it is considered necessary or useful to do otherwise. It follows from Table 3 that the weighted sum of the excitements Ex1 is 1.9774, and the weighted sum of the excitements Ex2 is 0.2472. Also, the average importance per point played is equal to 0.0117, the average Ex1 per point played is 0.0930, and average Ex2 per point played is 0.0116.

##### Table 3

State | Probability | Importance, I_{i} | n_{i} | n_{i} * I_{i} | n_{i} * I_{i}^{2} |

W, 1a | 0.9492 | 0.2115 | 0.7278 | 0.1539 | 0.0326 |

W, 0b | 0.7885 | 0.2172 | 2.7994 | 0.6081 | 0.1321 |

W, –1a | 0.7320 | 0.2353 | 2.0715 | 0.4875 | 0.1147 |

1, b | 0.6143 | 0.2353 | 4.0397 | 0.9507 | 0.2237 |

0, a | 0.5532 | 0.2549 | 5.3154 | 1.3551 | 0.3455 |

–1, b | 0.3594 | 0.2618 | 1.2757 | 0.3340 | 0.0875 |

L, 1a | 0.4903 | 0.2618 | 0.6542 | 0.0713 | 0.0448 |

L, 0b | 0.2913 | 0.2689 | 2.5160 | 0.6766 | 0.1819 |

L, –1a | 0.2214 | 0.2913 | 1.8619 | 0.5424 | 0.1580 |

Total a, Na | 10.6308 | 2.7102 | 0.6956 | ||

Total b, Nb | 10.6308 | 2.5694 | 0.6252 | ||

Total or Average | 21.2615 | 0.2483 |

The analyses summarized in Tables 2 and 3 for W1(W2AL^{a}, W2AL^{b}) were repeated for W1(W3PW^{a}, W3PW^{b}), and a comparison of the two systems is given in Table 4. The efficiency of W1(W3PW^{a}, W3PW^{b}) when pa = 0.76 and pb = 0.74 is equal to 0.999822 (from equation (1)), whilst W1(W2AL^{a}, W2AL^{b}) has unit efficiency. It can be seen that the more efficient of these two scoring systems, W1(W2AL^{a}, W2AL^{b}), has the following seven characteristics

1. a greater cpr,

2. points with greater average importance,

3. a greater value for the average importance per point played,

4. points with smaller average total excitements, Ex1 and Ex2,

5. smaller values for the average total excitement per point played,

6. greater average total Shannon entropy, and

7. greater average total Shannon entropy per point played.

##### Table 4

W1(W2AL^{a}, W2AL^{b}) | W1(W3PW^{a}, W3PW^{b}) | |

Na | 10.630774 | 10.841475 |

Nb | 10.630774 | 10.416320 |

Expected duration, μ | 21.261549 | 21.257795 |

Probability A wins, P | 0.5531539 | 0.5531445 |

Efficiency | 1.0 | 0.999822 |

cpr | 1.237907 | 1.237860 |

(P-Q)/μ | 0.005 | 0.005 |

P*Q | 0.2471747 | 0.2471757 |

S = nΣ_{i}p_{i}q_{i}I_{i}^{2} | 0.2471747 | 0.2471757 |

0.25 –I^{2}*δ^{2}*μ^{2} (with I = 0.25) | 0.2471747 | 0.2471757 |

Average Importance, a-points | 0.2549437 | 0.2449901 |

Average Importance, b-points | 0.2416930 | 0.2516034 |

Average Importance, all points | 0.2483183 | 0.2482306 |

Average Importance per point played | 0.0116792 | 0.0116772 |

Average total excitement, Ex1, a-points | 0.9886987 | 0.9689286 |

Average total excitement, Ex1, b-points | 0.9886987 | 1.0084767 |

Average total excitement, Ex1, all points | 1.9773973 | 1.9774053 |

Average total excitement Ex1 per point played | 0.093003 | 0.093020 |

Average total excitement, Ex2, a-points | 0.1268820 | 0.1192684 |

Average total excitement, Ex2, b-points | 0.1202927 | 0.1279072 |

Average total excitement, Ex2, all points | 0.2471747 | 0.2471756 |

Average total excitement Ex2 per point played | 0.0116254 | 0.0116275 |

Average total Shannon entropy | 11.9504 | 11.9437 |

Average total Shannon entropy per point played | 0.56207 | 0.56185 |

As a second example we compare W1(W3PL^{a}, W3PL^{b}) with W1(W4AL^{a}, W4AL^{b}) when pa = 0.76 and pb = 0.74. The value of (P-Q)/*μ* for each of these two scoring systems is equal to 0.0025. Equation (1) can be used to show that the system W1(W3PL^{a}, W3PL^{b}) has an efficiency of 1.000089 whilst W1(W4AL^{a}, W4AL^{b}) has efficiency of 1 when pa = 0.76 and pb = 0.74. (It is noted that when pa = pb = 0.75, both these scoring systems have an expected duration of 256/3 points and all points have an importance of 0.125). It was shown that the more efficient scoring system W1(W3PL^{a}, W3PL^{b}) has the same seven characteristics noted above.

As a third example we compare W1(W3PL^{a}, W3PL^{b}) with W1(W5PW^{a}, W5PW^{b}) when pa = 2/3 + 0.01 and pb = 2/3 – 0.01. The value of (P-Q)/*μ* for each of these two scoring systems is equal to 3/1100. Equation (1) can be used to show that the system W1(W3PL^{a}, W3PL^{b}) has an efficiency of 1.0000546 and W1(W5PW^{a}, W5PW^{b}) has efficiency of 0.999891 when pa = 2/3 + 0.01 and pb = 2/3 – 0.01. (It is noted that when pa = pb = 2/3, both these scoring systems have an expected duration of 30.25 and all points have an importance of 3/22.) When pa = 2/3 + 0.01 and pb = 2/3 – 0.01, the more efficient scoring system W1(W3PL^{a}, W3PL^{b}) has the same seven characteristics noted in the two examples above.

A modified approach for deriving *some* of the results in the above table (but not those for Ex1) is now described. This approach is useful when the values of n in these systems are not as small as in the above examples, and the matrices needed to be inverted (numerically) would be quite large. To demonstrate this, suppose we are interested in calculating the characteristics for W1(WnAL^{a}, WnAL^{b}) and W1(WmPL^{a}, WmPL^{b}) when (pa, pb) equals, say, (0.71, 0.69). These two systems have the same value for (P-Q)/*μ* when *n* = 8 and *m* = 6. Making use of the expressions in Table 1, equation (1), and Theorem 2, the results for these two systems are shown in Table 5. It can be seen that the more efficient scoring system W1(W6PL^{a}, W6PL^{b}) has the following 5 characteristics

1. a greater cpr,

2. points with smaller total average excitement Exc2,

3. a smaller value for the total average excitement Exc2 per point played,

4. greater average total Shannon entropy, and

5. greater average total Shannon entropy per point played.

##### Table 5

W1(W6PL^{a}, W6PL^{b}) | W1(W8AL^{a}, W8AL^{b}) | |

Na | 143.642952 | 145.450714 |

Nb | 147.279482 | 145.450714 |

Expected duration, μ | 290.922434 | 290.901428 |

Probability A wins, P | 0.6818265 | 0.6818134 |

Efficiency | 1.000079406 | 1.0 |

cpr | 2.142939516 | 2.142809837 |

(P-Q)/μ | 0.00125 | 0.00125 |

P*Q | 0.2169391 | 0.2169439 |

Average total excitement Ex2 = S = nΣ_{i}p_{i}q_{i}I_{i}^{2} | 0.2169391 | 0.2169439 |

Average total excitement Ex2 per point played | 0.000745694 | 0.000745764 |

Average total Shannon entropy | 177.67567 | 177.63203 |

Average total Shannon entropy per point played | 0.610732 | 0.610626 |

As a second example of this modified approach, suppose we are interested in calculating the characteristics for W1(WnAL^{a}, WnAL^{b}) and W1(WmPW^{a}, WmPW^{b}) when (pa, pb) equals, say (0.71, 0.69). Here it can be shown that W1(W7AL^{a}, W7AL^{b}) and W1(W11PW^{a}, W11PW^{b}) have the same value of (P-Q)/*μ*, and the more efficient system W1(W7AL^{a}, W7AL^{b}) can be shown to have the same five characteristics noted above.

As a third example we compare W1(WnAL^{a}, WnAL^{b}) and W1(WmPL^{a}, WmPL^{b}) when (pa, pb) equals, say (0.72, 0.70). Here W1(W72AL^{a}, W72AL^{b}) and W1(W51PL^{a}, W51PL^{b}) have the same value of (P-Q)/*μ*, and the more efficient system W1(W51PL^{a}, W51PL^{b}) can be shown to have the same five characteristics noted above.

In general, it can be seen that, given any two values of pa and pb, it is possible to compare any two of the three general W systems under consideration (AL, PW, PL) by using an appropriate n and m value, and the more efficient system can be shown using the ‘*matrix approach*’ *to have the seven characteristics noted above. Correspondingly, the* ‘*non-matrix approach*’ *can be used to show that the more efficient system has the five characteristics notedsecondly.*

## 3Conclusions

It has been noted that a set of tennis can be considered to be a rather specific design for a sequential 2-sample binomial statistical test, albeit not an efficient one. The excitement of a particular point within a tennis set can be measured by the absolute change in a player’s probability of winning the set as a result of that point being played. A squared measure of excitement has also been defined. These excitement measures for a point are thus measures of variability in a player’s probability of winning as a result of the point being played. The most efficient sequential 2-sample binomial test in a given situation has been shown to have the smallest average excitement per point played (or per bernouilli trial). This most efficient binomial test has also been shown to have the largest average ‘importance’ per point played and the largest ‘Shannon entropy’ per point played.

These characteristics of the most efficient 2-sample binomial tests give further insights into the design of efficient statistical tests, and may be useful conceptually in the design of statistical tests for other situations.

## Appendices

### Appendix

**Example A1.** This is an example of Theorem 2. Consider a game in which the winner is the first player to reach 3 ‘units’. Suppose player A gets 1 ‘unit’ for each point he wins, and player B gets 1 ‘unit’ for each point he wins except the first point played for which he gets two ‘units’ if he wins it. Clearly this is an unfair game. Using the notation (n1, n2, n3) to represent the state where player A has won n1 ‘units’, player B has won n2 ‘units’ and n3 points have been played, the possible states in this game are (0,0,0), (1,0,1), (0,2,1), (2,0,2), (1,1,2), (1,2,2), (0,3,2) = L, (3,0,3) = W, (2,1,3), (2,2,3), (1,2,3), (1,3,3) = L, (3,1,4) = W, (3,2,4) = W, (2,2,4), (2,3,4) = L, (1,3,4) = L, (3,2,5) = W and (2,3,5) = L. The absorbing states where player A loses (L) or wins (W) are identified. Taking the 10 transient (or non-absorbing) states in the above order, and supposing the *p*-values (for the probability that player A wins the point in that state) are respectively 0.8, 0.3, 0.7, 0.4, 0.5, 0.6, 0.4, 0.5, 0.6 and 0.6, it can be shown(by calculating backwards from the last possible point) that the importances of these points are equal to 0.4388, 0.296, 0.3, 0.24, 0.4, 0.5, 0.4, 1.0, 0.6 and 1.0 respectively. For these values of p, the values of n_{i} for these transient states are equal to 1, 0.8, 0.2, 0.24, 0.56, 0.14, 0.424, 0.084, 0.28 and 0.4224 respectively. It follows that ** Σ**n

_{i}p

_{i}q

_{i}I

_{i}

^{2}= 0.2462741184. First principles can be used to show that the probability A wins the game, P is equal to 0.56104, and Theorem 2 can then be verified.

**Example A2.** We now suppose player A in Example A1 modifies his *p*-values in the 10 transient states in the above example by *δ*_{i} values of – 0.2, 0.1, – 0.1, 0.1, 0.1, 0.1, 0.1, – 0.1, 0.1, and – 0.1 respectively. The n_{i} values are now equal to 1, 0.6, 0.4, 0.24, 0.36, 0.24, 0.336, 0.168, 0.144 and 0.2688 and, using Theorem 1, *Δ*P =** Σ**n

_{i}*

*δ*

_{i}*I

_{i}= – 0.07144 and so player A’s probability of winning is now P’ = 0.56104 – 0.07144 = 0.4896, which can be verified by first principles.

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