A Shorter-Length Confidence-Interval Estimator (CIE) for...
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A Shorter-Length Confidence-Interval Estimator (CIE) for Sharpe-Ratio Using a Multiplier k* to the
Usual Bootstrap-Resample CIE and Computational Intelligence
Chandra Shekhar Bhatnagar1, [email protected]
Ashok Sahai2, [email protected]
Viswanadham Bulusu 3, [email protected]
ABSTRACT
The population value of the Sharpe (1966) performance measure for portfolio i is defined as i f
i
r
for i = 1, 2,..., n. It is simply the
mean excess return over the standard deviation of the excess returns for the portfolio. The sample estimate of any of these portfolio
measures is challenging not only because of the dynamic nature of this measure but also because of the statistical estimation issue
involved therein. This paper has been motivated by the desire to meet the challenge of statistical estimation. A new estimator for
Sharpe‟s ratio is formulated using the optimal value defined as k*, which is used as a multiplier for the usual sample-counterpart
estimator. This formulation has been pivotal to an efficient Confidence-Interval estimator (CIE). „Computational Intelligence‟ has
been deployed for the optimal mixing [using the optimal value of a design parameter, θ] of the proposed estimator and usual
sample-counterpart estimator with the aim of achieving the shortest length of the proposed bootstrap-resample Confidence-Interval
estimator (PBCIE) for Sharpe‟s ratio. We have been successful in achieving a shorter length through the proposed Bootstrap-
resample Confidence Interval Estimator [PBCIE] for Sharpe‟s ratio vis-à-vis the Usual Bootstrap-resample Confidence Interval
Estimator [UBCIE], without paying the usual cost in terms of a greater „Coverage Error‟. An empirical simulation study has been
used to bring forth the potential gain through a more efficient estimation in the context, with the limitation of the normal distribution
being followed by the population for the portfolios. The empirical simulation study is modeled around the values of parameters in
the study by Vinod and Morey (1999)
Key Words & Phrases: Bootstrap resampling; Computational intelligence; Coverage error & the length of the confidence interval
estimation; Empirical simulation study.
1 Department of Management Studies, The University of the West Indies,St. Augustine, Trinidad 2 Department of Mathematics and Statistics, The University of the West Indies, St. Augustine, Trinidad 3 Principal, Aurora‟s Degree & PG College, Chikkadpally; Hydearbad, India.
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I. Introduction
The Sharpe‟s Ratio (1966, 1994) is one of the standard tools in evaluating the performance of portfolios. It is
intuitive and lends itself easily to computation and interpretation. It represents the excess return per unit of
standard deviation of return and can be easily looked up as the slope of the capital allocation line (CAL).
Since the Sharpe‟s ratio gives us the price of risk, it follows that the ratio is widely used in comparing
portfolio performance and identifying superior portfolios. Using Roy‟s (1952) argument to use the reward –
to- risk ratio in appraising portfolio (or any strategy‟s) performance, the Sharpe‟s ratio modifies Markowitz‟s
(1952) efficient frontier of risky assets by incorporating a proxy risk-free rate (or the rate offered by a
benchamrk portfolio resulting in what we understand as the Information Ratio). From there, it facilitates the
task of identifying the optimum portfolio that is tangent to the the efficient frontier, having a property of
maximizing the slope of CAL.
Returns are often not normal (Goetzmann, Ingersoll, Spiegel and Welch (2002)), and comparable over time
(Sharpe (1994), Lo (2002)) and since they serve as the first data admission in computing Sharpe‟s ratio, there
is bound to be an estimation error in the ratio itself. The recognition of non-normality as a contributing factor
in estimation errors has always nagged the researchers, more so since Michaud (1989) examined and
questioned the “optimality” of the “optimized” portfolio in the Markowitz mean-variance paradigm. Further,
due to the presence of a random denominator in the definition of the ratio, the sampling distribution of the
Sharpe ratio is somewhat difficult to determine, even when using data from large samples (Christie (2007)).
Lo (2002) set the ball rolling with his work on the statistical distribution of the Sharpe ratio under various
scenarios for the return distribution. Earlier, Jobson and Korkie (1981) did consider a test of the difference
between Sharpe ratios under the assumption of multivariate normality, but found that their test lacked power.
We tackle the challenge of statistical estimation by attempting to propose a new estimator for Sharpe‟s ratio to
serve as an efficient Confidence-Interval estimator (CIE). We draw from the work of Vinod and Morey (2001)
who proposed a modified version of the Sharpe ratio, called the Double Sharpe ratio, to take into account
estimation risk. We use bootstrap sampling and computational intelligence with the aim of achieving the
shortest length proposed bootstrap-resample Confidence-Interval estimator of the Sharpe‟s Ratio. The
procedure followed is similar but not limited to Sahai and Strepnek (2011)
In the next section, we specify the Sharpe‟s ratio and discuss our proposed bootstrap confidence interval (CI)
estimator for the ratio. Section III illustrates the relative gain from our proposed estimator. Section IV
concludes the paper.
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II. The Proposed Bootstrap Confidence Interval Estimator for Sharpe’s Ratio
Let us say, there is an investment position, P, invested partially in a risky portfolio and a risk-free asset. If w
represents the weight on the risky portfolio i, µ represents the expected return, and rf is the risk-free rate of
return, the expecte return of position P can be described as:
(1 )P i fw w r (1)
We can re-write (1) as follows:
P i f fw wr r , or
[ ]P f i fr w r (2)
Since the risk of combined position P, as measured by the standard deviation of expected return, would
emanate from only the risky portfolio, we can write the standard deviation of position P as:
P iw , which further implies that;
P
i
w
(3)
Substituting (3) in (2) yields the capital allocation line, CAL;
PP f i f
i
r r
(4)
From (4), it can be seen that i f
i
r
is the slope of the CAL, also known as the Sharpe‟s ratio, Sri. The
population value of the Sharpe‟s performance measure for portfolio i is simply the mean excess return over
the standard deviation of the excess returns for the portfolio. Therefore, for any portfolio in general, we have
the population value of the Sharpe‟s ratio as i f
i
r
. In the aforesaid μ is the population mean, rf is the risk-
free rate of return with zero variance and σi is the portfolio‟s standard deviation. It is commonly seen in the
literature, that the sample counterparts that estimate these population parameters, namely the sample mean,
and the sample standard deviation are calculated from a random sample (x1, x2, x3,…, xn) as follows:
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1
n
i
i
x
xn
,
2
2 1
1
n
i
i
x x
sn
, and
2s s
This leads to an applied point estimate for Sharpe‟s ratio of;
ˆx
Srs
As indicated earlier, one problem with the Sharpe‟s ratio is that its denominator is random, as it is computed
using a data sample of returns on a given history and not the whole population of returns. So, it is difficult to
evaluate its risk estimation. Vinod and Morey (2001) proposed a modified version of the Sharpe‟s ratio, called
the Double Sharpe ratio, to take into account the estimation risk. This ratio is defined as ˆ
ˆˆ
Sr
SrDSr
, where
ˆSr is the standard deviation of the Sharpe ratio estimate, or the estimation risk. They do not use the sample
(x1, x2, x3,…, xn) directly in the calculation of their „Double Sharpe Ratio‟. Instead, to calculate this standard
deviation they use bootstrap methodology to generate 999 resamples from the original returns. We note here
that the sampling error is seminal to the estimation risk or the estimation error. Vinod and Morey (2001)‟s
„Double Sharpe ratio‟ takes care of this „estimation error‟ implicitly, just like the Sharpe‟s ratio.
Our proposed improvement of Vinod and Morey (2001)‟s „Double Sharpe Ratio‟ also uses 999 bootstrap
resamples. These resamples have been used to calculate the bootstrap mean of these estimates and hence
„Confidence Interval Estimate (CIE)‟ of Sharpe‟s ratio. The improved „Confidence Interval Estimate (CIE)‟ of
Sharpe‟s ratio constructed and proposed in this paper consists in estimation of both the numerators & the
denominators of the ratio.
For doing so, our first target is to find an efficient estimator of the inverse of the normal standard deviation 1
. For that we first prove the following result:
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Lemma: For a random sample (x1, x2, x3, …, xn) from a normal population N (μ, σ), * 1.k
is the “Minimum
Mean-Square-Error Estimator (MMSE) of 1
; wherein;
2. 1
( 1) 2*
( 3)
2
n
nk
n
(5)
Proof: It can easily be checked that;
*
2
1 1.
1
Es
k
Es
Rest follows from the well-known fact that (n-1). s2 ~
2n-1.
Q.E.D.
We can handle the efficient estimation of numerator ˆSr of the Double Sharpe ratio, by possibly a more
efficient estimator using bootstrap resamples. This new estimator will take care of the „estimator error‟, rather
less explicitly.
To illustrate our proceedings comprehensibly we, for the ready comparative reference, borrow the study by
Vinod and Morey (1999) and to keep things in perspective as we proceed forward, we reproduce a selection
from their work:
“……the resampling for the Sharpe measure is done “with replacement” of the original excess returns
themselves for j =1,2, …, J or 999 times. Thus, we calculate 999 Sharpe measures from the original excess
return series. The choice of the odd number 999 is convenient, since the rank-ordered 25-th and 975-th values
of estimated Sharpe ratios arranged from the smallest to the largest, yield a useful 95% confidence interval. It
is from these 999 Sharpe measures that we calculate ( rS ˆ ). As an illustration, we have calculated the
Sharpe and Double Sharpe ratios for the 30 largest growth mutual funds. (as of January 1998 in terms of
overall assets managed)”.
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Their work reports the excess mean monthly returns, the standard deviation of the excess monthly returns, the
Sharpe ratio, the mean and standard deviation of the bootstrapped Sharpe ratios, the lower [0.025] and upper
[0.975] confidence values of the bootstrapped Sharpe value, the 95% confidence interval width, and the
Double Sharpe ratio. They mention that in their case, the sampling distribution that represents the estimation
risk is non-normal with positive skewness. This is why the means of the bootstrapped Sharpe ratios are always
slightly higher than the point estimates of Sharpe ratios, which ignore the estimation risk altogether.
In line with their work, we compute the „Usual Bootstrap-resample Confidence-Interval Estimator [UBCIE]
of Sharpe‟s ratio using the “the lower [0.025] and upper [0.975] confidence values of the bootstrapped
Sharpe value”, say LCV & UCV respectively.
Our “Proposed Bootstrap-resample Confidence-Interval Estimator [PBCIE] of Sharpe‟s ratio” has two phases.
In the first phase, we propose the “Modified Bootstrap-resample Confidence-Interval Estimator [MBCIE] of
Sharpe‟s ratio by modifying the LCV & UCV with k*, as below:
MLCV = k*. LCV (6)
and,
MUCV = k*. UCV (7)
In the second phase, we consider the “Proposed Bootstrap-resample Confidence-Interval Estimator [PBCIE]
of Sharpe‟s ratio as the one with the “Lower & Upper Confidence Values” , as below:
PLCV = LCV + θ.(LCV - k*.LCV) (8)
and
PUCV = UCV + θ.(UCV - k*.UCV) (9)
The parameter θ is the “Design Parameter” in the “Proposed Bootstrap-resample Confidence-Interval
Estimator [PBCIE] of Sharpe-Ratio” proposed to be used “Optimally” to design the proposed PBCIE is such a
manner as to lower the its “length” without paying the usual price in terms of the “Coverage Error” with the
CIE. This has been achieved by using the “Computational Intelligence” to determine that “Optimal Value” of
the design-parameter θ. The extensive simulational computational results lead to this sought-after Optimal-
Value of the design-parameter θ to be 15.6.
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III. Empirical Study Illustrating the Relative Gain through our Proposed CI Estimator
The empirical simulation study is carried out using a Matlab 2010b code for various illustrative values of the
sample sizes ~ 11, 21, 31, 41, 51, 71, 85 & 101. The parent population is taken to be normal with the
population Sharpe ratio „Sr‟ as 0.20 [around the values of the case-study in Vinod and Morey (1999)]. The
various values of population standard deviation (likewise in that study) are taken as σ = 3.25, 3.75, 4.25, 4.75,
5.25, 5.75, 6.25, 6.75 & 7.25 for illustration. The number of replications in the simulation is taken to be quite
large ~ „4444‟.
In each of these (4444) replications, for a typical value-combination of “n & σ”, we let the computer generate
the psuedo-random sample from the relevant “Normal Distribution” with the value of σ , and that of the
„Sharpe Ratio (Sr = 0.2)”. That sample is then used for the „999‟ bootstrap-resamples leading to the „Lower &
Upper‟ values of the various (95%) CIs; LCV & UCV for „Usual Bootstrap-resample Confidence-Interval
Estimator [UBCIE] for Sharpe‟s ratio & PLCV & PUCV for „Proposed Bootstrap-resample Confidence-
Interval Estimator [PBCIE] for Sharpe‟s ratio . Thence, from all these 4444 replications, we calculate for
these CIs {[UBCIE] & [PBCIE]}, the following performance-icons‟ values:
Coverage Probability ~ The relative frequency of the actual value being inside the relevant CI.
Coverage Error ~ Abs. (0.95 - Coverage Probability) for the relevant CI.
Length ~ average of the values Abs.(Lower Value of CI – Upper value of the CI) for the relevant CI.
Left Bias ~ average of the values Abs.(Lower Value of CI – Actual Value of SR (0.2)) {iff the actual value is
less than the lower value of the CI} for the relevant CI.
Right Bias ~ average of the values Abs.(Upper Value of CI – Actual Value of SR (0.2)) {iff the actual value is
more than the upper value of the CI} for the relevant CI.
Relative Bias = Abs. Left Bias - Right Bias
Left Bias + Right Bias
The resultant values of these „Features of CIs‟ are tabulated in Tables A.1 through A.9, in the appendix.
As apparent from the tabulated values in the appendix, our „Proposed Bootstrap-resample Confidence-Interval
Estimator [PBCIE] of Sharpe‟s ratio is consistently shorter in its “length” than the „Usual Bootstrap-resample
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Confidence-Interval Estimator [UBCIE] of Sharpe‟s ratio‟. Nevertheless, we have evidently manipulated
[through our optimal choice of the value of the design-parameter θ in our PBCIE of Sharpe‟s ratio using
“Computational Intelligence”] for the said “Optimal mixing of UBCIE of Sharpe‟s ratio & the “Modified
Bootstrap-resample Confidence-Interval Estimator [MBCIE] of Sharpe‟s ratio.
IV. Conclusion
The Sharpe's ratio is one of the widely prevalent metrics for evaluating and comparing portfolio performance.
It relates the reward of investing with its inherent risk. However, in a world where financial data does not
strictly conform to desired statistical attributes, the ratio‟s reliability may be questioned due to statistical
estimation error. This study seeks to and achieves an improvement in so far as a more robust statistical
estimation is evident by using bootstrap resampling and computational intelligence. The simulation results
demonstrate a marked improvement in terms of a shorter length of the proposed bootstrap-resample
Confidence-Interval estimator (PBCIE) for Sharpe‟s ratio, while keeping the coverage error in check. This has
been achieved by using k* as the multiplier for the usual sample counterpart estimator for the Sharpe‟s ratio
of the population. Using computational intelligence, a unique design parameter, θ, has been arrived at for an
optimal mixing of the proposed estimator and usual sample-counterpart estimator.
References:
Goetzmann, William N, Jonathan E Ingersoll, Matthew I Spiegel, and Ivo Welch, 2002, “Sharpening Sharpe
Ratios”, Yale Working Paper
H.D. Vinod and M.R. Morey, 1999, A Double Sharpe Ratio, Fordham University, New York
H.M. Markowitz, 1952, “Portfolio Selection”, Journal of Finance, 7(1), 77-91
Jobson, J.D. and B.M. Korkie, 1981, "Performance Hypothesis Testing with the Sharpe and Treynor
Measures," Journal of Finance, 36, No. 4, 889-908
Lo, Andrew W, 2002, “The Statistics of Sharpe Ratios”, Financial Analysts Journal, 36-52
Michaud, Richard O, 1989, “The Markowitz Optimization Enigma: Is 'Optimized' Optimal?”, Financial
Analysts Journal, 31-42
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Roy, Arthur D., 1952, “Safety First and Holding of Assets”, Econometricia, 431-450
Sahai, Ashok and Strepnek, Grant. H, 2011, “An Estimation Error Corrected Sharpe Ratio using Bootstrap
Resampling”, Journal of Applied Finance and Banking, Vol.1, No.2, 189-206
S. Christie, 2007, Beware the Sharpe Ratio, Macquarie University Applied Finance Centre, Sydney
Vinod, H. D. and M. R. Morey, 2001 “A Double Sharpe Ratio” in Advances in Investment Analysis and
Portfolio Management, Vol. 8.
W.F. Sharpe, 1966, “Mutual Fund Performance”, Journal of Business, 39, 119-138
W.F. Sharpe, 1994, “The Sharpe Ratio”, Journal of Portfolio Management, 21(1), 49-58
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APPENDIX
SIMULATION RESULTS [4444REPLICATIONS] FOR 95% CI :
THE PROPOSED VIS-A-VIS THE USUAL BOOTSTRAP CI FOR Sr USING k* AND COMPUTATIONAL INTELLIGENCE
Table A.1
n = 11, k*=0.922746
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.904365 0.045635 0.775564 0.029478 0.066157 0.383529
PBCIEstimator 0.904365 0.045635 0.304701 0.066157 0.029478 0.383529
σ = 3.750000
UBCIEstimator 0.908191 0.041809 0.770863 0.029703 0.062106 0.352941
PBCIEstimator 0.908191 0.041809 0.304089 0.062106 0.029703 0.352941
σ = 4.25
UBCIEstimator 0.90099 0.04901 0.770903 0.066157 0.032853 0.336364
PBCIEstimator 0.90099 0.04901 0.30294 0.066157 0.032853 0.336364
σ = 4.75
UBCIEstimator 0.90099 0.04901 0.774925 0.032853 0.066157 0.336364
PBCIEstimator 0.90099 0.04901 0.30294 0.066157 0.032853 0.336364
σ = 5.25
UBCIEstimator 0.903915 0.046085 0.775883 0.031953 0.064131 0.334895
PBCIEstimator 0.903915 0.046085 0.305519 0.064131 0.031953 0.334895
σ = 5.75
UBCIEstimator 0.897165 0.052835 0.797595 0.035104 0.067732 0.317287
PBCIEstimator 0.897165 0.052835 0.306319 0.067732 0.035104 0.317287
σ = 6.25
UBCIEstimator 0.89964 0.05036 0.778255 0.033303 0.067057 0.336323
PBCIEstimator 0.89964 0.05036 0.303756 0.067057 0.033303 0.336323
σ = 6.75
UBCIEstimator 0.901665 0.048335 0.778221 0.033078 0.065257 0.327231
PBCIEstimator 0.901665 0.048335 0.304833 0.065257 0.033078 0.327231
σ = 7.25
UBCIEstimator 0.90009 0.04991 0.79186 0.029253 0.070657 0.414414
PBCIEstimator 0.90009 0.04991 0.306329 0.070657 0.029253 0.414414
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Table A.2
n = 21, k*=0.961945
σ = 3.250000
95% CI Estimator
for SR
Coverage
Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.922142 0.027858 0.699992 0.025653 0.052205 0.34104
PBCIEstimator 0.922142 0.027858 0.384994 0.025653 0.052205 0.34104
σ = 3.750000
UBCIEstimator 0.925518 0.024482 0.701911 0.027228 0.047255 0.268882
PBCIEstimator 0.925518 0.024482 0.385653 0.027228 0.047255 0.268882
σ = 4.25
UBCIEstimator 0.928443 0.021557 0.69918 0.024752 0.046805 0.308176
PBCIEstimator 0.928443 0.021557 0.384956 0.024752 0.046805 0.308176
σ = 4.75
UBCIEstimator 0.926193 0.023807 0.699455 0.027228 0.04658 0.262195
PBCIEstimator 0.926193 0.023807 0.385489 0.027228 0.04658 0.262195
σ = 5.25
UBCIEstimator 0.923267 0.026733 0.698154 0.026553 0.05018 0.307918
PBCIEstimator 0.923267 0.026733 0.384651 0.026553 0.05018 0.307918
σ = 5.75
UBCIEstimator 0.930693 0.019307 0.698936 0.025653 0.043654 0.25974
PBCIEstimator 0.930693 0.019307 0.385386 0.025653 0.043654 0.25974
σ = 6.25
UBCIEstimator 0.924842 0.025158 0.695847 0.031503 0.043654 0.161677
PBCIEstimator 0.924842 0.025158 0.384979 0.031503 0.043654 0.161677
σ = 6.75
UBCIEstimator 0.926868 0.023132 0.698519 0.025878 0.047255 0.292308
PBCIEstimator 0.926868 0.023132 0.384726 0.025878 0.047255 0.292308
σ = 7.25
UBCIEstimator 0.930243 0.019757 0.701766 0.023177 0.04658 0.335484
PBCIEstimator 0.930243 0.019757 0.385501 0.023177 0.04658 0.335484
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Table A.3
n = 31, k*=0.974754
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.932493 0.017507 0.622104 0.027453 0.040054 0.186667
PBCIEstimator 0.932493 0.017507 0.457921 0.027453 0.040054 0.186667
σ = 3.750000
UBCIEstimator 0.936994 0.013006 0.618924 0.026103 0.036904 0.171429
PBCIEstimator 0.936994 0.013006 0.456452 0.026103 0.036904 0.171429
σ = 4.25
UBCIEstimator 0.935869 0.014131 0.621041 0.024077 0.040054 0.249123
PBCIEstimator 0.935869 0.014131 0.457496 0.024077 0.040054 0.249123
σ = 4.75
UBCIEstimator 0.935419 0.014581 0.619503 0.025203 0.039379 0.219512
PBCIEstimator 0.935419 0.014581 0.456784 0.025203 0.039379 0.219512
σ = 5.25
UBCIEstimator 0.939694 0.010306 0.620684 0.026103 0.034203 0.134328
PBCIEstimator 0.939694 0.010306 0.457053 0.026103 0.034203 0.134328
σ = 5.75
UBCIEstimator 0.931818 0.018182 0.618582 0.028578 0.039604 0.161716
PBCIEstimator 0.931818 0.018182 0.456729 0.028578 0.039604 0.161716
σ = 6.25
UBCIEstimator 0.939019 0.010981 0.620812 0.024752 0.036229 0.188192
PBCIEstimator 0.939019 0.010981 0.456905 0.024752 0.036229 0.188192
σ = 6.75
UBCIEstimator 0.932943 0.017057 0.620508 0.024302 0.042754 0.275168
PBCIEstimator 0.932943 0.017057 0.457767 0.024302 0.042754 0.275168
σ = 7.25
UBCIEstimator 0.940819 0.009181 0.620678 0.021377 0.037804 0.277567
PBCIEstimator 0.940819 0.009181 0.457566 0.021377 0.037804 0.277567
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Table A.4
n = 41, k*=0.981112
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.932043 0.017957 0.562544 0.022952 0.045005 0.324503
PBCIEstimator 0.932043 0.017957 0.456505 0.022952 0.045005 0.324503
σ = 3.750000
UBCIEstimator 0.939919 0.010081 0.560547 0.023627 0.036454 0.213483
PBCIEstimator 0.939919 0.010081 0.456179 0.023627 0.036454 0.213483
σ = 4.25
UBCIEstimator 0.943294 0.006706 0.558505 0.018902 0.037804 0.333333
PBCIEstimator 0.943294 0.006706 0.455138 0.018902 0.037804 0.333333
σ = 4.75
UBCIEstimator 0.940594 0.009406 0.558583 0.024977 0.034428 0.159091
PBCIEstimator 0.940594 0.009406 0.455309 0.024977 0.034428 0.159091
σ = 5.25
UBCIEstimator 0.943744 0.006256 0.558568 0.022502 0.033753 0.2
PBCIEstimator 0.943744 0.006256 0.455104 0.022502 0.033753 0.2
σ = 5.75
UBCIEstimator 0.941044 0.008956 0.560738 0.023177 0.035779 0.21374
PBCIEstimator 0.941044 0.008956 0.455998 0.023177 0.035779 0.21374
σ = 6.25
UBCIEstimator 0.943969 0.006031 0.560158 0.022727 0.033303 0.188755
PBCIEstimator 0.943969 0.006031 0.455534 0.022727 0.033303 0.188755
σ = 6.75
UBCIEstimator 0.939019 0.010981 0.558946 0.024527 0.036454 0.195572
PBCIEstimator 0.939019 0.010981 0.455623 0.024527 0.036454 0.195572
σ = 7.25
UBCIEstimator 0.937219 0.012781 0.56014 0.029253 0.033528 0.0681
PBCIEstimator 0.937219 0.012781 0.456249 0.029253 0.033528 0.0681
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Table A.5
n = 51, k*=0.984912
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.937669 0.012331 0.512111 0.024077 0.038254 0.227437
PBCIEstimator 0.937669 0.012331 0.439221 0.024077 0.038254 0.227437
σ = 3.750000
UBCIEstimator 0.949595 0.000405 0.511922 0.022277 0.028128 0.116071
PBCIEstimator 0.949595 0.000405 0.438955 0.022277 0.028128 0.116071
σ = 4.25
UBCIEstimator 0.942844 0.007156 0.512718 0.020027 0.037129 0.299213
PBCIEstimator 0.942844 0.007156 0.438928 0.020027 0.037129 0.299213
σ = 4.75
UBCIEstimator 0.938569 0.011431 0.511413 0.028803 0.032628 0.062271
PBCIEstimator 0.938569 0.011431 0.438753 0.028803 0.032628 0.062271
σ = 5.25
UBCIEstimator 0.934293 0.015707 0.513681 0.024077 0.041629 0.267123
PBCIEstimator 0.934293 0.015707 0.439384 0.024077 0.041629 0.267123
σ = 5.75
UBCIEstimator 0.943969 0.006031 0.512978 0.022952 0.033078 0.180723
PBCIEstimator 0.943969 0.006031 0.439233 0.022952 0.033078 0.180723
σ = 6.25
UBCIEstimator 0.943969 0.006031 0.512852 0.021377 0.034653 0.236948
PBCIEstimator 0.943969 0.006031 0.439163 0.021377 0.034653 0.236948
σ = 6.75
UBCIEstimator 0.94577 0.00423 0.511085 0.024302 0.029928 0.103734
PBCIEstimator 0.94577 0.00423 0.43874 0.024302 0.029928 0.103734
σ = 7.25
UBCIEstimator 0.941719 0.008281 0.511504 0.025878 0.032403 0.111969
PBCIEstimator 0.941719 0.008281 0.438982 0.025878 0.032403 0.111969
15
Table A.6
n = 61, k*=0.987439
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.942844 0.007156 0.475927 0.024527 0.032628 0.141732
PBCIEstimator 0.942844 0.007156 0.419925 0.024527 0.032628 0.141732
σ = 3.750000
UBCIEstimator 0.940369 0.009631 0.476062 0.024077 0.035554 0.192453
PBCIEstimator 0.940369 0.009631 0.420332 0.024077 0.035554 0.192453
σ = 4.25
UBCIEstimator 0.94532 0.00468 0.475442 0.025878 0.028803 0.053498
PBCIEstimator 0.94532 0.00468 0.419655 0.025878 0.028803 0.053498
σ = 4.75
UBCIEstimator 0.944644 0.005356 0.475901 0.021152 0.034203 0.235772
PBCIEstimator 0.944644 0.005356 0.419931 0.021152 0.034203 0.235772
σ = 5.25
UBCIEstimator 0.943744 0.006256 0.475624 0.023402 0.032853 0.168
PBCIEstimator 0.943744 0.006256 0.420421 0.023402 0.032853 0.168
σ = 5.75
UBCIEstimator 0.938119 0.011881 0.474645 0.028128 0.033753 0.090909
PBCIEstimator 0.938119 0.011881 0.419939 0.028128 0.033753 0.090909
σ = 6.25
UBCIEstimator 0.942394 0.007606 0.475762 0.023402 0.034203 0.1875
PBCIEstimator 0.942394 0.007606 0.419811 0.023402 0.034203 0.1875
σ = 6.75
UBCIEstimator 0.937669 0.012331 0.475538 0.026553 0.035779 0.148014
PBCIEstimator 0.937669 0.012331 0.420101 0.026553 0.035779 0.148014
σ = 7.25
UBCIEstimator 0.937669 0.012331 0.475136 0.025878 0.036454 0.169675
PBCIEstimator 0.937669 0.012331 0.420178 0.025878 0.036454 0.169675
16
Table A.7
n = 71, k*=0.989241
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.939469 0.010531 0.445152 0.022502 0.038029 0.256506
PBCIEstimator 0.939469 0.010531 0.401157 0.022502 0.038029 0.256506
σ = 3.750000
UBCIEstimator 0.94712 0.00288 0.444846 0.022502 0.030378 0.148936
PBCIEstimator 0.94712 0.00288 0.401085 0.022502 0.030378 0.148936
σ = 4.25
UBCIEstimator 0.942169 0.007831 0.445246 0.024527 0.033303 0.151751
PBCIEstimator 0.942169 0.007831 0.401377 0.024527 0.033303 0.151751
σ = 4.75
UBCIEstimator 0.943069 0.006931 0.444511 0.027903 0.029028 0.019763
PBCIEstimator 0.943069 0.006931 0.401178 0.027903 0.029028 0.019763
σ = 5.25
UBCIEstimator 0.945095 0.004905 0.444467 0.024302 0.030603 0.114754
PBCIEstimator 0.945095 0.004905 0.40127 0.024302 0.030603 0.114754
σ = 5.75
UBCIEstimator 0.943969 0.006031 0.444334 0.021827 0.034203 0.220884
PBCIEstimator 0.943969 0.006031 0.400812 0.021827 0.034203 0.220884
σ = 6.25
UBCIEstimator 0.942844 0.007156 0.444299 0.025653 0.031503 0.102362
PBCIEstimator 0.942844 0.007156 0.401083 0.025653 0.031503 0.102362
σ = 6.75
UBCIEstimator 0.944644 0.005356 0.444934 0.024077 0.031278 0.130081
PBCIEstimator 0.944644 0.005356 0.401544 0.024077 0.031278 0.130081
σ = 7.25
UBCIEstimator 0.939019 0.010981 0.443682 0.026328 0.034653 0.136531
PBCIEstimator 0.939019 0.010981 0.400823 0.026328 0.034653 0.136531
17
Table A.8
n = 85, k*=0.991040
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.948245 0.001755 0.410266 0.023177 0.028578 0.104348
PBCIEstimator 0.948245 0.001755 0.377535 0.023177 0.028578 0.104348
σ = 3.750000
UBCIEstimator 0.95027 0.00027 0.40935 0.020477 0.029253 0.176471
PBCIEstimator 0.95027 0.00027 0.376814 0.020477 0.029253 0.176471
σ = 4.25
UBCIEstimator 0.952295 0.002295 0.410413 0.020477 0.027228 0.141509
PBCIEstimator 0.952295 0.002295 0.377576 0.020477 0.027228 0.141509
σ = 4.75
UBCIEstimator 0.943519 0.006481 0.410511 0.021827 0.034653 0.227092
PBCIEstimator 0.943519 0.006481 0.377481 0.021827 0.034653 0.227092
σ = 5.25
UBCIEstimator 0.946445 0.003555 0.409964 0.026778 0.026778 0
PBCIEstimator 0.946445 0.003555 0.377319 0.026778 0.026778 0
σ = 5.75
UBCIEstimator 0.95162 0.00162 0.410785 0.021377 0.027003 0.116279
PBCIEstimator 0.95162 0.00162 0.377858 0.021377 0.027003 0.116279
σ = 6.25
UBCIEstimator 0.943744 0.006256 0.410274 0.026328 0.029928 0.064
PBCIEstimator 0.943744 0.006256 0.37727 0.026328 0.029928 0.064
σ = 6.75
UBCIEstimator 0.944869 0.005131 0.410498 0.023627 0.031503 0.142857
PBCIEstimator 0.944869 0.005131 0.377696 0.023627 0.031503 0.142857
σ = 7.25
UBCIEstimator 0.946445 0.003555 0.410325 0.025203 0.028353 0.058824
PBCIEstimator 0.946445 0.003555 0.377411 0.025203 0.028353 0.058824
18
Table A.9
n = 101, k*=0.992478
σ = 3.250000
95% CI Estimator for SR Coverage Probability Coverage Error Length Left Bias Right Bias Relative Bias
UBCIEstimator 0.944194 0.005806 0.379228 0.026103 0.029703 0.064516
PBCIEstimator 0.944194 0.005806 0.35415 0.026103 0.029703 0.064516
σ = 3.750000
UBCIEstimator 0.936994 0.013006 0.379392 0.027678 0.035329 0.121429
PBCIEstimator 0.936994 0.013006 0.354069 0.027678 0.035329 0.121429
σ = 4.25
UBCIEstimator 0.939019 0.010981 0.379455 0.024977 0.036004 0.180812
PBCIEstimator 0.939019 0.010981 0.354343 0.024977 0.036004 0.180812
σ = 4.75
UBCIEstimator 0.946895 0.003105 0.379154 0.021827 0.031278 0.177966
PBCIEstimator 0.946895 0.003105 0.35401 0.021827 0.031278 0.177966
σ = 5.25
UBCIEstimator 0.946445 0.003555 0.379266 0.022727 0.030828 0.151261
PBCIEstimator 0.946445 0.003555 0.354091 0.022727 0.030828 0.151261
σ = 5.75
UBCIEstimator 0.94847 0.00153 0.379468 0.024077 0.027453 0.065502
PUBCIEstimator 0.94847 0.00153 0.354477 0.024077 0.027453 0.065502
σ = 6.25
UBCIEstimator 0.943519 0.006481 0.379636 0.024302 0.032178 0.139442
PBCIEstimator 0.943519 0.006481 0.354252 0.024302 0.032178 0.139442
σ = 6.75
UBCIEstimator 0.945095 0.004905 0.379695 0.022277 0.032628 0.188525
PBCIEstimator 0.945095 0.004905 0.354264 0.022277 0.032628 0.188525
σ = 7.25
UBCIEstimator 0.937894 0.012106 0.37939 0.030378 0.031728 0.021739
PBCIEstimator 0.937894 0.012106 0.354378 0.030378 0.031728 0.021739