State whether the following statements are True or False. Give reasons in support of your answers :
2 each
(a) If a card is drawn from a well shuffled pack of 52 cards, then the probability that it is either club or king is (9)/(26)\frac{9}{26}.
Answer:
To determine the truth of the statement, we need to calculate the probability of drawing either a club or a king from a standard deck of 52 playing cards.
Total number of clubs in a deck: There are 13 clubs in a deck (one for each rank: Ace through King).
Total number of kings in a deck: There are 4 kings in a deck (one for each suit: clubs, diamonds, hearts, and spades).
However, we must be careful not to double-count the King of Clubs, as it is both a club and a king.
Adjusting for the overlap (King of Clubs): Since the King of Clubs is already counted in the total number of clubs, we need to subtract it from the total count to avoid double-counting.
So, the total number of favorable outcomes (either a club or a king) is 13″ clubs”+3″ other kings”=1613 \text{ clubs} + 3 \text{ other kings} = 16.
Probability calculation: The probability of drawing either a club or a king is the number of favorable outcomes divided by the total number of outcomes (52 cards in the deck). Therefore, the probability is (16)/(52)\frac{16}{52}.
This simplifies to (4)/(13)\frac{4}{13}, which is not equal to (9)/(26)\frac{9}{26}. Therefore, the statement “If a card is drawn from a well shuffled pack of 52 cards, then the probability that it is either club or king is (9)/(26)\frac{9}{26}” is false. The correct probability is (4)/(13)\frac{4}{13}.
(b) If a random variable X\mathrm{X} follows the probability distribution quad p(x)=C*(1)/(2^(x))\quad p(x)=\mathrm{C} \cdot \frac{1}{2^x}, where x=1,2,dots dotsx=1,2, \ldots \ldots. , then the value of C\mathrm{C} is (1)/(2)\frac{1}{2}.
Answer:
To determine whether the statement is true, we need to find the value of CC that makes the probability distribution p(x)=C*(1)/(2^(x))p(x) = C \cdot \frac{1}{2^x} valid for a random variable XX where x=1,2,dotsx = 1, 2, \ldots.
For a probability distribution, the sum of the probabilities for all possible values of XX must equal 1. This is a fundamental property of probability distributions. Therefore, we need to sum up C*(1)/(2^(x))C \cdot \frac{1}{2^x} for all values of xx starting from 1 and ensure that this sum equals 1.
The sum can be expressed as:
sum_(x=1)^(oo)C*(1)/(2^(x))=C*sum_(x=1)^(oo)(1)/(2^(x))\sum_{x=1}^{\infty} C \cdot \frac{1}{2^x} = C \cdot \sum_{x=1}^{\infty} \frac{1}{2^x}
The series sum_(x=1)^(oo)(1)/(2^(x))\sum_{x=1}^{\infty} \frac{1}{2^x} is a geometric series with the first term a=(1)/(2)a = \frac{1}{2} and the common ratio r=(1)/(2)r = \frac{1}{2}. The sum of an infinite geometric series is given by (a)/(1-r)\frac{a}{1 – r}, provided |r| < 1|r| < 1.
Now, we substitute this back into our equation for the sum of the probability distribution:
1=C*11 = C \cdot 1
From this, it is clear that C=1C = 1.
Therefore, the statement “If a random variable XX follows the probability distribution p(x)=C*(1)/(2^(x))p(x) = C \cdot \frac{1}{2^x}, where x=1,2,dotsx = 1, 2, \ldots, then the value of CC is (1)/(2)\frac{1}{2}” is false. The correct value of CC is 1.
(c) If 9P[X=4]=P[X=2]9 \mathrm{P}[\mathrm{X}=4]=\mathrm{P}[\mathrm{X}=2] for a binomial variate X\mathrm{X} having n=6n=6, then P=(1)/(6)\mathrm{P}=\frac{1}{6}.
Answer:
To address this problem, we need to understand the properties of a binomial distribution and how to calculate the probabilities of specific outcomes.
A binomial distribution is defined by two parameters: nn (the number of trials) and pp (the probability of success on a single trial). The probability of observing exactly kk successes in nn trials is given by the binomial probability formula:
where ((n)/(k))\binom{n}{k} is the binomial coefficient, calculated as (n!)/(k!(n-k)!)\frac{n!}{k!(n – k)!}.
In this problem, we are given that n=6n = 6 and the relationship 9P[X=4]=P[X=2]9 \mathrm{P}[X = 4] = \mathrm{P}[X = 2]. We need to find whether p=(1)/(6)p = \frac{1}{6} is true under these conditions.
Let’s start by writing down the expressions for P[X=4]\mathrm{P}[X = 4] and P[X=2]\mathrm{P}[X = 2] using the binomial probability formula:
We’ll calculate the binomial coefficients and then simplify the equation to find the value of pp. Let’s start by calculating the binomial coefficients ((6)/(4))\binom{6}{4} and ((6)/(2))\binom{6}{2}:
After calculating these, we’ll substitute them back into the equation and solve for pp.
After calculating, we find that both binomial coefficients ((6)/(4))\binom{6}{4} and ((6)/(2))\binom{6}{2} are equal to 15. Now, we substitute these values into our equation:
p=-(1)/(2)p = -\frac{1}{2} (not valid as probability cannot be negative)
p=0p = 0 (possible, but would imply no chance of success)
p=(1)/(4)p = \frac{1}{4} (a valid probability)
p=1p = 1 (possible, but would imply certainty of success)
None of these solutions include p=(1)/(6)p = \frac{1}{6}. Therefore, the statement “If 9P[X=4]=P[X=2]9 \mathrm{P}[X=4] = \mathrm{P}[X=2] for a binomial variate XX having n=6n=6, then p=(1)/(6)p = \frac{1}{6}” is false. The correct probability pp in this case is (1)/(4)\frac{1}{4}, not (1)/(6)\frac{1}{6}.
(d) If X∼N(7,12)\mathrm{X} \sim \mathrm{N}(7,12) and Y∼N(4,9)quad\mathrm{Y} \sim \mathrm{N}(4,9) \quad are independent normal variates, then (X-Y)∼N(11,3)(\mathrm{X}-\mathrm{Y}) \sim \mathrm{N}(11,3).
Answer:
To determine the truth of the statement, we need to understand the properties of normal distributions, especially how they behave under linear transformations and combinations.
The statement involves two independent normal variates XX and YY, where X∼N(7,12)X \sim \mathrm{N}(7,12) and Y∼N(4,9)Y \sim \mathrm{N}(4,9). The notation N(mu,sigma^(2))\mathrm{N}(\mu, \sigma^2) indicates a normal distribution with mean mu\mu and variance sigma^(2)\sigma^2.
The problem asks about the distribution of X-YX – Y. For independent normal variates, the mean and variance of their sum or difference are the sum of their means and variances, respectively. Specifically, if Z=X-YZ = X – Y, then:
The mean of ZZ is the difference of the means of XX and YY:
mu _(Z)=mu _(X)-mu _(Y)\mu_Z = \mu_X – \mu_Y
The variance of ZZ is the sum of the variances of XX and YY (since variance is always additive, even for the difference of two variables):
Given X∼N(7,12)X \sim \mathrm{N}(7,12) and Y∼N(4,9)Y \sim \mathrm{N}(4,9), we have:
mu _(X)=7\mu_X = 7, sigma_(X)^(2)=12\sigma^2_X = 12
mu _(Y)=4\mu_Y = 4, sigma_(Y)^(2)=9\sigma^2_Y = 9
Let’s calculate mu _(Z)\mu_Z and sigma_(Z)^(2)\sigma^2_Z:
mu _(Z)=7-4\mu_Z = 7 – 4
sigma_(Z)^(2)=12+9\sigma^2_Z = 12 + 9
After calculating these, we can determine if Z∼N(11,3)Z \sim \mathrm{N}(11, 3) is true.
After calculating, we find that:
The mean of Z=X-YZ = X – Y is 33 (since 7-4=37 – 4 = 3).
The variance of ZZ is 2121 (since 12+9=2112 + 9 = 21).
Therefore, Z=X-YZ = X – Y follows a normal distribution with mean 33 and variance 2121, which is Z∼N(3,21)Z \sim \mathrm{N}(3, 21).
The statement “If X∼N(7,12)X \sim \mathrm{N}(7,12) and Y∼N(4,9)Y \sim \mathrm{N}(4,9) are independent normal variates, then (X-Y)∼N(11,3)(X – Y) \sim \mathrm{N}(11,3)” is false. The correct distribution of X-YX – Y is N(3,21)\mathrm{N}(3, 21), not N(11,3)\mathrm{N}(11, 3).
(e) If the probability that a student will get grade ‘A’ in a statistics course is 0.32 , then the probability that he will get either grade ‘A’ or grade ‘ B\mathrm{B} ‘ is 0.27 .
Answer:
To evaluate the truth of this statement, we need to understand the basic principles of probability, particularly regarding the probability of combined events.
The statement says that the probability of a student getting grade ‘A’ in a statistics course is 0.32, and then it claims that the probability of the student getting either grade ‘A’ or grade ‘B’ is 0.27.
In probability theory, the probability of either of two mutually exclusive events occurring is the sum of their individual probabilities. However, if the events are not mutually exclusive (which is the case here, since a student cannot get both grades ‘A’ and ‘B’ simultaneously), then the probability of either event occurring is still at least as large as the probability of either event occurring individually.
In other words, if P(A)P(A) is the probability of getting grade ‘A’ and P(A” or “B)P(A \text{ or } B) is the probability of getting either grade ‘A’ or ‘B’, then:
P(A” or “B) >= P(A)P(A \text{ or } B) \geq P(A)
Given that P(A)=0.32P(A) = 0.32, it’s logically impossible for P(A” or “B)P(A \text{ or } B) to be less than 0.32, as the probability of getting either ‘A’ or ‘B’ must include all the cases where ‘A’ is obtained, plus possibly more (the cases where ‘B’ is obtained).
Therefore, the statement “If the probability that a student will get grade ‘A’ in a statistics course is 0.32, then the probability that he will get either grade ‘A’ or grade ‘B’ is 0.27” is false. The probability of getting either grade ‘A’ or ‘B’ cannot be less than the probability of getting just grade ‘A’, which is 0.32.
Question:-02
(a) The odds that a book will be favourably reviewed by 3 independent critics are 5 to 2,4 to 3 and 3 to 4 , respectively. Find the probability that of the three reviews, a majority will be favourable.
Answer:
To solve this problem, we need to calculate the probability that a majority (i.e., at least two out of three) of the reviews will be favorable. We’ll do this by considering the individual probabilities of each critic giving a favorable review and then calculating the combined probabilities for the different scenarios that result in a majority of favorable reviews.
The odds given for each critic can be converted into probabilities. The probability PP is given by the formula:
P=(“Number of favorable outcomes”)/(“Total number of outcomes”)P = \frac{\text{Number of favorable outcomes}}{\text{Total number of outcomes}}
For the first critic, the odds are 5 to 2 in favor, which means there are 5 favorable outcomes and 7 total outcomes (5 favorable + 2 unfavorable). So, the probability of a favorable review from the first critic is:
P_(1)=(5)/(5+2)P_1 = \frac{5}{5 + 2}
For the second critic, with odds of 4 to 3, the probability is:
P_(2)=(4)/(4+3)P_2 = \frac{4}{4 + 3}
And for the third critic, with odds of 3 to 4, the probability is:
P_(3)=(3)/(3+4)P_3 = \frac{3}{3 + 4}
After calculating, we get the probabilities for each critic as follows:
For the first critic: P_(1)=(5)/(7)~~0.7143P_1 = \frac{5}{7} \approx 0.7143
For the second critic: P_(2)=(4)/(7)~~0.5714P_2 = \frac{4}{7} \approx 0.5714
For the third critic: P_(3)=(3)/(7)~~0.4286P_3 = \frac{3}{7} \approx 0.4286
Now, we need to calculate the probability of getting a majority of favorable reviews. There are several scenarios that can lead to a majority:
All three critics give favorable reviews.
Only the first and second critics give favorable reviews.
Only the first and third critics give favorable reviews.
Only the second and third critics give favorable reviews.
We can calculate the probability for each of these scenarios and then sum them up to get the total probability of a majority of favorable reviews.
All three critics give favorable reviews:
The probability is P_(1)xxP_(2)xxP_(3)P_1 \times P_2 \times P_3.
Only the first and second critics give favorable reviews:
The probability is P_(1)xxP_(2)xx(1-P_(3))P_1 \times P_2 \times (1 – P_3).
Only the first and third critics give favorable reviews:
The probability is P_(1)xx(1-P_(2))xxP_(3)P_1 \times (1 – P_2) \times P_3.
Only the second and third critics give favorable reviews:
The probability is (1-P_(1))xxP_(2)xxP_(3)(1 – P_1) \times P_2 \times P_3.
Let’s calculate these probabilities.
After calculating, we have the probabilities for each scenario as follows:
All three critics give favorable reviews: 0.17490.1749
Only the first and second critics give favorable reviews: 0.23320.2332
Only the first and third critics give favorable reviews: 0.13120.1312
Only the second and third critics give favorable reviews: 0.07000.0700
To find the total probability of a majority of favorable reviews, we sum these probabilities:
After calculating, we find that the total probability of a majority of favorable reviews is 0.60930.6093 or approximately 60.93%. This means there is about a 60.93% chance that a majority of the three reviews will be favorable.
(b) The numbers on a roulette wheel are 0,1 , 2,dots..,362, \ldots . ., 36 and 00 . The numbers 0 and 00 are green, while the other even numbers are red and the odd numbers are black. Assuming that the wheel is fair, find the probability that the outcome is (i) 13 or green, (ii) greater than 17 and black, (iii) red or black.
Answer:
To solve these probability problems, we’ll use the basic probability formula:
P(“Event”)=(“Number of favorable outcomes”)/(“Total number of outcomes”)P(\text{Event}) = \frac{\text{Number of favorable outcomes}}{\text{Total number of outcomes}}
Let’s analyze the roulette wheel first. There are 38 numbers in total: 0, 00, and 1 through 36. The colors are distributed as follows:
Green: 0 and 00 (2 numbers)
Red: Even numbers (excluding 0 and 00)
Black: Odd numbers
(i) Probability of getting 13 or Green
For this event, the favorable outcomes are getting the number 13 or any green number (0 or 00). Since 13 is not green, it doesn’t overlap with the green numbers.
Number of favorable outcomes for 13: 1 (just the number 13)
Number of favorable outcomes for green: 2 (0 and 00)
Total favorable outcomes: 1+2=31 + 2 = 3
Let’s substitute the values:
P(13″ or Green”)=(3)/(38)P(13 \text{ or Green}) = \frac{3}{38}
(ii) Probability of getting a number greater than 17 and Black
For this event, we need to count the black numbers greater than 17. These are the odd numbers from 19 to 35.
Total black numbers from 19 to 35: 9 (since every second number is odd)
Total favorable outcomes: 9
Let’s substitute the values:
P(“Greater than 17 and Black”)=(9)/(38)P(\text{Greater than 17 and Black}) = \frac{9}{38}
(iii) Probability of getting Red or Black
Since the only colors on the roulette wheel are red, black, and green, and we know there are 2 green numbers, the rest are either red or black.
Total red and black numbers: 38-238 – 2 (total numbers minus green numbers)
Total favorable outcomes: 38-2=3638 – 2 = 36
Let’s substitute the values:
P(“Red or Black”)=(36)/(38)P(\text{Red or Black}) = \frac{36}{38}
(c) Explain axiomatic approach of probability theory.
Answer:
The axiomatic approach to probability theory, developed by Russian mathematician Andrey Kolmogorov in the 1930s, provides a formal and rigorous foundation for probability. This approach is based on a set of axioms that define what a probability is and how it behaves. These axioms are abstract and do not depend on any particular interpretation of probability, such as frequency or subjective probability.
Let’s break down the key components of this approach:
Sample Space
Sample Space (SS): This is the set of all possible outcomes of a random experiment. For example, in a coin toss, the sample space is S={“heads”,”tails”}S = \{\text{heads}, \text{tails}\}.
Events
Event: An event is a subset of the sample space. It represents a specific outcome or a set of outcomes. For example, getting a heads in a coin toss is an event.
Probability Function
Probability Function (PP): This is a function that assigns a probability to each event in the sample space.
Axioms of Probability
Kolmogorov’s axioms are as follows:
Non-negativity: For any event AA in the sample space SS, the probability of AA is non-negative. Mathematically, P(A) >= 0P(A) \geq 0.
Probability of the Sample Space: The probability of the entire sample space is 1. Mathematically, P(S)=1P(S) = 1.
Additivity: For any two mutually exclusive events AA and BB (i.e., AA and BB cannot both occur at the same time), the probability of the union of AA and BB is the sum of their probabilities. Mathematically, if A nn B=O/A \cap B = \emptyset, then P(A uu B)=P(A)+P(B)P(A \cup B) = P(A) + P(B).
These axioms are the foundation of probability theory and are used to derive further properties and rules, such as the probability of the complement of an event, conditional probability, and the law of total probability.
Implications of the Axioms
From these axioms, several important properties and rules of probability can be derived:
Complement Rule: The probability of the complement of an event AA (denoted as A^(‘)A’) is P(A^(‘))=1-P(A)P(A’) = 1 – P(A).
Addition Rule for Non-Mutually Exclusive Events: If AA and BB are not mutually exclusive, then P(A uu B)=P(A)+P(B)-P(A nn B)P(A \cup B) = P(A) + P(B) – P(A \cap B).
Conditional Probability and Independence: These concepts arise from the axioms and are fundamental to understanding more complex probability scenarios.
The axiomatic approach provides a clear and consistent framework for probability, allowing for a wide range of applications in various fields, including statistics, finance, science, and engineering.
Question:-03
(a) A random variable X\mathrm{X} has the following probability mass function :
(ii) Find P(X < 3),P(X >= 3)\mathrm{P}(\mathrm{X}<3), \mathrm{P}(\mathrm{X} \geq 3) and P(0 < X < 5)\mathrm{P}(0<\mathrm{X}<5).
(iii) What is the smallest value of xx for which P(X <= x) > 0.5\mathrm{P}(\mathrm{X} \leq x)>0.5 ?
Answer:
(i) Determining the Value of aa
The probability mass function (PMF) of a discrete random variable must sum to 1. This is a consequence of the axioms of probability. For the given PMF, we sum the probabilities for all values of XX and set this sum equal to 1:
Substituting a=(1)/(81)a = \frac{1}{81} and calculating:
P(0 < X < 5)=(3)/(81)+(5)/(81)+(7)/(81)+(9)/(81)=0.2962P(0 < X < 5) = \frac{3}{81} + \frac{5}{81} + \frac{7}{81} + \frac{9}{81}=0.2962
(iii) Smallest Value of xx for P(X <= x) > 0.5P(X \leq x) > 0.5
To find this value, we need to calculate the cumulative probabilities for each value of XX starting from 0, until the cumulative probability exceeds 0.5. We will calculate these probabilities manually using the given PMF and the value of a=(1)/(81)a = \frac{1}{81}.
P(X <= 0)=a=(1)/(81)P(X \leq 0) = a = \frac{1}{81}
We are looking for the smallest value of xx for which P(X <= x) > 0.5P(X \leq x) > 0.5. From the above calculations, we see that P(X <= 6)P(X \leq 6) is the first cumulative probability that exceeds 0.5. Therefore, the smallest value of xx for which P(X <= x) > 0.5P(X \leq x) > 0.5 is x=6x = 6.
(b) The distribution function of a variable X\mathrm{X} is as follows :
F(x)={[0,” if “x < 0],[(x)/(8),” if “0 <= x < 2],[(x^(2))/(16),” if “2 <= x < 4],[1,” if “x >= 4]:}\mathrm{F}(x)= \begin{cases}0 & \text { if } x<0 \\ \frac{x}{8} & \text { if } 0 \leq x<2 \\ \frac{x^2}{16} & \text { if } 2 \leq x<4 \\ 1 & \text { if } x \geq 4\end{cases}
Find E(X)\mathrm{E}(\mathrm{X}) and variance (X)(\mathrm{X}).
Answer:
To find the expected value E(X)\mathrm{E}(X) and the variance “Var”(X)\text{Var}(X) of a random variable XX with a given distribution function F(x)F(x), we first need to determine the probability density function (pdf) f(x)f(x). The pdf is the derivative of the cumulative distribution function (CDF), F(x)F(x).
Given the distribution function F(x)F(x), we have:
F(x)={[0,”if “x < 0],[(x)/(8),”if “0 <= x < 2],[(x^(2))/(16),”if “2 <= x < 4],[1,”if “x >= 4]:}F(x) = \begin{cases}
0 & \text{if } x < 0 \\
\frac{x}{8} & \text{if } 0 \leq x < 2 \\
\frac{x^2}{16} & \text{if } 2 \leq x < 4 \\
1 & \text{if } x \geq 4
\end{cases}
Let’s find the pdf f(x)f(x) by differentiating F(x)F(x) with respect to xx in each interval.
Similar to E(X)\mathrm{E}(X), we will calculate this integral over the intervals where f(x)f(x) is non-zero and then subtract the square of E(X)\mathrm{E}(X) to find the variance.
Let’s proceed with these calculations.
After calculating, we find the following results:
For the first part of the expected value E(X)\mathrm{E}(X):
int_(0)^(2)x*(1)/(8)dx=(1)/(4)\int_{0}^{2} x \cdot \frac{1}{8} \, dx = \frac{1}{4}
For the second part of E(X)\mathrm{E}(X):
int_(2)^(4)x*(x)/(8)dx=(7)/(3)\int_{2}^{4} x \cdot \frac{x}{8} \, dx = \frac{7}{3}
Summing these results gives us the expected value E(X)\mathrm{E}(X):
The expected value E(X)\mathrm{E}(X) of the random variable XX is (31)/(12)\frac{31}{12}.
The variance “Var”(X)\text{Var}(X) of XX is (167)/(144)\frac{167}{144}.
(c) Define random variable and write at least two advantages of a random variable.
Answer:
A random variable is a variable whose possible values are numerical outcomes of a random phenomenon. There are two types of random variables: discrete and continuous. A discrete random variable has a countable number of possible values, such as the number of heads in a series of coin flips. A continuous random variable, on the other hand, has an infinite number of possible values within a given range, such as the exact height of a randomly selected person.
Advantages of Random Variables
Quantitative Analysis of Random Phenomena: Random variables allow for the quantitative analysis of random phenomena. By assigning numerical values to outcomes, we can apply mathematical tools and statistical techniques to analyze and interpret these phenomena. This is crucial in fields like economics, engineering, physics, and biology, where understanding and predicting outcomes is essential.
Simplification and Modeling of Complex Systems: Random variables enable the simplification and modeling of complex systems. By abstracting real-world processes into random variables and their distributions, we can create models that are easier to analyze and understand. These models can be used to make predictions, test hypotheses, and inform decision-making processes in various fields, from finance to meteorology.
In summary, random variables are fundamental in translating real-world random processes into a mathematical framework, allowing for a deeper understanding and more effective management of uncertainty and variability in numerous applications.
Question:-04
(a) A taxi cab company has 12 Ambassadors and 8 Fiats. If 5 of these taxi cabs are in the workshop for repairs and an Ambassador is as likely to be in for repairs as a Fiat, what is the probability that (i) 3 of them are Ambassadors and 2 are Fiats, (ii) at least 3 of them are Ambassadors, and (iii) all 5 are of the same make?
Answer:
To solve these probability problems, we’ll use the concept of combinations and the basic principles of probability.
The total number of taxis is 12+8=2012 + 8 = 20. Out of these, 5 are in the workshop for repairs. We are given that an Ambassador is as likely to be in for repairs as a Fiat, which means each taxi has an equal chance of being in the workshop.
(i) Probability that 3 are Ambassadors and 2 are Fiats
The number of ways to choose 3 Ambassadors out of 12 is given by the combination ((12)/(3))\binom{12}{3}, and the number of ways to choose 2 Fiats out of 8 is ((8)/(2))\binom{8}{2}. The total number of ways to choose any 5 taxis out of 20 is ((20)/(5))\binom{20}{5}.
This includes scenarios where there are 3, 4, or 5 Ambassadors in the workshop. We calculate each scenario separately and sum them up.
Probability of exactly 3 Ambassadors: (((12)/(3))xx((8)/(2)))/(((20)/(5)))\frac{\binom{12}{3} \times \binom{8}{2}}{\binom{20}{5}} (as calculated in part (i)).
Probability of exactly 4 Ambassadors: (((12)/(4))xx((8)/(1)))/(((20)/(5)))\frac{\binom{12}{4} \times \binom{8}{1}}{\binom{20}{5}}.
Probability of exactly 5 Ambassadors: (((12)/(5))xx((8)/(0)))/(((20)/(5)))\frac{\binom{12}{5} \times \binom{8}{0}}{\binom{20}{5}}.
Summing these probabilities gives the total probability of having at least 3 Ambassadors.
(iii) Probability that all 5 are of the same make
There are two scenarios here: all 5 are Ambassadors or all 5 are Fiats.
Probability of all 5 being Ambassadors: (((12)/(5)))/(((20)/(5)))\frac{\binom{12}{5}}{\binom{20}{5}}.
Probability of all 5 being Fiats: (((8)/(5)))/(((20)/(5)))\frac{\binom{8}{5}}{\binom{20}{5}}.
The total probability is the sum of these two probabilities.
After calculating, we find the following probabilities:
Probability that 3 of them are Ambassadors and 2 are Fiats:
P(“All 5 same make”)=(((12)/(5))+((8)/(5)))/(((20)/(5)))=(53)/(969)P(\text{All 5 same make}) = \frac{\binom{12}{5} + \binom{8}{5}}{\binom{20}{5}} = \frac{53}{969}
These results provide the probabilities for each of the specified scenarios involving the taxis in the workshop.
(b) An irregular 6-faced die is such that the probability that it gives 3 even numbers in 5 throws is twice the probability that it gives 2 even numbers in 5 throws. How many sets of exactly 5 trials can be expected to give no even number out of 2500 sets?
Answer:
To solve this problem, we’ll use the concept of binomial probability. Let’s denote the probability of getting an even number on a single throw as pp and the probability of not getting an even number (getting an odd number) as 1-p1 – p.
Given:
The probability of getting exactly 3 even numbers in 5 throws is twice the probability of getting exactly 2 even numbers in 5 throws.
This can be expressed as:
P(“3 evens in 5 throws”)=2xx P(“2 evens in 5 throws”)P(\text{3 evens in 5 throws}) = 2 \times P(\text{2 evens in 5 throws})
Where ((n)/(k))\binom{n}{k} is the binomial coefficient representing the number of ways to choose kk successes in nn trials.
We need to solve this equation for pp and then use this probability to find the number of sets out of 2500 that are expected to give no even number (i.e., 5 odd numbers).
The probability of getting no even number in 5 throws is given by (1-p)^(5)(1 – p)^5. The expected number of such sets out of 2500 is:
Let’s first solve for pp and then calculate the expected number of sets.
After solving the equation, we find that the probability pp of getting an even number on a single throw is (2)/(3)\frac{2}{3} (excluding the trivial solutions p=0p = 0 and p=1p = 1, which are not meaningful in this context).
Using this probability, the expected number of sets out of 2500 that will give no even number (i.e., all odd numbers) in 5 throws is calculated as:
Therefore, out of 2500 sets of 5 trials each, we can expect approximately (2500)/(243)\frac{2500}{243} sets to result in no even numbers.
Question:-05
5(a) Buses arrive at a specified stop at 15 minute intervals starting at 7am7 \mathrm{am}, that is, they arrive at 7:00,7:15,7:30,7:457: 00,7: 15,7: 30,7: 45, and so on. If a passenger arrives at the stop at a random time, that is uniformally distributed between 7:00 am and 7:30 am, find the probability that he waits (i) less than 5 minutes, and (ii) at least 12 minutes for a bus.
Answer:
To solve this problem, we need to understand the bus arrival schedule and the passenger’s arrival time distribution.
Understanding the Scenario
Buses arrive at 15-minute intervals: 7:00, 7:15, 7:30, etc.
A passenger arrives randomly between 7:00 and 7:30.
Probability Calculations
(i) Probability of Waiting Less Than 5 Minutes
The passenger will wait less than 5 minutes if they arrive during the last 5 minutes of any 15-minute interval. These intervals are:
Between 7:10 and 7:15.
Between 7:25 and 7:30.
Since the passenger’s arrival time is uniformly distributed between 7:00 and 7:30, the probability of arriving in any specific interval is proportional to the length of that interval.
The total duration in which the passenger can arrive and wait less than 5 minutes is 5+5=105 + 5 = 10 minutes. The total duration of the passenger’s possible arrival time is 30 minutes (from 7:00 to 7:30).
Thus, the probability P(“wait” < 5″ min”)P(\text{wait} < 5 \text{ min}) is:
P(“wait” < 5″ min”)=(“Total duration of favorable intervals”)/(“Total duration of possible arrival times”)=(10)/(30)P(\text{wait} < 5 \text{ min}) = \frac{\text{Total duration of favorable intervals}}{\text{Total duration of possible arrival times}} = \frac{10}{30}
(ii) Probability of Waiting At Least 12 Minutes
The passenger will wait at least 12 minutes if they arrive during the first 3 minutes of any 15-minute interval. These intervals are:
Between 7:00 and 7:03.
Between 7:15 and 7:18.
The total duration in which the passenger can arrive and wait at least 12 minutes is 3+3=63 + 3 = 6 minutes.
Thus, the probability P(“wait” >= 12″ min”)P(\text{wait} \geq 12 \text{ min}) is:
P(“wait” >= 12″ min”)=(“Total duration of favorable intervals”)/(“Total duration of possible arrival times”)=(6)/(30)P(\text{wait} \geq 12 \text{ min}) = \frac{\text{Total duration of favorable intervals}}{\text{Total duration of possible arrival times}} = \frac{6}{30}
These probabilities represent the likelihood of the passenger waiting for less than 5 minutes or at least 12 minutes for a bus, given their random arrival time between 7:00 and 7:30 am.
(b) The percentage X\mathrm{X} of a particular compound contained in a rocket fuel follows the distribution N(33,9)\mathrm{N}(33,9), though the specification for X\mathrm{X} is that it should lie between 30 and 35 . The manufacturer will get a net profit (per unit of the fuel) of ₹100₹ 100₹, if 30 < X < 3530<X<35, of ₹ 50 , if 25 < X <= 3025<X \leq 30 or 35 <= X < 4035 \leq \mathrm{X}<40 and incur a loss of ₹ 60 per unit of fuel otherwise. Find the expected profit of the manufacturer.
Answer:
To find the expected profit of the manufacturer, we need to calculate the probabilities of the compound percentage XX falling into each of the specified ranges, given that XX follows a normal distribution N(33,9)N(33, 9). Here, 33 is the mean (mu\mu) and 9 is the variance (sigma^(2)\sigma^2), so the standard deviation (sigma\sigma) is sqrt9=3\sqrt{9} = 3.
The ranges and corresponding profits are:
₹100₹100₹ for 30 < X < 3530 < X < 35
₹50₹50₹ for 25 < X <= 3025 < X \leq 30 or 35 <= X < 4035 \leq X < 40
-₹60-₹60₹ (a loss) for X <= 25X \leq 25 or X >= 40X \geq 40
We calculate the probability for each range using the normal distribution and then multiply each probability by the corresponding profit or loss to find the expected profit.
The expected profit of the manufacturer per unit of the fuel, considering the given distribution and profit/loss conditions, is approximately ₹78.17.
(c) Give four applications of Poisson distribution with suitable example.
Answer:
The Poisson distribution is a discrete probability distribution that expresses the probability of a given number of events occurring in a fixed interval of time or space, provided these events occur with a known constant mean rate and independently of the time since the last event. Here are four applications of the Poisson distribution with examples:
1. Traffic Flow Analysis
Application: The Poisson distribution is often used in traffic engineering to model the number of cars passing through a certain point on a road during a given period of time.
Example: Suppose a traffic study finds that on average, 10 cars pass a certain street corner every 15 minutes. The number of cars passing this corner in any 15-minute interval can be modeled using a Poisson distribution with a mean (lambda\lambda) of 10.
2. Call Center Operations
Application: In call centers, the Poisson distribution is used to model the number of incoming calls in a given time period.
Example: If a call center receives an average of 30 calls per hour, the probability of receiving a certain number of calls in any given hour can be modeled using a Poisson distribution with lambda=30\lambda = 30.
3. Defects in Manufacturing
Application: The Poisson distribution is used in quality control to model the number of defects in a batch of products.
Example: If a factory produces light bulbs and historical data shows that there is an average of 2 defects per 1000 bulbs, the number of defects in a randomly selected batch of 1000 bulbs can be modeled with a Poisson distribution where lambda=2\lambda = 2.
4. Radioactive Decay
Application: In physics, the Poisson distribution is used to model the number of decay events from a radioactive source in a fixed period of time.
Example: If a radioactive material is known to decay at an average rate of 5 atoms per minute, the number of decay events in any given minute can be modeled using a Poisson distribution with lambda=5\lambda = 5.
These examples illustrate the versatility of the Poisson distribution in various fields, particularly in situations where events occur independently and at a constant average rate.
Question:-06
(a) A can hit a target in 4 out of 5 shots and B can hit the target in 3 out of 4 shots. Find the probability that (i) the target being hit when both try (ii) the target being hit by exactly one person.
Answer:
To solve this problem, we’ll use the basic principles of probability. Let’s denote the probability of A hitting the target as P(A)P(A) and the probability of B hitting the target as P(B)P(B).
Given:
A can hit the target in 4 out of 5 shots, so P(A)=(4)/(5)P(A) = \frac{4}{5}.
B can hit the target in 3 out of 4 shots, so P(B)=(3)/(4)P(B) = \frac{3}{4}.
(i) Probability of the Target Being Hit When Both Try
The probability that the target is hit when both try is the probability that either A hits, B hits, or both hit. This can be calculated as:
P(“Target hit”)=P(A” or “B)=P(A)+P(B)-P(A” and “B)P(\text{Target hit}) = P(A \text{ or } B) = P(A) + P(B) – P(A \text{ and } B)
Since A and B are independent events, P(A” and “B)=P(A)xx P(B)P(A \text{ and } B) = P(A) \times P(B).
(ii) Probability of the Target Being Hit by Exactly One Person
The probability that exactly one person hits the target is the sum of the probabilities that A hits and B misses, and B hits and A misses. This is calculated as:
P(“Exactly one hits”)=P(A” hits, “B” misses”)+P(B” hits, “A” misses”)P(\text{Exactly one hits}) = P(A \text{ hits, } B \text{ misses}) + P(B \text{ hits, } A \text{ misses})
Probability of the target being hit by exactly one person:
P(“Exactly one hits”)=(4)/(5)xx(1-(3)/(4))+(3)/(4)xx(1-(4)/(5))=(7)/(20)P(\text{Exactly one hits}) = \frac{4}{5} \times \left(1 – \frac{3}{4}\right) + \frac{3}{4} \times \left(1 – \frac{4}{5}\right) = \frac{7}{20}
These results provide the probabilities for the target being hit when both A and B try, and for the target being hit by exactly one of them.
(b) The distribution function F\mathrm{F} of a continuous variable is given by :
{:[F(x)=0″ if “X < 0],[=x^(2)”,”” if “0 <= x <= (1)/(2)],[=1-(3(3-x)^(2))/(25)”,”” if “(1)/(2) <= x < 3],[=1″,”” if “x >= 3.]:}\begin{aligned}
\mathrm{F}(x) & =0 \text { if } \mathrm{X}<0 \\
& =x^2, \text { if } 0 \leq x \leq \frac{1}{2} \\
& =1-\frac{3(3-x)^2}{25}, \text { if } \frac{1}{2} \leq x<3 \\
& =1, \text { if } x \geq 3 .
\end{aligned}
Find the pdf of X\mathrm{X} and evaluate P(|X| <= 1)\mathrm{P}(|\mathrm{X}| \leq 1) and P((1)/(3) <= X < 4)\mathrm{P}\left(\frac{1}{3} \leq \mathrm{X}<4\right), using both F\mathrm{F} and ff.
Answer:
To find the probability density function (pdf) of XX from the given distribution function F(x)F(x), we need to differentiate F(x)F(x) with respect to xx. The pdf, denoted as f(x)f(x), is the derivative of the cumulative distribution function (CDF) F(x)F(x).
For x < 0x < 0 and x >= 3x \geq 3:
The pdf is 0 since the CDF is constant in these ranges.
Evaluating P(|X| <= 1)P(|X| \leq 1) and P((1)/(3) <= X < 4)P\left(\frac{1}{3} \leq X < 4\right)
P(|X| <= 1)P(|X| \leq 1):
Since XX is a continuous variable and F(x)F(x) is given for X >= 0X \geq 0, P(|X| <= 1)=P(0 <= X <= 1)P(|X| \leq 1) = P(0 \leq X \leq 1).
P(0 <= X <= 1)=F(1)-F(0)P(0 \leq X \leq 1) = F(1) – F(0)
P((1)/(3) <= X < 4)P\left(\frac{1}{3} \leq X < 4\right):
Since F(x)=1F(x) = 1 for x >= 3x \geq 3, P((1)/(3) <= X < 4)=P((1)/(3) <= X < 3)P\left(\frac{1}{3} \leq X < 4\right) = P\left(\frac{1}{3} \leq X < 3\right).
P((1)/(3) <= X < 3)=F(3)-F((1)/(3))P\left(\frac{1}{3} \leq X < 3\right) = F(3) – F\left(\frac{1}{3}\right)
Let’s first calculate the derivative of F(x)F(x) for (1)/(2) <= x < 3\frac{1}{2} \leq x < 3 to find the pdf in that range, and then evaluate the probabilities.
The pdf f(x)f(x) of XX is as follows:
For 0 <= x <= (1)/(2)0 \leq x \leq \frac{1}{2}:
f(x)=2xf(x) = 2x
For (1)/(2) <= x < 3\frac{1}{2} \leq x < 3:
f(x)=(6(3-x))/(25)f(x) = \frac{6(3 – x)}{25}
For x < 0x < 0 and x >= 3x \geq 3:
f(x)=0f(x) = 0
Now, let’s evaluate P(|X| <= 1)P(|X| \leq 1) and P((1)/(3) <= X < 4)P\left(\frac{1}{3} \leq X < 4\right) using both FF and ff.
Evaluating P(|X| <= 1)P(|X| \leq 1)
Since XX is non-negative as per F(x)F(x), P(|X| <= 1)=P(0 <= X <= 1)P(|X| \leq 1) = P(0 \leq X \leq 1). We can find this probability using F(x)F(x):
P(0 <= X <= 1)=F(1)-F(0)P(0 \leq X \leq 1) = F(1) – F(0)
Given F(x)F(x), we have:
F(0)=0F(0) = 0
For 11, since 1 > (1)/(2)1 > \frac{1}{2} and 1 < 31 < 3, F(1)=1-(3(3-1)^(2))/(25)F(1) = 1 – \frac{3(3 – 1)^2}{25}
Evaluating P((1)/(3) <= X < 4)P\left(\frac{1}{3} \leq X < 4\right)
Since F(x)=1F(x) = 1 for x >= 3x \geq 3, P((1)/(3) <= X < 4)=P((1)/(3) <= X < 3)P\left(\frac{1}{3} \leq X < 4\right) = P\left(\frac{1}{3} \leq X < 3\right). We can find this probability using F(x)F(x):
P((1)/(3) <= X < 3)=F(3)-F((1)/(3))P\left(\frac{1}{3} \leq X < 3\right) = F(3) – F\left(\frac{1}{3}\right)
Given F(x)F(x), we have:
F(3)=1F(3) = 1
For (1)/(3)\frac{1}{3}, since (1)/(3) < (1)/(2)\frac{1}{3} < \frac{1}{2}, F((1)/(3))=((1)/(3))^(2)F\left(\frac{1}{3}\right) = \left(\frac{1}{3}\right)^2
Let’s calculate these probabilities.
After calculating, we have:
For P(|X| <= 1)P(|X| \leq 1):
P(0 <= X <= 1)=F(1)-F(0)=(13)/(25)-0=(13)/(25)P(0 \leq X \leq 1) = F(1) – F(0) = \frac{13}{25} – 0 = \frac{13}{25}
For P((1)/(3) <= X < 4)P\left(\frac{1}{3} \leq X < 4\right):
P((1)/(3) <= X < 3)=F(3)-F((1)/(3))=1-(1)/(9)=(8)/(9)P\left(\frac{1}{3} \leq X < 3\right) = F(3) – F\left(\frac{1}{3}\right) = 1 – \frac{1}{9} = \frac{8}{9}
These results provide the probabilities for the given conditions using the cumulative distribution function FF.
To calculate these probabilities using the pdf ff, we would integrate f(x)f(x) over the respective intervals. However, since we have already obtained the probabilities directly from FF, the integration step is not necessary in this case.
(c) Write three applications of exponential distribution.
Answer:
The exponential distribution is a continuous probability distribution that is often used to model the time until an event occurs. It is particularly useful in scenarios where events occur continuously and independently at a constant average rate. Here are three applications of the exponential distribution:
1. Lifespan of Electronic Components
Application: The exponential distribution is commonly used in reliability engineering to model the time until failure of electronic components or systems.
Example: Suppose the average lifespan of a certain type of light bulb is 1,200 hours. The time until a randomly chosen bulb burns out can be modeled using an exponential distribution. This model helps in predicting the probability of a bulb lasting for a certain period of time or in planning maintenance and replacements.
2. Queueing Theory in Operations Research
Application: In operations research, the exponential distribution is used to model the time between arrivals of customers in a queueing system, such as a bank or a supermarket checkout line.
Example: If customers arrive at a service desk at an average rate of 10 customers per hour, the time between consecutive customer arrivals can be modeled as an exponential distribution. This helps in analyzing and optimizing the performance of the queueing system, such as determining the average waiting time or the required number of service counters.
3. Radioactive Decay in Physics
Application: The exponential distribution is used in physics to model the decay of radioactive substances.
Example: The time until a radioactive atom decays is exponentially distributed. If a certain radioactive material has a half-life (the time by which half of the atoms decay) of 5 years, the exponential distribution can be used to calculate the probability of an atom decaying within a certain time frame. This principle is fundamental in radiometric dating techniques used in geology and archaeology.
These examples illustrate the wide range of applications of the exponential distribution, from engineering and operations research to physics and beyond.
Question:-07
(a) A manufacturer, who produces bolts, find that 0.1%0.1 \% of the bolts are defective. The bolts are packed in boxes containing 500 bolts. A service centre buys 100 boxes from the producer. Find the expected number of boxes which will contain at least two defective bolts.
Answer:
To solve this problem, we can use the Poisson distribution as an approximation. The Poisson distribution is a good approximation for the number of occurrences of a rare event in a large number of trials, which fits our scenario of finding defective bolts in large quantities.
Given:
The probability of a bolt being defective is 0.1%0.1\% or 0.0010.001.
Each box contains 500 bolts.
The expected number of defective bolts in a box is the product of the number of trials (bolts in a box) and the probability of success (a bolt being defective):
We want to find the expected number of boxes with at least two defective bolts. First, we calculate the probability of a box having 0 or 1 defective bolt and then subtract this from 1 to get the probability of having at least 2 defective bolts.
The probability of a box having exactly kk defective bolts in a Poisson distribution is given by:
Finally, the expected number of boxes with at least two defective bolts out of 100 boxes is:
“Expected number of boxes”=100 xx P(X >= 2)\text{Expected number of boxes} = 100 \times P(X \geq 2)
Let’s calculate these probabilities and the expected number of boxes.
After calculating, we find:
The probability of a box having at least two defective bolts is approximately 0.09020.0902.
Therefore, the expected number of boxes out of 100 that will contain at least two defective bolts is approximately 9.029.02.
This means, on average, about 9 boxes out of 100 are expected to contain at least two defective bolts.
(b) If the time (in hours) required to repair a machine is exponentially distributed with lambda=(1)/(2)\lambda=\frac{1}{2}, then :
(i) What is the probability that the repair time exceeds 2 hours?
(ii) What is the conditional probability that a repair takes at least 10 hours given that its duration exceeds 9 hours ?
Answer:
The exponential distribution is defined by the probability density function (pdf):
f(x;lambda)=lambdae^(-lambda x)” for “x >= 0f(x;\lambda) = \lambda e^{-\lambda x} \text{ for } x \geq 0
where lambda\lambda is the rate parameter. In this case, lambda=(1)/(2)\lambda = \frac{1}{2}.
(i) Probability that the Repair Time Exceeds 2 Hours
The probability that the repair time exceeds a certain value xx in an exponential distribution is given by the survival function, which is the complement of the cumulative distribution function (CDF):
(ii) Conditional Probability that a Repair Takes at Least 10 Hours Given that its Duration Exceeds 9 Hours
The conditional probability in an exponential distribution is memoryless, meaning the probability of the event occurring in the next time interval is independent of how much time has already passed. Thus, the conditional probability is the same as the unconditional probability for the additional time.
This means, given that the repair has already taken more than 9 hours, there is approximately a 60.65% chance that it will take at least 10 hours in total.
These results are based on the memoryless property of the exponential distribution, which makes the calculation of conditional probabilities straightforward.
(c) Write at least two applications of beta distribution.
Answer:
The Beta distribution is a versatile distribution that is particularly useful in scenarios where probabilities are modeled on a bounded interval, typically between 0 and 1. It is widely used in Bayesian statistics, quality control, and project management. Here are two applications of the Beta distribution:
1. Bayesian Inference and Learning
Application: In Bayesian statistics, the Beta distribution is often used as a prior distribution for binomial proportions. This is because the Beta distribution is a conjugate prior for the binomial distribution, which simplifies the process of updating beliefs with new evidence.
Example: Suppose a machine learning model is being trained to classify emails as spam or not spam. Initially, there is uncertainty about the true proportion of spam emails. A Beta distribution can be used to represent this uncertainty. As more emails are classified and the model is updated with this new data, the parameters of the Beta distribution are updated, reflecting the improved understanding of the proportion of spam emails.
2. Project Management and PERT
Application: In project management, particularly in Program Evaluation and Review Technique (PERT), the Beta distribution is used to model the completion times of different tasks or activities.
Example: In a construction project, the time to complete a particular task can vary. The Beta distribution can be used to model this variability, taking into account the most optimistic, most pessimistic, and most likely completion times. This helps in estimating the overall project completion time and in identifying potential delays.
These applications demonstrate the flexibility of the Beta distribution in handling scenarios where probabilities or proportions are modeled within a specific range, incorporating both prior knowledge and new information.